FinTech and Consumer Financial Well-Being

in the Information Age

Bruce Carlin∗ Arna Olafsson† Michaela Pagel‡

January 2019

Abstract

We analyze how FinTech adoption improves consumer financial decision-making.

Using a regression discontinuity in time design, we exploit the exogenous introduction of a mobile application for a financial aggregation platform. In response,

individuals accessed information about their transactions and bank account balances more often, which led to significant reductions in high-interest unsecured

debt and bank fees. The magnitudes are economically significant: for the overall

population, one additional monthly login reduced consumer debt by 14 percent over

a 2-year period. Additionally, we complement our within-individual identification

with cross-sectional evidence using a difference-in-differences estimation strategy.

Our empirical finding that additional information about account balances helps to

reduce consumer debt sheds light on the widespread use of such debt throughout the

developed world, which has been a long-standing puzzle in the household-finance

literature (Laibson et al., 2000).

JEL classifications: D14, D83, G02.

∗Department of Finance, Anderson School of Management, University of California at Los Angeles,

Los Angeles, CA, USA, & NBER. bruce.carlin@anderson.ucla.edu

†Department of Finance, Copenhagen Business School, 2000 Frederiksberg, Denmark. ao.fi@cbs.dk

‡Division of Economics and Finance, Columbia Business School, NY, USA, NBER, & CEPR.

mpagel@columbia.edu

We thank numerous seminar participants, our discussants, and conference participants at the AFFECT

Conference University of Miami, University of Kentucky Finance Conference, Santiago Finance Conference, 6th ITAM Finance Conference, and the AEA. This project has received funding from Danish

Council for Independent Research, under grant agreement no 6165-00020. We are indebted to Ag ́ust  ́

Schweitz Eriksson and Meniga for providing and helping with the data.
1 Introduction

How does access to information affect individual decision making? For decades, this has

been one of the most fundamental questions in economics (e.g., Stigler, 1961). With

the advent of the information age, and the surge of FinTech products consumers use

(e.g., mint.com, personalcapital.com, YNAB.com), we would presume that people are

better informed and equipped to make good choices. However, beyond measuring the

adoption of new technology, actually quantifying its economic impact is challenging. We

know that people of different generations and demographic backgrounds incorporate new

technology into their lives at different rates (Anderson, 2015). But we know very little to

date about how this affects actual outcomes, and whether any effects vary cross-sectionally

in the population.

Sorting this out in a robust and careful way is challenging because it is typically

impossible to deal with endogeneity, reverse causality, and omitted variables without

making some leaps of faith. While it is intuitive that less costly access to information

may increase welfare, it is also likely that higher wealth increase either the incentives to

acquire information or the ease of accessing it.1

In this paper, we address these issues by using a unique data set from Iceland. A

substantial fraction of the citizens in the country use a common on-line platform that

consolidates all of their bank account information and transaction histories in one place.

Before 2014, access to this personal financial information only occurred via the Internet on a desktop or laptop computer. On November 14, 2014, a mobile application was

exogenously released, which gave users easier and remote access to bank account information. Figure 1 shows the propensity to log in to the financial aggregation platform

before and after the mobile app introduction, documenting that consumers indeed increased their information access in response to the availability of new technology. Before

1

In the United States, as of 2015, high income consumers were much more likely than low income

consumers to use the Internet (97% versus 74%) and own a smartphone (87% versus 52%) (Perrin and

Duggan, 2015; Perrin, 2015, see). Also, according to Smit (2014), this difference is greater in adults older

than 65 years. In this age group, 90% of high income elderly people access the Internet, whereas only

39% of low income seniors go on-line.

1
turning to the effects this had, it is important to note that the mobile application did

not offer consumers either notifications or financial advice before they actually logged

in and it did not have a functionality to execute transactions. As such, any observable

change in consumer outcomes that we document occurred because of less costly access to

information and thus more frequent information acquisition, not because of notifications,

financial advice, or more convenient transactions.

{Figure 1 around here}

In our data set, we have time-series information about the frequency and method of

access to bank information (desktop vs. smartphone), which we can analyze together

with demographic data, economic decisions (e.g., consumption and savings), channels

through which consumers access credit (credit cards versus debit card overdrafts), and the

resultant financial outcomes (consumer debt and bank fees). One key economic outcome

that we focus on is the tendency for people to pay penalties in the form of interest

on short-term uncollateralized debt and other fees, such as late and non-sufficient fund

fees. No matter what an individual’s utility function might be, paying lower bank fees in

response to voluntarily acquiring more frequent information should improve their welfare.

We use a regression discontinuity in time design, where the time of the exogenous introduction of the mobile application is used to instrument logins. This allows us to isolate

the causal impact of more information on economic outcomes. In the first stage, we estimate the change in an individual’s propensity to log into their financial accounts, which

characterizes how new technology affects access to information. In the second stage, we

use the predicted jump in logins at the time of the app introduction to identify the per

login effect of the app introduction on financial fee payments and other economic outcomes. In both stages, we include individual fixed effects to control for all time-invariant

omitted factors or individual characteristics that could affect the economic outcomes we

measure. Thus, we estimate a causal within-individual local average treatment effect

(LATE). However, since the app was broadly adopted relatively quickly by all age groups

2
and we look at a long time period before and after the introduction of the app, we believe

our results can be generalized.

Because the regression discontinuity in time design relies on time-series variation for

identification, one potential challenge is a higher likelihood that important covariates are

also discontinuous to the forcing variable over time. If other confounding events take

place at the same time and affect adopters differently from non-adopters, our identification would be challenged. We undertake a number of steps to address this problem.

First, we carefully analyze whether any other confounding institutional changes or new

regulations occurred during our time period of the app introduction.2 Second, we include

controls for the month of the year and for concurrent economic conditions (e.g., interest

rates, inflation, and unemployment). Third, we use different functional forms and bandwidths of time from the app introduction to alleviate concerns about time-series trends

and time-varying confounds that we assume to change smoothly across the date of the

experiment.3 Finally, as a robustness check and to complement our within-individual

time-series identification approach with cross-sectional identification, we also employ a

difference-in-differences estimation strategy to document the effects of the app introduction on adopters versus non-adopters.

The mobile application helped consumers pay less financial fees. Based on just the

raw data, Figure 2 shows the total bank penalties paid during our time series. Up until

the introduction of the app, financial fees increased. But, once the app was introduced,

there was a trend reversal and the amount of fees paid grew at a lower rate. Based on our

regression results for the entire population, each added login was associated with approx2To our knowledge, the only institutional change that occurred during our evaluation window was

on December 14 2014, when a court ruling took place that addressed deceptive merchant fee practices.

However, this ruling did not involve consumer financial fees. Furthermore, the central bank of Iceland was

reducing interest rates marginally in November 2014, a potential confound that we address by controlling

for the central bank policy rate directly. Furthermore, the time fixed effects control for all macroeconomic

trends before and after the app introduction.

3As documented by Hausman and Rapson (2017), estimates may be biased if the time-series properties

of the data are ignored, for instance in the presence of autoregressive processes. In contrast, tests for

sorting or bunching near the discontinuity, as typically done for standard regression discontinuity (RD)

designs, are irrelevant, making the methodology closer to an event study than a regression discontinuity

design. Thus, unlike in standard RD designs, using large bandwidths around the threshold does not

constitute a problem.

3
imately $2.24 lower bank fees per month and $1.77 lower overdraft interest. Accounting

for the frequency of individual monthly logins, logging in at least once in response to

the app introduction was associated with a decrease of $19.62 in bank fees and $15.47

in overdraft interest. Given that the average individual who adopted the app rolls over

$1,356 in overdraft debt ($4,698 conditional on having overdraft debt) and pays around

$13 in interest expenses per month, when they look at their overdraft balance one more

time per month, they reduce their overdrafts by approximately 14 percent over a 2-year

period.4

{Figure 2 around here}

Furthermore, Figures 3 and 4 separately display the evolution of overdraft interest

and late fees paid during our time series. We can see in the raw data that most of the

reduction in overall fees is driven by overdraft interest, i.e., individuals roll over less highinterest consumer debt in response to accessing information about their account balances

more often.

{Figures 3 and 4 around here}

Relative to the monthly expenditures during the sample period, the effect we document represents an economically meaningful change, especially for lower income households.5 Moreover, our findings help to shed light on why high-interest consumer debt

exists in such magnitudes, even though it is not consistent with standard preferences in

life-cycle consumption models (Laibson et al., 2000). Indeed, the 2015 American Household Credit Card Debt Study estimates the total credit card debt owed by an average

U.S. household to be $15,762, which amounts to a total of $733 billion. Our empirical

4The use of a long time period allows us to generalize our effect. Furthermore, we find that this

estimated effect does not change when we use alternative bandwidths of one fourth, one half, and two

thirds of the bandwidth in our baseline specification. Given that the app had been quickly and broadly

adopted, we believe we can generalize our estimated effects.

5We provide back-of-the envelope calculations to show that the average individual is plausibly better

off logging in more as opposed to not logging into the app.

4
finding that consumers manage to reduce their debt holdings by paying more attention

to it speaks to non-standard preferences and overconsumption problems as a likely explanation for the initial use of consumer debt (Laibson et al., 2007), rather than rational

consumption smoothing in response to permanent income shocks when funds are tied

up in illiquid savings (Kaplan and Violante, 2014) or rational consumption smoothing in

response to transitory income shocks (Keys, 2010; Sullivan, 2008).

Beyond making more responsible consumption-savings decisions after paying more

attention to bank account balances, the observed drop in financial penalties could be

explained by changes in how people used consumer credit. We find this to be the case

as well. In the total population, adoption of the technology was associated with a 10.6%

growth in credit card use relative to debit cards in managing short-term liabilities. Increasing credit card use is a rational response to having better information. Since credit

cards offer a 30-50 day float to avoid paying interest for convenience users, compared to

overdrafts where interest is incurred immediately, they are superior to consumers for very

short-term debt holdings. However, such better liability management can only explain

a fraction of our reduction in overdraft interest. We thus conclude that paying greater

attention to finances itself causes more prudent consumption and savings decisions, which

is also consistent with the fact that we observe most of the fee reductions in overdraft

interest rather than late fees or non-sufficient fund fees. In other words, the savings appear driven by more prudent spending decisions instead of being relatively mechanical

reductions in avoidable fees.

The academic profession has only hit the tip of the iceberg in characterizing the potential benefits and costs of technology on consumer financial decision-making. This is

a nascent and growing literature. Agarwal et al. (2018) show that individuals learn to

avoid late fees after having paid them initially. Stango and Zinman (2014) document that

individuals respond to surveys about overdrafts by paying greater attention to account

balances and incurring fewer fees. Levi (2015) shows that individuals respond to information about their net worth by increasing their savings in certain conditions. Medina

5
(2016) finds that reminders for timely payment reduce the credit card late fees that are

paid. Karlan et al. (2016) show that text message reminders help consumers to avoid

penalties.6 Generally, these studies involve some sort of reminder or stimulus that induces people to change their behavior towards one specific form of avoidable financial

fees. In contrast, in our study, we show that simply because individuals access information more frequently without receiving reminders, messages, or other stimuli, they reduce

their high-interest consumer debt. Furthermore, a defining feature of our study is that

we have information not only on individual financial standing at very high accuracy and

frequency, but also on individual access to that information via logins to the financial

aggregation app.

Consistent with our results, several previous studies have shown that the quality and

channel through which information is accessed affects consumer knowledge and decision

making. Fernandes et al. (2014) show that just-in-time access to on-line advice improves

financial decision-making. Lusardi et al. (2015) show that on-line videos are more effective

than standard materials like written disclosures when consumers make choices. Carlin

et al. (2016) show that video content is beneficial in helping consumers to both choose

better opportunities and avoid falling prey to deceptive advertising in retail financial

markets, and are also drivers of social learning in these settings. On the other hand, in

some circumstances, it is possible that having more access to information may lead to

worse outcomes. As Bernhardt and Cuevas (2016) show, better access to information led

to the Felices y Forrados consumer financial fiasco in Chile.

The recent rise of FinTech has certainly piqued the interest of the academic community. For example, Buchak et al. (2017) study the effect of FinTech on shadow banking.

The authors show that because of different regulatory requirements, FinTech lenders

account for the majority of the growth in shadow bank mortgage lending. Philippon

(2016) studies the impact of FinTech on the financial industry and how it affects access

6Other studies that analyze the determinants and effects of attention using logins to retirement,

brokerage, and bank accounts are Karlsson et al. (2009); Gherzi et al. (2014); Gargano and Rossi (2017);

?.

6
to financial services. A review of the evolution of FinTech is provided by Arner et al.

(2016).

The remainder of the paper is organized as follows. In Section 2, we describe the

data and offer summary statistics. In Section 3, we explain our identification approach.

In Section 4, we report our main results and discuss their robustness. Finally, Section 5

presents concluding remarks.

2 Data and summary statistics

We use data from Iceland that are collected by Meniga, a financial aggregation software

provider to European banks and financial institutions.7 Meniga’s account aggregation

platform allows bank customers to manage all of their bank accounts and credit cards

across multiple banks in one place by consolidating data from various sources (internal

and external). Meniga’s financial feed reflects consumers’ financial lives in familiar social

media style. This data set has already proved useful for studying the spending responses

of individuals to income arrivals and how individuals transition into retirement (Olafsson

and Pagel, 2018a,b).

Each day, the application automatically records all bank and credit card transactions, including descriptions as well as balances, overdraft, and credit limits. Figure 5

displays screenshots of the app’s user interface. The first screenshot shows background

characteristics that the user provides, the second one shows transactions, and the third

one includes bank account information. The initial version of the app did not include

elements of financial advice, but later versions flagged certain events (e.g., unusually high

transactions, money deposits and low balance). Examples of this are displayed in Figure 6. Furthermore, the figure shows a screenshot of the default options for messages

7Meniga was founded in 2009 and is the European market leader of white-label Personal Finance Management (PFM) and next-generation online banking solutions, reaching over 50 million mobile banking

users across 20 countries. In the US, comparable software is provided by mint.com, personalcapital.com,

or YNAB.com. Relative to these US software providers, Meniga is less focused on advice with respect

to spending, saving, or credit cards as well as portfolio performance. The app thus offers a clean and

simple overview over personal finances.

7
that are turned off except for receiving merchant offers (that are similar to groupon offers). Meniga expanded their merchant offer features recently, however, when the app

got introduced, it did not sent those offers yet. Moreover, the app does not send push

notifications, so that individuals would have to log in first to see messages or flagged

data. Moreover, it is important to note that we do not find most of the reductions in

late fees or non-sufficient fund fees, which should be helped by messages, but rather a

general reduction in roll-over consumer debt. Contrary to some of the advertisements on

the app’s website (the “international demo” on the Meniga homepage does not accurately

reflect how the platform looks and functions in Iceland), users have to log in initially to

see all messages and warnings.8

{Figures 5 and 6 around here}

In January 2017, the Icelandic population counted 338,349 individuals, 262,846 of

which were older than 18. At the same time, Meniga had 52,545 users, which is about

20 percent of the adult individuals living in Iceland. We study 13,411 active users with

complete records, i.e., for whom we observe all balances, salary arrivals, and transactions.

In general, all individuals in our sample have passed an ”activity test” that is designed

to verify that we are capturing all of their financial picture. More specifically, our sample of Meniga users is restricted to individuals with complete records, defined by four

requirements. First, we restrict our sample to individuals for whom we see bank account

balances and credit lines. Second, we restrict our sample to individuals for whom we

observe income arrivals (this does not only include labor market income but also, e.g.,

unemployment benefits, pension payments, invalidity benefits, and student loans). The

third requirement is that key demographic information about the user is available (age,

sex, and postal code). The final requirement is that the consumption of each user must be

8However, the app did not send these messages over the sample period that we are considering.

Furthermore, the current version of the app asks for permission to send push notifications, but, to the

best of our knowledge from having the app installed, does not actually send any.

8
credible, which we ensure by requiring at least 5 food transactions in at least 23 months

of a 24 months period.

All the tables and figures we show (except for Table 4 which includes all active users

that started using the software or app at some point), for instance, figure 2, are based

on this final sample. In terms of demographic statistics, the final sample of users is not

different from the overall sample and because Meniga’s service is marketed through banks,

we can confirm that our sample is representative of the adult population of Iceland. For

three generational categories based on when individuals are born, Baby Boomers (1946-

1964), Generation X’ers (1965-1980), and Millennials (1981-2000), Table 1 summarizes

the demographic data in our study and provides a comparison with those reported in the

representative consumer survey of Statistics Iceland.

{Table 1 around here}

We aggregate the data to a monthly panel of individual logins, financial penalties,

credit use, and consumption choices from November 2012 to November 2016. The data

include information on how many times each individual logs in via the app or via a

desktop. The app was introduced on November 14, 2014.9 Because we are interested in

debt expenses that might be avoided by having better information and allowing consumers

to make small and relatively costless changes in their behavior, we consider three types of

penalties: late payment interest, non-sufficient funds fees, and late fees. Additionally, we

observe the interest expenses for individuals that hold overdrafts, which is the primary

form of Icelandic high-interest unsecured consumer debt.

1 Late-payment interest: Credit card companies charge late-payment interest

daily from the date a payment is due and payable to the date it is paid in full.

2 Non-sufficient funds fees: When there are insufficient funds or the overdraft

limit is exceeded in the consumer’s current account in the event of attempted debit

card transactions, the bank charges their account with fees.

9We do not find any evidence of individuals linking more accounts following the app introduction.

9
3 Late fees: Fees assessed for paying bills after their due date.

4 Interest: An overdraft occurs when withdrawals from a current account exceed

the available balance. This means that the balance is negative and hence that the

bank provides credit to the account holder and interest is charged at the agreed rate.

Virtually all current accounts in Iceland offer a pre-agreed overdraft facility, the size

of which is based upon affordability and credit history. This overdraft facility can be

used at any time without consulting the bank and can be maintained indefinitely

(subject to ad hoc reviews). Although an overdraft facility may be authorized,

technically the money is repayable on demand by the bank. In reality, repayment

demands are rare because the overdrafts are profitable for banks and expensive for

customers.

Table 2 displays summary statistics about the penalties incurred and the use of various

forms of consumer credit by people in our sample. The table displays average penalties

per month and per individual as well as their standard deviations across individuals.

Comparison is made between consumers who logged in using the app to those who did

not, within windows of time around the app introduction that varied from 3 months to

18 months. Total and individual sources of financial penalties were lower for consumers

who used the cell phone app. Additionally, consumers who used the app were more likely

to use credit cards to cover their expenditures. Of course, Table 2 does not allow us

to make causal claims yet, as use of the app and financial performance are endogenous,

which our identification strategy ameliorates.

{Table 2 around here}

Overall, individuals in Iceland enjoy access to substantial consumer credit and pay

considerable financial fees for it. In this sense, Iceland is very similar to the US. As can

be seen in Table 3, individuals hold approximately $4,698 in overdrafts conditional on

having overdraft debt (in Iceland, individuals typically pay off their credit card in full

10
and use overdrafts to roll-over debt). Nevertheless, they still enjoy substantial liquidity,

i.e., further borrowing capacity before they hit their limits, i.e., $11,169 on average.

Furthermore, the table shows average income, spending, balances, limits, and financial

fees for adopters and non-adopters. None of the differences between the groups are

statistically significant in the raw data, which is reassuring, though the validity of our

main identification strategy will not rely on a comparison of adopters and non-adopters.

While Table 3 shows the comparison of our final sample of adopters and non-adopters

for which we observe all data two years before and after the app introduction, Table 4

displays a comparison of financial fees paid as well as overall financial standing for all

active users. It can be seen that those individuals that started using the software at least

two years before the app introduction have somewhat higher income and consumer debt

though none of the differences are statistically significant.

{Table 3 around here}

We collect income and spending data in the panel by extracting it from the PFM

system, which has already been categorized by a three tiered approach.10 The system

categorizes the income into 20 different income categories. Regular income categories

are child support, child benefits, dividends, parental leave benefits, pensions, housing

benefits, rental benefits, rental income, salary, student loans, and unemployment benefits. Irregular income categories are grants, other income, insurance claims, investment

transactions, loan write-offs, reimbursements, tax rebates, travel allowances, and lottery

winnings. Total household income is defined as the sum of regular and irregular income

of spouses.

Spending is categorized into 15 categories. The spending categories are groceries,

fuel, alcohol, ready made food, home improvement, transportation, clothing and accessories, sports and activities, pharmacies, media, bookstores, thermal baths, toy stores,

insurances, and various subcategories of recreation (e.g., cinemas, gaming, and gambling).

10This three-tiered approach uses system rules, user rules and community-rules. More details are

available from the authors upon request.

11
For the purposes of our empirical analysis, we define two categories of spending. The

first contains necessities such as groceries, fuel, and pharmacy. The second includes discretionary entertainment such as alcohol, restaurant/takeout, lottery, gambling, gaming,

and cinema. Table 4 displays summary statistics about the income and spending categories for all active users, as well as spending statistics from the representative consumer

survey of Statistics Iceland. All numbers have been converted to US dollars. To the

extent that the categories match, we find very similar figures in our sample as in the

representative consumer survey. Thus, our sample appears to be fairly representative,

not only in terms of demographics, but also with respect to income and spending.

Also according to Table 4, our sample characteristics are similar to US data. The

average age of our sample is 38 whereas the average age in the US population in 2015 was

38. The percentage of women in our sample is 46% whereas the US representative was

51% in 2015. The mean income in the U.S. population in 2015 dollars per adult member

was $3,266, whereas the individual monthly mean income in our sample is $3,783.11

{Table 4 around here}

3 Empirical Strategy

We use a regression discontinuity in time design that exploits the discontinuity in individual access to the financial aggregation platform that arose when the mobile application

was introduced on November 14, 2014. The timing of the app introduction is plausibly

exogenous to individual characteristics but caused some individuals to log in more often

and is thus a valuable source of identifying variation. We exploit this to estimate a causal

effect of less costly access to information on spending as well as financial penalties. The

instrumental variable design may be implemented by the following two-equation system:

Yit = αi + βLit + 1 [t ≥ c] fl (t − c) + 1 [t < c] fr (c − t) + it, (1)

11All US numbers stem from the US Census Bureau’s American Community Survey (ACS) in 2015.

12
Lit = γi + 1 [t ≥ c] (gl (t − c) + λ) + 1 [t < c] gr (c − t) + νit, (2)

where Yit is a measure of the economic outcomes (i.e., financial penalties or spending

categories) for individual i at time t, αi and γi are individual fixed effects, c is the

time of the app introduction, and fl, fr, gl, and gr are unknown functional forms that

capture the effect of time from the mobile app introduction on economic outcomes. In

all specifications, we cluster standard errors at the individual level as standard in highfrequency individual-level panel data (see, e.g. Baker, 2014).

The interpretation of Equation (1) is that it describes the average economic outcomes

for individuals under alternative assignments into higher frequency logins, controlling for

any other relationship between the time from the mobile app introduction and economic

outcomes. Since logging in more often is not randomly assigned, logins are likely correlated with the error component in a simple ordinary least squares (OLS) regression

of economic outcomes on logins. As such, OLS estimates of (1) would not have any

causal interpretation. Therefore, we estimate the two-equation system by two-stage least

squares (2SLS) using the discontinuity in logins caused by the app introduction as an

instrument. The 2SLS estimate of β characterizes the causal effect of technology on

economic outcomes.12

We estimate the system of equations using both polynomial and local linear regressions. The only restriction on the functional forms that capture the effects of time, fl

and fr (gl and gr), is that they must differ at c by λ. We estimate λ as the jump in logins

at the mobile app introduction date in the first-stage regression. Then, we estimate β in

the second stage. Our empirical design thus uses the discontinuities in the relationship

between the mobile app introduction and higher frequency of logins to identify the causal

effect of observing financial accounts on economic outcomes, i.e., by distinguishing the

12This 2SLS approach faces the problem that the endogenous variable is a dummy and thus has

a non-linear probability distribution which the second-stage regression relies upon. In such settings,

Angrist and Pischke (2008) advise garden-variety 2SLS for dummy endogenous variables rather than the

use of forbidden plug-in regressions or nonlinear fitted values as instruments, which also ensures that

standard errors are computed correctly. Thus, we stick to the standard 2SLS approach as our preferred

specification but ensured that we find similar marginal effects using alternative methods.

13
nonlinear and discontinuous function, 1 [t ≥ c], from the smooth function f (t).

The key identification assumption that underlies our approach is that f(·) is a continuous function. Intuitively, the continuity assumption requires that differential assignment

of logging in more often is the only source of discontinuity in outcomes around the time of

the mobile app introduction, c, so that unobservables vary smoothly as a function of time

from app introduction and, in particular, do not jump at the time of the introduction. As

such, all potential time-varying confounds must be assumed to change smoothly across

the date of the experiment. Formally, then, the conditional mean function, E [Yit|t − c],

is continuous in (t−c) at 0, or equivalently E [it|t − c] is continuous in (t−c) at 0. Under

this assumption the treatment effect, β, is obtained by estimating the discontinuity in the

empirical regression function at the point where the probability of the treatment dummy

jumps at the assignment threshold and can be given a causal interpretation.

As shown in Lee (2008) and Lee and Lemieux (2010), smoothness of the density of

the treatment-determining variable is sufficient for the continuity assumption to hold. In

our case, this assumption explicitly allows for individuals to have some control over their

value of the assignment variable. As long as this control is imprecise, which it clearly is

in our case since they did not control when the app was introduced, assignment to higher

login frequencies will be randomized around the threshold.

We can examine whether this quasi-random variation in the cost of accessing information changes individuals’ economic outcomes by estimating the following reduced form

model:

Yit = τi + 1 [t ≥ c] (fl(t − c) + π) + 1 [t < c] fr (c − t) + ξit, (3)

where π can be interpreted as an “intention-to-treat” (ITT) effect of the mobile app

introduction on economic outcomes. The ratio of the reduced form coefficient π and the

first-stage coefficient λ is numerically equivalent to the 2SLS estimate of β, provided that

the same bandwidth is used in equations (2) and (3) in the local linear case and the

same order of polynomial is used for f and g in the polynomial regression case, since the

14
two-equation system is exactly identified. The ITT effect captures the effect of the app

introduction on the whole population.

The IV estimates of Equation (2) use discontinuities in the relationship between the

mobile app introduction and higher frequency of logins to identify the causal effect of

observing financial accounts on economic outcomes at the same time that any other

relationship between time from the app introduction and economic outcomes measured

by financial fees is controlled for by including a smooth function of absolute time from

the app introduction as a control. We use both a global polynomial approach and a local

linear approach with varying bandwidths around the app introduction.

In the context of the causal model above, the instrumental variable estimate should

be interpreted as an average effect of the increased logins for individuals whose log in

behavior was influenced by the app introduction. This group may not necessarily be a

good representation of the entire population of individuals. Thus, we estimate a local

average treatment effect (LATE) rather than an average treatment effect. That said, the

app has been broadly adopted quickly over the long time period that we consider, as can

be seen in Figure 8, which means that we do not identify off of a very specific part of the

population.

The identification approach relies on a single exogenous event, the app introduction.

This event’s effects on economic outcomes could be confounded if other events happened

or things changed around the same time, which affected adopters differently than nonadopters. As we discuss and analyze in Sections 4.5 and 4.4, our analysis is robust to a

difference-in-differences approach and to the best of our knowledge, no confounding event

took place around the same time.

Frequently in regression discontinuity designs, there is a trade-off between having two

periods that are as close in time to each other as possible (obtained by reducing the time

window around the app introduction) and having a longer sample period (by widening

the window). In our case, this is not a problem here because individuals who start using

the app later are more similar to those that never use it at all than to individuals who

15
start using it immediately after the introduction. However, to address this we report our

findings for several time windows (i.e. 6, 12, and 18 months before and after the app

introduction).

As discussed by Hausman and Rapson (2017), regression discontinuity in time estimates may be biased if the time-series properties of the data are ignored, for instance

in the presence of autoregressive processes. Whenever a potential reduction of fees itself

would cause a further reduction in fees, our estimates could be biased upwards. While

autoregression is a potential concern in many environmental applications of regression

discontinuity in time designs, it is probably not a concern here. After all, the wealth

effect from a small and transient reduction in fees is not likely to, in and of itself, cause

a persistent drop in the propensity for an individual to incur financial fees in the future. While serial dependence in the residuals might arise, we address this by clustering

standard errors at the individual level. Finally, as in a standard regression discontinuity

design, one may worry about strategic behavior around the threshold. However, using

time as an assignment variable makes this irrelevant. But, one might still worry about a

type of sorting where individuals start using the platform only when the app is introduced

(i.e., individuals only use the aggregation service because it can be accessed via the app).

Because we only consider individuals in our study who were already using the financial

aggregation platform before the app introduction, we do not have to worry about this

concern.

It is important to note that all of our results are estimated including individual fixed

effects, which control for all time-invariant observable or unobservable characteristics. A

potential issue is that individual characteristics for those individuals who adopt the new

technology may change around the introduction of the app. Our difference-in-differences

specification in Section 4.5 should address this concern.

16
4 Results

4.1 Logins

Based on the raw data plotted in Figure 1, there is a clear discontinuity in the propensity

of individuals to log into their financial accounts around the introduction of the mobile

app. This is further described in Table 5, which gives some summary statistics about

logins for the age and gender demographic categories. Before the introduction of the

mobile app, men appeared more attentive to their accounts than women and this gap

increased once the app became available. Figure 7 shows that for every age group, men

were more likely to access their personal information via the mobile app right after its

introduction. By August 2016, however, approximately the same fraction of men and

women had adopted the new technology (43% versus 39%). Figure 8 also characterizes

this trend by plotting the cumulative adoption of the smartphone technology through

time. We can observe a fairly quick and broad adoption of the app by both genders and

all age groups, this alleviates concerns that we are documenting an effect identified off of

a very specific fraction of the population.

{Table 5, Figure 7, and Figure 8 around here}

People of different generations adopted the new technology at much different rates.

According to Table 5, the number of logins for Millennials more than doubled, whereas

logins for Baby Boomers increased at a lower rate. In November 2014, even though the

app was introduced halfway through the month, the number of app logins accounted for

60% of total logins for Millennials, whereas it only accounted for 28% of logins for Baby

Boomers. By August 2016, roughly, 52% of Millennials had used the app, compared to

only 27% of Baby Boomers.

Empirical analysis confirms these trends in the first stage regressions for the entire

population. Table 6 shows our estimates using a 24-month window before and after the

app introduction. Column (1) shows a significant jump in logins after the mobile app

17
introduction. Based on the results, individuals were 9.23% more likely to log in each

month after the app was made available. That is, individuals logged in 0.8 more times

per month after the new technology was available. Both of these results are economically

and statistically significant.

{Table 6 around here}

4.2 Financial Outcomes

The raw data in Figure 2 suggests that less costly access to information led to fewer fees

and interest payments for consumer debt. The figure plots the raw average of each month’s

total financial fee payments for the estimation sample and fits two linear regression lines,

one up until November 2014 and one after November 2014. Up until the introduction

of the app, financial fees increased, because the economy was expanding. But after the

app introduction, this trend reversed.13 We do not see a discontinuity in this figure, as

for the logins in Figure 1, which is due to the gradual adoption of the app by different

individuals, but we clearly see a change in the slope of financial fees paid.

{Table 7 around here}

This is further characterized in Table 6. Column (2) shows the estimate for coefficient

π in Equation (3), the intention-to-treat effect of the mobile app introduction on financial

fee payments. Column (3) shows the 2SLS IV estimate for coefficient β in Equation (1),

the causal LATE effect of the mobile app introduction. Column 3 shows that in the overall

population, each extra login was associated with a $2.24 reduction in financial fees. This

13Economic growth around the time of the app introduction slowed and then picked up again but

unless the economic trend changed discontinuously in November 2014 and affected adopters differently

from non-adopters, macro-economic circumstances cannot explain our results as discussed in Section 4.4.

Moreover, Hundtofte et al. (2018) show that individuals borrow more in good economic times rather

than when they get hit by income shocks such as unemployment. This is what we see in the upward

trend of overdraft payments up until the introduction of the app, i.e., Figure 3.

18
effect was similar for men and women and did not differ reliably across generations.14

Accounting for the frequency of individual monthly logins, logging in at least once in

response to the app introduction was associated with a decrease of $19.62 in bank fees

and $15.47 in overdraft interest. As can be seen in Table 3, the average individual

who adopted the app rolls over $1,356 in overdraft debt ($4,698 conditional on having

overdraft debt) and pays around $13 in interest expenses per month. Thus, when they

look at their overdraft balance one more time per month, they reduce their overdrafts by

approximately 14 percent over a 2-year period.

A back-of-the envelope calculation suggests that the average hourly wage is approximately $3,783/(52/12)/40 ≈ $22 per hour, assuming a 40 hour work-week. Only if the

average individual spends more than $19.62/ $22=0.89 hours with the app per month,

which appears implausible, he or she would be better off not logging into the app at all.

The savings of a marginal log in is $2.24/ $22=0.1, i.e., worth 6 minutes of work, which

also appears like an implausible time commitment to log in to the app. Furthermore, the

14 percent reduction in overdrafts over a two-year period is substantial and has overall

interest costs of 0.14 $1,356(1+0.13/ 12)24=$246 or $852 conditional on overdraft debt

(the prevailing annualized overdraft interest rate at the time of the app introduction was

approximately 13% (see Figure 9) and is compounded at the monthly level).

The choice of length of time around the app introduction on November 14, 2014, is

important as it affects the smoothing of our data. It is therefore important to show that

our results are robust to varying the bandwidth.Table 8 therefore presents the results

of our analysis where we vary the bandwidth around the app introduction and results

using global polynomials up to order four. The statistical and economic significance of

our estimates remain largely unchanged. Reassuringly, the results show that the effects

do not differ by much depending on the specification.

{Table 8 around here}

14Estimates are reported in ISK, to obtain the USD estimates, the coefficients can simply be divided

by 100. This adjustment reflects the approximate exchange rate over our sample period.

19
4.3 Credit Use and Expenditures

Beyond knowing that individuals who log in more reduce their financial fee payments,

the exact channel by which individuals save is hard to detect even with comprehensive

transaction-level data. A potential channel might be the tendency of individuals to use

credit versus debit cards. After all, overdraft interest is a substantial fraction of financial

fees paid, and, as shown in Table 2, consumers who used the app were more likely to use

credit cards to make expenditures.

We explore this further in Table 9 where we measure the impact of logins on the

fraction of expenditures paid by credit cards. According to the results, for the entire

population, each additional login was associated with a 2.36% increase in the fraction of

expenditures purchased with a credit card.15 Likewise, using a dummy variable for a login

at any time using the app, the fraction of purchases made with a credit card increased

by approximately 20.36%. Table 8 confirms these results with shorter symmetric bands

of time around the app introduction and global polynomial controls up to order four.

{Tables 9 and 10 around here}

These results provide a rational explanation for why individuals had some economic

gain from the new technology. For consumers with low savings, use of a credit card

is superior to overdrawing a bank account with a debit card, when managing shortterm liquidity needs. Credit cards typically provide a 30-50 day float until interest is

charged, whereas overdraft fees are incurred immediately. A simple back-of-the-envelope

calculation can be used to quantify the impact of using credit cards rather than debit

cards on overdraft interest payments. A 2.36% increase in monthly spending on credit

cards times an average monthly expenditure of $1,580 equals $32.2 in additional expenses

paid via credit cards rather than debit cards. This translates to a monthly interest savings

of 32.2(0.13/12) = $0.348, as the prevailing overdraft interest rate at the time of the app

introduction was approximately 13% (see Figure 9).

15This growth rate is computed by dividing 0.0106 by the base rate of 0.45.

20
{Figure 9 around here}

Nevertheless, the monthly savings associated with better short-term liquidity management cannot explain the entire 14 percent decrease in overdraft debt over a 2-year

period. It seems that the more frequent observation of balances also makes them more

salient and that this helps consumers to reduce them.

4.4 Discussion of Robustness

As we have reiterated, the app introduction was not associated with more frequent reminders or notifications about individual accounts. Users only could view notifications

after they logged in. Individuals were also not able to sign up to receive reminders or push

notifications about events in their accounts (e.g., when they had unpaid bills). The only

messages by the app that took place during our time series are merchant offers that were

called card-linked offers (CLOs). However, these did not get launched until mid-2015 and

were not prevalent until 2017. Since this took place well after the app introduction, we

do not believe these offers constitute a problem to our specification or help account for

the reduction in financial fees we observe. In line with the absence of messages about low

balances or payments, we find only very small reductions in late fees and non-sufficient

fund fees and most reductions in overdraft interest.

Another potential concern is whether our analysis could be confounded by other

events that changed around November 2014, such as regulation changes or macroeconomic events. The only regulation change that we are aware of is a court ruling on

December 14, 2014 that addressed deceptive merchant fee practices. As this did not

involve consumer fees at all, we do not consider this to materially affect our analysis.

Additionally, since our findings are robust to a difference-in-differences specification, it is

unlikely that this regulation had any effect on consumers. Appendix A displays all the

Factiva economic news search results for Iceland over November 2014 to analyze potential

confounding events. Any discontinuous changes should have been noticed and reported

21
as economic news in November 2014, which, however, we do not find in the Factiva search

reports. What many articles are about is that the Icelandic central bank took another

step in reducing interest rates in November 2014 (the interest rate displays a general

downward trend over 2014 and 2015 although overdraft interest payments are trending

upwards). This is a potential confounding event that we address by directly controlling

for the central bank policy rate as we now briefly discuss. Without doubt, other macroeconomic conditions, such as personal and government consumption, output, or economic

sentiment, changed as well over the period. However, to the extent that these did not

change discontinuously in November 2014, our identification strategy is not affected.

As mentioned, we reviewed several macroeconomic indicators and conditions around

the event and only found one that could be considered concerning. There was a small

decrease in interest rates around the time of the app introduction (Figure 9). This could

be a potential concern since this would directly affect interest expenses, which are part of

the financial fees that we calculate. If adopters were disproportionally indebted, then a

discontinuous change in the overdraft interest rate could decrease their interest expenses

more. But, there are several reasons we do not think this is problematic. First, when we

directly control for such changes in the central bank policy rate, which determines changes

in overdraft interest rates, we do not observe a change in our estimates. Second, our

findings are robust to using a difference-in-differences approach that compares adopters

of the technology to non-adopters before and after the app introduction. Last, we observe

reductions in late fees and non-sufficient fund fees, which are not tied to the interest rate.

Indeed, Figure 4 shows the same trend reversal in late fees in the raw data.

A final concern might be that the financial crisis of 2008 affected Iceland differently

than other countries where consumer debt is prevalent or could have influenced our findings. After the crisis of 2008, Iceland recovered quickly and experienced high GDP

growth and low unemployment during our entire sample period. This recovery has been

attributed to its welfare system (Olafsson, 2016). Additionally, as it turns out, Iceland is

similar to many other economies, including the US, with regard to the use of consumer

22
debt. As can be seen in Table 3, individuals in Iceland hold approximately $4,698 in

overdrafts conditional on having overdraft debt (in Iceland, individuals typically pay off

their credit card in full and use overdrafts to roll-over debt). Nevertheless, they still enjoy substantial liquidity because they have additional borrowing capacity before hitting

their limits, i.e., $11,169 on average. In comparison, in the US, the average credit card

debt for individuals who roll it over is approximately $4,000 in the Survey of Consumer

Finances (SCF) data and individuals also enjoy substantial borrowing capacity. Thus,

we believe that our results can be generalized to the US and other European countries

with relatively large consumer debt holdings, such as the UK, Spain, and Turkey.

4.5 Difference-in-differences estimation

While the regression discontinuity in time design is our preferred identification approach,

we want to further alleviate concerns that factors other than the introduction of the

mobile app are driving our results and perform a difference-in-differences estimation. We

define “inactive” users as a control group and individuals who use the app in the first six

months after its introduction as the “treatment” group. While the control group are not

users of the app, they still meet our sample requirements of having complete records over

the entire sample period, i.e., they linked all accounts and we observe regular salary and

grocery transactions.

Figure 10 provides an illustration for the difference in logins between the treatment

and control groups, before and after the mobile app introduction. The trends in the

average number of logins before the smartphone introduction were almost parallel between the groups. However, after the introduction, the logins for adopters spiked.16 So,

it appears that the two groups experienced different changes in accessing bank account

information within a narrow time frame, but had parallel trends before the app introduction. Furthermore, as can be seen in Table 3, the spending, income, and balances

16There is a discrete jump in logins at the time of the app introduction and no pre-introduction runup. The increase in the figure is an artifact that arose when we created the graph and made the lines

continuous.

23
statistics of adopters and non-adopters are not significantly different from each other

before the app introduction. That also reassures us that we consider two samples that

match on observable characteristics.

{Figure 10 around here}

We estimate the following regression model:

Yit = α + βXit + τTi + f (t − c) + γ1 [t ≥ c] Ti + it, (4)

where treatment status is defined as

Ti =







0 if no mobile logins and no desktop logins in the year before the app intro

1 if at least one mobile login in first 6 months after app intro

In the model, the effect of the time from the app introduction on the outcome variable of

interest is captured by the function f (t) and we seek to analyze E[Yit|Ti]. If the correct

specification of the control function f(t) is used (i.e. the true conditional mean function

E[ωi|Ti]), it will capture all dependence between Ti and it so that the conditional mean

independence assumption will hold ( i.e., E[it|Ti] = 0).

This procedure renders consistent and unbiased OLS estimates in the case of linear

control functions. In this case, the causal effect of the treatment variable T on the

outcome variable Yit is captured by γ (Hahn et al., 2001). One problem is that this

regression-based estimation approach requires specification of the functional form f(·)

and any misspecified control function might produce inconsistent estimates. However,

by including the interaction term between the time from the app introduction and the

treatment dummy, we allow the slope coefficients to differ on each side of the threshold. In

the baseline specification, we use polynomials of time (months) from the app introduction

but we furthermore check that our estimates are robust to allowing for different functional

24
forms of the time control function.

The results are in Table 11. The difference-in-differences estimates show that the

mobile app led to a sizable and a statistically significant reduction in total bank fees,

late fees, and overdraft interest. The estimates show an approximately $4.68 reduction

in total bank fees when comparing individuals that started logging in more with the use

of the mobile app as compared to inactive users.

{Table 11 around here}

While we estimate a large effect on overdraft interest in our main specification in

Section 4.2, the difference-in-differences estimates are driven by late fees. This can be

explained by the fact that we compare adopters to inactive users in the difference-indifferences specification while we compare adopters to their previous selves in our main

specification, and we would therefore not necessarily expect the estimated effects to be

the same.

Our findings are consistent with the cross-sectional relationship between financial fees

and logins that we observe in the raw data. Figure 11 shows the averages of total bank

fees, late fees, and overdraft interest by the number of monthly logins. We can see that

in the cross-section of individuals, fewer logins are associated with higher overdrafts and

higher late fees.17

{Figure 11 around here}

5 Concluding Remarks

In this study, we analyze the effect of the introduction of a mobile app by a financial

aggregator which eases their consumers’ plight to gather information and make good

choices in two ways. First, it lowers search costs and makes finding personal information

17See ? for an in-depth analysis of the within-individual attention patterns.

25
easier. Second, it makes financial information more salient. This latter mechanism is

very important for consumers in retail financial markets. According to Loewenstein et al.

(2014) “[t]here are serious limitations on the amount of information to which people

can attend at any point in time” and “[d]isclosures are so ubiquitous [...] that it would

be impossible for people to attend to even a fraction of the disclosures to which they

are exposed.” Similarly, Hirshleifer and Teoh (2003) note that “[l]imited attention is a

necessary consequence of the vast amount of information available in the environment, and

of limits to information processing power.” Given this limited attention span, consumers

tend to focus on the most prominent stimuli or salient information. By consolidating

each user’s financial accounts, Meniga’s platform helps to reduce the costs of information

access and the mobile application makes that access clearer to the consumers that use it.

We document and quantify the effects that less costly access to information about

financial accounts has on consumers in the market. We find a substantial reduction

in financial fee payments in response to accessing information more often. This effect

should be welfare enhancing given that individuals log in voluntarily and the time costs

of logging in are very small. The decrease in financial fee payments is driven by overdraft

interest. In fact, people reduce their roll-over consumer debt by about 14 percent in a

2-year period, which carries high interest costs as it is unsecured. As noted before, since

the app does not send reminders or notifications, the decreases in high-interest consumer

debt that we document results from increased attention to personal finances.

That people reduce their overdrafts by paying more attention to them may be informative about how the overdrafts are accumulated in the first place. The leading but

competing economic explanations for the use short-term consumer debt are the following: 1) time-inconsistent preferences and overconsumption problems (Laibson et al., 2000,

2007) or 2) a desire to smooth income fluctuations in the presence of illiquid savings (Kaplan and Violante, 2014; Keys, 2010; Sullivan, 2008). Our findings may speak to the

former rather than the latter mechanism. After all, if individuals pay more attention

to their finances and then reduce their overdrafts, we could infer that they were not

26
happy with holding large overdrafts. Thus, our findings are relevant for policy-makers

and consumer protection. Moreover, the analysis in this paper contributes to a small

but growing literature on technology and economic outcomes. Given the regime shift we

experienced over the last decade associated with on-line education, social learning, and

electronic access to information, future study in this area appears warranted.

27
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29
Figures and Tables

Figure 1: Propensity to log in around the app introduction. Each raw data dot represents

the fraction of individuals who logged in in any given month. The lines are simple linear

fits through the data points before and after the app introduction.

30
Figure 2: Bank fees and penalty payments around the app introduction. Each raw data

dot represents the average amount of financial fees (NSF fees, late fees, and overdraft

interest) paid by all individuals in any given month. The lines are simple linear fits

through the data points before and after the app introduction.

Figure 3: Overdraft interest around the app introduction. Each raw data dot represents

the average amount of overdraft interest paid by all individuals in any given month. The

lines are simple linear fits through the data points before and after the app introduction.
32

Figure 4: Late fees around the app introduction. Each raw data dot represents the

average amount of late fees paid by all individuals in any given month. The lines are

simple linear fits through the data points before and after the app introduction.

Figure 5: The financial aggregation app: screenshots of home screens.
33

Figure 6: The financial aggregation app: screenshots of financial feed displaying messages

next to transactions and the default settings for messages. The app does not send push

notifications and individuals have to log in to see these messages.

Table 1: Demographic statistics

Panel A Mean Standard Statistics

Deviation Iceland

Age 40.6 11.5 37.2

Female 0.49 0.50 0.48

Unemployed 0.08 0.27 0.06

Parent 0.23 0.42 0.33

Pensioner 0.15 0.36 0.12

Panel B Years Sample Count

Baby Boomer 1946-1964 2,974

Generation X 1965-1980 6,239

Millennial 1981-2000 4,328

Notes: The three generational categories are based on when individuals were born, Baby Boomers (1946-1964), Generation X’ers (1965-

1980), and Millennials (1981-2000).
Table 2: Financial fees and credit card expenditure shares for non-adopters a

3 months 6 months 12 months 

no login login ∆ no login login ∆ no login login 

Total financial 29.9 24.1 -5.9 29.5 23.5 -6.1 28.7 23.5 

fees (112.4) (56.8) (106.7) (53.6) (90.8) (56.9) Credit card 0.3 0.2 -0.1 0.3 0.2 -0.1 0.3 0.2 interest (3.0) (1.9 ) (3.1) (1.8) (3.0) (1.8 ) NSF fees 0.2 0.2 -0.0 0.2 0.2 -0.0 0.2 0.2 

(2.1 ) (1.9 ) ( 2.1 ) ( 1.9 ) ( 2.2 ) ( 1.8 ) 

Late fees 10.1 7.0 -3.0 10.1 6.9 -3.2 9.6 6.8 

(90.3 ) (38.1) (86.5) (34.4 ) ( 70.6 ) ( 38.3 ) 

Overdraft 19.3 16.6 -2.7 18.9 16.2 -2.7 18.6 16.4 

interest

a (54.9 ) ( 37.6 ) (51.7 ) ( 36.6) ( 48.8 ) (38.0 ) 

Credit card 0.45 0.56 0.11 0.45 0.55 0.10 0.46 0.56 

expenditure share (0.39 ) (0.38) (0.39 ) ( 0.38 ) ( 0.39 ) ( 0.38) 

Notes: All numbers are in US dollars. Standard deviations are displayed below mean averages. Financial fees and credi

and adopters per month for 3, 6, 12, or 18 months after the app introduction. Raw data averages per individual per moa This is the average for all individuals in the group, i.e., not conditional on having overdrafts.

34
35

Table 3: Financial fees and standing for non-adopters and adopters

Non-adopters Adopters

Age 42.7 37.8

(12.5) (11.2)

Female 0.50 0.46

Total income 4,273 4,353

(5,821) (48,539)

Regular income 4,110 3,783

(5,499) (5,154)

Irregular income 163 569

(1,760) (48,196)

Total spending 1,543 1,438

(1,630) (1,683)

Current account balance 2,006 1,738

(9,713) (6,554)

Savings account balance 3,623 4,289

(22,451) (35,587)

Cash 5,629 6,027

(26,001) (36,443)

Liquidity 10,697 11,169

(25,647) (36,690)

Overdraft amount (conditional) -5,167 -4,698

(9,124) (10,856)

Overdraft amount (unconditional) -1,637 -1,356

(5,745) (6,303)

Credit card balance -1,665 -1,580

(1,972) (1,970)

Current account limit 2,765 2,484

(6,665) (11,902)

Credit card limit 4,414 4,715

(4,838) (6,165)

Credit utilization 0.43 0.42

(0.30) (0.31)

Total bank fees 26 21

(75) (79)

Overdraft interest (conditional) 50 46

(70) (61)

Overdraft interest (unconditional) 17 13

(48) (41)

# individuals 7,492 5,391

Notes: The table shows the average financial fees and standing of individual adopters and non-adopters before the app introduction, i.e., our final

sample of individuals for which we observe complete records the 2 years

before and after the app introduction. All numbers are in USD. Overdraft

amounts and interest expenses are reported both with and without conditioning on having overdraft debt. Standard deviations are displayed below

mean averages.
Table 4: Income and consumption statistics

Mean Standard Statistics

Deviation Iceland

Monthly regular income 3,038 3,184 3,227

Monthly salary 2,704 2,993 2,456

Monthly spending:

Total 1,315 1,224

Groceries 468 389 490

Fuel 236 259 (359)

Alcohol 62 121 85

Ready Made Food 170 1723 (252)

Home Improvement 150 465 (229)

Transportations 58 700 66

Clothing and Accessories 87 181 96

Sports and Activities 44 148 (36)

Pharmacies 40 62 42

Notes: The table shows the consumption of income of all active users that we

observe starting at some point before or after the app introduction. All numbers are in US dollars. Parentheses indicate that data categories do not match

perfectly. Raw data averages per individual and per month.

Table 5: Login statistics

Logins Logins App Logins % Pop logins Freq app use

Oct 2014 Nov 2014 Nov 2014 Nov 2014 by Aug 2016

Total 12,120 21,245 11,477 20% 41%

Men 7,131 13,901 7,510 24% 43%

Women 4,989 7,344 3,967 17% 39%

Baby Boomers 2,346 3,061 855 18% 27%

Generation Xers 6,435 11,064 6,621 21% 41%

Millennials 3,020 6,631 3,939 20% 52%

Note: Total logins before and after the app introduction.

36
Figure 7: Share of adopters by gender and age group. Age group 1, if age <= 25; 2 if 25

< age <= 30; 3 if 30 < age <= 35; 4 if 35 < age <= 40; 5 if 40 < age <= 45; 6 if 45

< age <= 50; 7 if 50 < age <= 60; 8 if 60 < age. Each raw data point represents the

fraction of individuals in each age group who logged in via the app at least once over the

sample period.

Figure 8: Uptake of adopters around the app introduction. Each raw data point represents the fraction of individuals in each age group who logged in via the app at least once

up until each month. Each line represents one generation and gender group.

37
38

Table 6: The effect of logins on financial fees

(1) (2) (3)

First Stage ITT IV

Total bank fees:

Total Logins 0.8078*** -181.1*** -224.1***

(0.0270) (37.3) (46.7)

I(Loginsit > 0) 0.0923*** -181.1*** -1,962.2***

(0.0017) (37.3) (405.5)

#Observations 643,728 643,728 643,728

#Individuals 13,411 13,411 13,411

Overdraft interest:

Total Logins 0.8078*** -142.0*** -176.8***

(0.0270) (18.5) (23.7)

I(Loginsit > 0) 0.0932*** -142.0*** -1,547.8***

(0.0017) (18.5) (202.9)

#Observations 643,728 643,728 643,728

#Individuals 13,411 13,411 13,411

Late fees:

Total Logins 0.8078*** -42.9 -53.2

(0.0270) (31.2) (38.7)

I(Loginsit > 0) 0.0932*** -42.9 -465.4

(0.0017) (31.2) (338.5)

#Observations 643,728 643,728 643,728

#Individuals 13,411 13,411 13,411

Notes: Standard errors are clustered at the individual level and are within parentheses. Each entry is separate regression and presents the estimated effect on financial fees as a result of the mobile app introduction using a 24-month symmetric

window. Column (1) shows the estimate for coefficient λ in Equation (2), the jump

in logins at the mobile app introduction. Column (2) shows the estimate for coefficient π in Equation (3), the intention-to-treat effect of the mobile app introduction

on financial fee payments. Column (3) shows the 2SLS IV estimate for coefficient

β in Equation (1), the causal LATE effect of the mobile app introduction. We either use the total number of logins as the variable Li

in Equations (1) and (2) or

an indicator variable for logging in at least once per month after the app introduction I(Loginsit > 0). All specifications include linear controls of time since the

app introduction where we allow the slopes on each side to differ. We also include

month-of-year fixed effects and individual fixed effects in all specifications.

Estimates are reported in ISK, Estimates are reported in ISK, to obtain the USD

estimates, the coefficients can simply be divided by 100. *** Significant at the 1

percent level. ** Significant at the 5 percent level. * Significant at the 10 percent

level.
Table 7: Financial penalties around the app introduction

October December ∆

2014 2014

Total bank fees

Men 34.90 32.42 -7.1%

(84.35) (73.67)

Women 29.00 27.46 -5.3%

(63.58) (68.89)

Overdraft interest

Men 23.39 22.47 -3.9%

(64.14) (57.84)

Women 18.59 18.53 -0.3%

(46.56) (51.49)

Late fees

Men 10.88 9.40 -13.6%

(49.78) (39.25)

Women 9.78 8.44 -13.7%

(36.59) (37.78)

Note: All numbers are in USD.

39
Table 8: The effects of logins on financial fees

Local Linear Method Global Polyn

(1) (2) (3) (4) 

Total logins -244.2*** -233.0*** -284.2** -208.9*** -25

(48.7) (57.4) (128.9) (57.5) (9

I(Loginsit

> 0) -2,368.4*** -2,270.2*** -3,853.1** -2,261.5*** -2,96

(468.1) (554.8) (1,728.3) (618.5) (1,0

Bandwidth 18 12 6 24 Polynomial order: Second T#Observations 482,796 321,864 160,932 643,728 64#Individuals 13,411 13,411 13,411 13,411 13

Notes: Standard errors are clustered at the individual level and are within parentheses. Each e

gression and presents the estimated effect on financial fees as a result of the mobile app introduprovide estimates using local linear regressions. Columns 4-6 present estimates using global polyn3rd, and a 4th order polynomial function of time from the mobile app introduction using a 24-mo

dow. The estimates are for coefficient

β in Equation (1), the causal LATE effect of the mobil

using the total number of logins as the variable

Li in Equation (1). The specifications in colum

linear controls of time since the app introduction where we allow the slopes on each side to differin columns (4) to (6) include polynomial controls of time since the app introduction where we on each side to differ. We also include month-of-year fixed effects and individual fixed effects 

Estimates are reported in ISK, to obtain the USD estimates, the coefficients can simply be divi*** Significant at the 1 percent level. ** Significant at the 5 percent level. * Significant at the 1
Table 9: The impact of logins on the share of expenditures paid by credit cards

(1) (2) (3)

First Stage ITT IV

Total Logins 0.8199*** 0.0087*** 0.0106***

(0.0278) (0.0012) (0.0014)

I(Loginsit > 0) 0.0953*** 0.0087*** 0.0916***

(0.0017) (0.0012) (0.0121)

#Observations 611,953 611,953 611,953

#Individuals 13,411 13,411 13,411

Notes: Standard errors are clustered at the individual level and are within parentheses. Each entry is separate regression and presents the estimated discontinuity

in the share of expenses paid by credit cards as a result of the mobile app introduction using a 24-month symmetric window. Column (1) shows the estimate

for coefficient λ in Equation (2), the jump in logins at the mobile app introduction. Column (2) shows the estimate for coefficient π in Equation (3) with the

variable Yi given by the share of expenditures paid by credit cards, the intentionto-treat effect of the mobile app introduction on financial fee payments. Column

(3) shows the 2SLS IV estimate for coefficient β in Equation (1) with the variable Yi given by the share of expenditures paid by credit cards, the causal LATE

effect of the mobile app introduction. We either use the total number of logins as

the variable Liin Equations (1) and (2) or an indicator variable for logging in at

least once per month after the app introduction I(Loginsit > 0). All specifications include linear controls of time since the app introduction where we allow

the slopes on each side to differ. We also include controls for total expenditure,

month-of-year fixed effects, and individual fixed effects in all specifications.

*** Significant at the 1 percent level. ** Significant at the 5 percent level. *

Significant at the 10 percent level.

41
Table 10: The effects of the number of monthly logins on the share of expenditure p

Local Linear Method Global Polynom

(1) (2) (3) (4) (5) 

Total logins 0.0118*** 0.0124*** 0.0099*** 0.0116*** 0.0169

(0.0015) (0.0017) (0.0031) (0.0020) (0.00

I(Loginsit

> 0) 0.1128*** 0.1194*** 0.1296*** 0.1264*** 0.1928

(0.0141) (0.0154) (0.0396) (0.0211) (0.03

Bandwidth 18 12 6 24 24 Polynomial order: Second Thir#Observations. 465,683 314,102 158,481 611,953 611,9#Individuals 13,410 13,408 13,407 13,411 13,4

Notes: Standard errors are clustered at the individual level and are within parentheses. Each 

rate regression and presents the estimated effect on financial fees as a result of the mobile apColumns 1-3 provide estimates using local linear regressions. Columns 4-6 present estimatpolynomials using a 2nd, 3rd, and a 4th order polynomial function of time from the mobile ap

using a 24-month symmetric window. The estimates are for coefficient

β in Equation (1) 

able

Yi given by the share of expenditures paid by credit cards, the causal LATE effect of t

introduction, using the total number of logins as the variable

Li in Equation (1). The lo

ifications include linear controls of time since the app introduction where we allow the slopto differ. We also allow the curvature of the global polynomials on each side to be differenclude month-of-year fixed effects and individual fixed effects in all specifications. Estimatin ISK, to obtain the USD estimates, the coefficients can simply be divided by 100. *** the 1 percent level. ** Significant at the 5 percent level. * Significant at the 10 percent lev
Figure 9: Trends of the central bank policy rate and overdraft interest rate through the

app introduction. Data source: Central Bank of Iceland https://www.cb.is/

Figure 10: Logins by adopters after the app introduction versus inactive users.

43
Table 11: The impact of logins on financial fees - Difference-in-differences e

(1) (2) (3) (4) 

Total bank fees:γ

-468.2*** -468.2*** -506.9*** -506.0*** -5

(142.6) (142.6) (147.1) (147.2) (

Overdraft interest:γ

55.0 55.0 -45.7 -44.8 

(122.1) (122.1) (129.1) (129.2) (

Late fees:γ

-238.0*** -238.0*** -269.1*** -268.6*** -2

(66.8) (66.8) (73.2) (73.2) 

Polynomial first first orderIncome X X Gender X X Age and X X age squared#Observations 336,042 336,042 287,595 287,595 2#Individuals 5,334 5,334 5,334 5,334 

Notes: Standard errors are clustered at the individual level and are within parentheses. Each entry 

presents the estimated effect of the mobile app introduction using a difference-in-differences approach, i.etion (4) represents the effect of the mobile app introduction on financial fee payments. *** SignificanSignificant at the 5 percent level. * Significant at the 10 percent level.
45

Figure 11: Monthly financial fee payments by bins of monthly logins. Each raw data dot

represents the average amount of fees paid by all individuals given their average monthly

login frequency. The lines are simple two-way fits through the data points.
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USA: 5-year forecast table

Economist Intelligence Unit - ViewsWire, 17 November 2014, 4201 words, (English)

Data summary: Global outlook Global outlook 2010 2011 2012 2013 2014 2015 2016 2017 2018 2019 International

assumptions (%) World GDP growth 4.0 2.6 2.0 2.1 2.3 2.9 2.8 2.9 ...

(Document EIUCP00020141119eabh0000h)

Good Morning Ms. Yellen, Rand Paul on Line One

Dow Jones Top North American Equities Stories, 01:09 PM, 5 November 2014, 2019 words, (English)

The Wall Street Journal's Daily Report on Global Central Banks for Wednesday, November 5, 2014: Sign up for the

newsletter: http://on.wsj.com/grandcentralsignup.

(Document DJTNAE1120141105eab5000ct)

Macro Horizons: GOP's Midterm Win In Focus, But Global Economy

Bigger Concern

Dow Jones Institutional News, 07:36 AM, 5 November 2014, 1550 words, (English)

By Michael J. Casey and Alen Mattich Macro Horizons covers the main macroeconomic and policy news events affecting

foreign-exchange, fixed income and equity markets around the world, as selected by editors in New York, London and Hong

Kong.

(Document DJDN000020141105eab500271)

Political/commercial background: International agreements

Economist Intelligence Unit - Country Commerce, 1 November 2014, 1838 words, (English)

Switzerland is a member of the Council of Europe, the IMF, the OECD, the Organisation for Security and Co-operation in

Europe, the World Bank and the World Trade Organisation (WTO). In May 2009 Switzerland became a member of the ...

(Document EIUCC00020141206eab10000a)

Good Morning Ms. Yellen, Rand Paul on Line One

Dow Jones Top Global Market Stories, 12:29 PM, 5 November 2014, 2019 words, (English)

The Wall Street Journal's Daily Report on Global Central Banks for Wednesday, November 5, 2014: Sign up for the

newsletter: http://on.wsj.com/grandcentralsignup.

(Document DJTGMS1120141105eab5000bs)

AgriNews Kiev (No. of pages: 23)

AgriNews, Kiev, 10 November 2014, 9396 words, (English)

CONTENT 1. GOVERNMENT POLICY AND DEVELOPMENT OF LEGISLATION

.................................................................................. 2 1.1. TOPIC OF THE WEEK ...

(Document AGRIKV0020150706eaba000gt)

Custodian REIT PLC Half Yearly Report

Regulatory News Service, 02:01 AM, 25 November 2014, 21914 words, (English)

TIDMCREI RNS Number : 8695X Custodian REIT PLC 25 November 2014 25 November 2014 Custodian REIT plc

("Custodian REIT" or "the Company") Interim Results

(Document RNS0000020141125eabp0001p)

Latest Developments In EU Export Controls And Economic Sanctions

Mondaq Business Briefing, 19 November 2014, 1545 words, Laurent Ruessmann, (English)

Following is a short update on recent developments in EU export controls and sanctions laws. Our Export Control Team

would be glad to assist you further should you have any questions or seek additional information.

(Document BBPUB00020141119eabj000mm)

3-page Market special: A departure from Economics 101

The Sunday Business Post, 23 November 2014, 1144 words, (English)

Central banks pumping hundreds of billions into retail banks will not get more plumbers or SMEs their overdraft facilities. In

the 1950s, the economist Oskar Morgenstern asked a simple question, and got a very strange answer. Morgenstern was ...

(Document SBPM000020141123eabn0001j)
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Europe Data: New Car Registrations By Country, Y/Y % Chgs

Market News International, 02:00 AM, 18 November 2014, 407 words, (English)

Release for: October 2014 Source: European Automobile Manufacturers Association Y/Y Jan-Oct Jan-Oct Y/Y Oct14 Oct13

%CHG 2014 2013 ...

(Document MARNEW0020141118eabi0004r)

Signs of growth in retail rental re-emerge in regional areas

The Sunday Business Post, 2 November 2014, 1062 words, (English)

The slow recovery in retail sales has at last begun to ripple out to some of the regional towns and cities. The slow recovery

in retail sales has at last begun to ripple out to some of the regional towns and cities, according to Florence ...

(Document SBPM000020141102eab20003o)

PH, Switzerland agree to narrow down trade gap

Manila Bulletin, 12 November 2014, 621 words, (English)

The Philippines and Switzerland governments are working to narrow down the huge trade deficit against the Philippines,

whose exporters are still having difficulties meeting the standards and quality requirements of a wealthy trading ...

(Document MABULL0020141111eabc0009d)

Landsbankinn hf.: Advisory opinion of the EFTA Court on the inflation

indexing provision of a bond

NASDAQ OMX Nordic Exchanges - Company Notices, 06:14 AM, 24 November 2014, 929 words, (English)

Today the EFTA Court handed down its advisory opinion on the interpretation of provisions in Directive 87/102/EEC on

consumer credit, and Directive 93/13/EEC on unfair terms in consumer contracts. The opinion was requested by the

Reykjavík ...

(Document NASDQC0020141124eabo001md)

Capital Control Plan

Irish Independent, 12 November 2014, 82 words, (English)

Briefs ICELAND took another step toward easing capital controls in a move that will free creditors in its failed banks as the

government moves ahead with a mortgage debt relief programme.

(Document IINM000020141112eabc0004p)

Tax-free shopping around the world

Manila Bulletin, 3 November 2014, 870 words, (English)

People around the world will try to avoid tax as much as they can. In fact, global companies tend to relocate their business

operations in countries where taxes are relatively low, or at least business-friendly.

(Document MABULL0020141104eab3000ai)

PH, Efta to start free trade talks

Philippine Daily Inquirer, 26 November 2014, 189 words, (English)

The Philippines and the four member states of the European Free Trade Association (Efta) are set to start negotiations for a

free trade agreement, following the successful conclusion of the so-called “scoping exercises” between the two ...

(Document AIWPHI0020141126eabq0001h)

Germany to require board quota

The Knoxville News Sentinel, 27 November 2014, 338 words, (English)

Germany to require board quota BERLIN — Germany’s leading companies will need to have at least 30 percent women on

their supervisory boards from 2016, according to a new directive being adopted by the government, Chancellor Angela

Merkel ...

(Document KXVL000020141127eabr0000m)

Cecilia S. Petersen, Knoxville

The Knoxville News Sentinel, 27 November 2014, 1015 words, (English)

Cecilia S. Petersen, Knoxville Whatever happened to Thanksgiving? I am dismayed by the increasing commercialism of all

holidays. Apparently, if it doesn’t reap retail dollars, it’s just not a holiday. Examine Veterans Day and Thanksgiving. ...

(Document KXVL000020141127eabr0001l)
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Lithuania's truck sales fall 28 pct in Jan-Oct y/y - ACEA

Baltic Business Daily, 04:12 AM, 27 November 2014, 196 words, (English)

VILNIUS, Nov 27, BNS - All three Baltic countries recorded a decline in new heavy commercial vehicle sales for the ten

months through October, figures from the European Automobile Manufacturers' Association (ACEA) showed on Thursday.

(Document BALDAI0020141127eabr0012y)

Equality, Korean style

Joins.com, 21 November 2014, 773 words, (English)

American-style winner-takes-all business practices have become widespread, deepening inequalities. South Korea

achieved two economic miracles from the 1960s through the 1990s. One is the often-cited passage from rags-to-riches. Per

capita ...

(Document JOONAI0020141120eabl0005p)

Brazil, US on the agenda during EFTA Ministerial

ForeignAffairs.co.nz, 24 November 2014, 424 words, (English)

MIL OSI - Source: Government of Iceland - Press Release/Statement Headline: Brazil, US on the agenda during EFTA

Ministerial 17.11.2014 Gunnar Bragi Sveinsson Minister for Foreign Affairs participated in the biannual Ministerial meeting of

the ...

(Document PARALL0020141125eabo000ec)

UPDATE 2-EU insurance watchdog warns on low interest rate threat

Reuters News, 04:18 PM, 30 November 2014, 515 words, (English)

* EIOPA releases results of insurer stress tests * EIOPA does not name individual insurers in results * Sector generally well

capitalised, EIOPA says (Adds European industry comment, detail)

(Document LBA0000020141130eabu00fz2)

Financial Adviser: The latitude of longevity.

Financial Adviser, 20 November 2014, 1433 words, Joseph Lu, (English)

The Longevity Science Panel forecasts that life expectancy will continue to rise in the next decade, and so ways have to be

found to meet the challenges - and opportunities - of an ageing population

(Document FADV000020141127eabk00019)

China and South Korea close to reaching free trade agreement

EFE News Service, 10 November 2014, 235 words, (English)

Beijing, Nov 10 (EFE).- Chinese President Xi Jinping on Monday met with his South Korean counterpart Park Geun-hye and

both announced a tentative free trade agreement, the state Xinhua news agency reported.

(Document WEFE000020141110eaba0005m)

Principle of home rule must be backed up by full tax powers

The Herald, 5 November 2014, 1132 words, NO BYLINE, (English)

THE new cross-party Campaign for Scottish Home Rule (“Home rule supporters vow to win meaningful settlement”, The

Herald, November 4) is right to look for a principled approach to further Scottish devolution. These principles could rest on

...

(Document GH00000020141105eab50003z)

All roads lead to retail parks

The Sunday Business Post, 30 November 2014, 820 words, (English)

Increased car sales, better roads and access to parking are driving the increase in rental rates for retail parks, writes Donal

Buckley. Ireland’s vastly improved motorway network could well be a key factor driving the latest buying trends ...

(Document SBPM000020141130eabu0003p)

New depository scheme from December 15

Business Standard, 15 November 2014, 131 words, BS Reporter New Delhi, (English)

Indian corporates, both listed and unlisted, would be able to raise money through depository receipts in 34 foreign

jurisdictions from December 15. Notifying the scheme, the finance ministry said any domestic company, both listed and ...

(Document BSTN000020141114eabf004fe)
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Britain doesn't need to be in Europe to strike important trade deals

The Telegraph Online, 10:10 AM, 5 November 2014, 464 words, By Douglas Carswell, (English)

What should we make of the proposed Transatlantic Trade and Investment Partnership, asks Douglas Carswell What

should one make of the proposed Transatlantic Trade and Investment Partnership or TTIP?

(Document TELUK00020141105eab5003k4)

European car sales up again in October.

ANSA - English Media Service, 04:24 AM, 18 November 2014, 93 words, (English)

(ANSA) - Turin, November 18 - European car sales increased for the 14th consecutive month in October, European

Automobile Manufacturers Association (ACEA) said on Tuesday. It said there were 1,112,628 new car registrations in the

EU and the ...

(Document ANSAEN0020141118eabi000b7)

Norway economy: Coming to terms with falling oil prices

Economist Intelligence Unit - ViewsWire, 7 November 2014, 1117 words, (English)

Norway is a wealthy economy and has come through previous negative oil shocks in decent shape, partly because the

positive spin-offs from a falling krone deliver some necessary rebalancing of the economy. Yet if the sudden drop in global ...

(Document EIUCP00020141108eab700033)

Why relying on GDP will destroy the world

The Telegraph Online, 11:01 AM, 17 November 2014, 754 words, Lauren Davidson, By Lauren Davidson, (English)

GDP is not the only way to measure global growth, and leaning on it too heavily has left the world "teetering on the brink of

environmental disaster and filled with anger and conflict."

(Document TELUK00020141117eabh003v0)

A 'Tax Day' Americans could love?

CNN Wire, 12:11 PM, 26 November 2014, 1119 words, By Edward J. McCaffery, (English)

Editor's note: Edward J. McCaffery is Robert C. Packard Trustee Chair in law and a professor of law, economics and

political science at the University of Southern California. He is the author of "Fair Not Flat: How to Make the Tax System ...

(Document CNNWR00020141126eabq007bx)

Food inflation hits eight-year low as shoppers benefit from price cuts of

essentials in supermarket wars

Mail Online, 06:48 AM, 5 November 2014, 575 words, CLAIRE HUGHES FOR THISISMONEY.CO.UK, (English)

Shoppers are benefiting from the lowest recorded food inflation figures since 2006 with falls in the price of kitchen essentials

such as milk, cheese and eggs, new data indicates.

(Document DAMONL0020141105eab50053h)

Corporate taxes: Double-tax treaties

Economist Intelligence Unit - Country Commerce, 1 November 2014, 948 words, (English)

India has comprehensive double-taxation agreements in force with 88 countries, covering all sources of income (however, a

few of them specify simply that standard national rates of withholding will be charged). There are 13 agreements ...

(Document EIUCC00020141206eab10003f)

India's gender gap is getting worse

Sunday Tribune, 2 November 2014, 365 words, (English)

NEW DELHI: Indian women still face some of the world's worst inequality in access to health care, education and work, despite years of rapid economic growth, a survey of 142 nations revealed.

(Document SUNDTB0020141102eab20004c)

All 3 Baltic countries post y/y growth in new car sales in Jan-Oct – ACEA

Baltic Business Daily, 04:17 AM, 18 November 2014, 209 words, (English)

VILNIUS, Nov 18, BNS - All three Baltic countries posted growth in new car sales in January through October, data from the

European Automobile Manufacturers' Association (ACEA) showed on Tuesday.

(Document BALDAI0020141118eabi000rt)

DIANNE Sharp, regional director of [...]
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The Journal, Newcastle, 20 November 2014, 754 words, PETER TROY, (English)

DIANNE Sharp, regional director of the CBI makes a good point in her column (The Journal Business, November 11) when

she asserts that concern around free movement and migration is at the centre of continued membership of the EU.

However, ...

(Document THEJOU0020141120eabk0001f)

Government sets its sights on new trade deal, Media release, 14 Nov

2014, Australian Minister for Trade and Investment, The Hon Andrew

Robb...

ForeignAffairs.co.nz, 17 November 2014, 406 words, (English)

MIL OSI - Source: Australian Government - Foreign Affairs and Trade - Press Release/Statement: Headline: Government

sets its sights on new trade deal, Media release, 14 Nov 2014, Australian Minister for Trade and Investment, The Hon

Andrew ...

(Document PARALL0020141117eabh0003o)

World: 5-year forecast table

Economist Intelligence Unit - ViewsWire, 21 November 2014, 884 words, (English)

Global assumptions Global forecast 2010 2011 2012 2013 2014 2015 2016 2017 2018 2019 Real GDP growth (%)

...

(Document EIUCP00020141123eabl0001l)

Icelandic central bank cuts key interest rate to 5.75 percent

Reuters News, 04:07 AM, 5 November 2014, 114 words, (English)

COPENHAGEN, Nov 5 (Reuters) - Iceland's central bank lowered its key interest rate to 5.75 percent from 6.00 percent on

Wednesday and said inflation was likely to fall further in the next few months and remain at or below target through ...

(Document LBA0000020141105eab500akr)

OECD raises growth forecast for Russian GDP in 2014 to 0.7%, lowers

to zero for 2015

Interfax: Russia & CIS Business and Financial Newswire, 10:16 AM, 6 November 2014, 254 words, (English)

MOSCOW. Nov 6 (Interfax) - The Organization for Economic Cooperation and Development (OECD) is expecting Russia's

GDP to grow 0.7% in 2014, followed by zero growth in 2015 and 2% growth in 2016, the organization said in a statement.

(Document DAIBN00020141106eab60015r)

Phl, European free trade group set talks

The Philippine Star, 24 November 2014, 410 words, By Louella D. Desiderio, (English)

MANILA, Philippines – The Philippines and European Free Trade Association (EFTA) are set to hold this month the first

round of meetings for a planned free trade agreement (FTA) in line with the aim to start negotiations by next year.

(Document PHSTAR0020141123eabo0000l)

World: 5-year forecast table

Economist Intelligence Unit - ViewsWire, 1 November 2014, 874 words, (English)

Global assumptions Global forecast 2010 2011 2012 2013 2014 2015 2016 2017 2018 2019 Real GDP growth (%)

...

(Document EIUCP00020141102eab100044)

Philippines: High-level Swiss business delegation visit Manila, Cebu

Thai News Service, 25 November 2014, 600 words, (English)

Section: General News - The visit of Swiss business delegation in Manila and Cebu this month further boosted economic

relations between the Philippines and Switzerland.

(Document THAINS0020141124eabp0005z)

Investors Chronicle - magazine and web content: RPC packs a punch.

Investors Chronicle - Magazine and Web Content, 27 November 2014, 313 words, Daniel Liberto, (English)

Success outside Europe and a new acquisition sent shares in the plastic packager up 5 per cent on results day. Rigid plastic

package supplier RPC (RPC) overcame flat economic growth in its core European market and high polymer prices to post
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...

(Document INVR000020141210eabr0003n)

Irish vote against sovereign debt mechanism puzzling

The Irish Times, 14 November 2014, 725 words, arthur beesley, Arthur Beesley, (English)

A few weeks ago, the United Nations General Assembly adopted a resolution to establish a new international mechanism to

restructure the sovereign debt of bankrupt countries, the noble objective being to prevent any repeat of Argentina's ...

(Document IRTI000020141114eabe0003l)

EMU Data: Flash GDP By Member State; Q/Q, Y/Y Pct Change

Market News International, 05:00 AM, 14 November 2014, 664 words, (English)

Release for: Third Quarter 2014(flash) Source: Eurostat Q/Q Pct Change Y/Y Pct Change 4Q13 1Q14 2Q14 3Q14 4Q13

1Q14 2Q14 ...

(Document MARNEW0020141114eabe00085)

EU/EMU Data: Harmonised CPI By Nation

Market News International, 05:12 AM, 14 November 2014, 470 words, (English)

Release for: Otcotber 2014(final) Source: Eurostat Oct14 Sep14 Aug14 Jul14 Oct13 Oct14 y/y y/y y/y y/y y/y ...

(Document MARNEW0020141114eabe0008a)

Europe patent for colorectal cancer prognostic technology

Scoop.co.nz, 07:35 PM, 25 November 2014, 812 words, Pacific Edge, (English)

26 November 2014 Europe grants Pacific Edge patent for colorectal cancer prognostic technology The European

Intellectual Property Office which operates across 38 countries including all European Union members, has awarded Pacific

Edge a ...

(Document SCCONZ0020141126eabq00065)

What Does IMF's Appointment of Crisis Veteran Say About Europe's

Economy?

Dow Jones Institutional News, 12:56 PM, 3 November 2014, 263 words, Ian Talley, By Ian Talley, (English)

If the International Monetary Fund's latest economic appointment is any indication, Europe's economy must still be in real

trouble. IMF chief Christine Lagarde named Poul Thomsen, architect of the controversial Greek bailout and one the ...

(Document DJDN000020141103eab3002yx)

FTA’s smoother Chinese capital should give nation a welcome shot in the

arm

The Australian, 12 November 2014, 1046 words, Glenda Korporaal, Glenda Korporaal, (English)

IT is too early to tell just how much of a stimulus the free trade agreement Australia is expected to sign with China will be to

our economy. But the deal, which could be signed on Monday at the G20 leaders meeting in Brisbane, has the ...

(Document AUSTLN0020141111eabc0004c)

World Furniture Outlook 2014-2015

PR Newswire (U.S.), 04:00 PM, 27 November 2014, 451 words, (English)

LONDON, Nov. 27, 2014 /PRNewswire/ -- The World Furniture Outlook 2014-2015 by CSIL provides an overview of the

world furniture industry with historical statistical data (production, consumption, imports, exports) and 2014 and 2015 ...

(Document PRN0000020141127eabr00048)

TABLE-OECD overview of deficit and inflation forecasts

Reuters News, 05:30 AM, 25 November 2014, 331 words, (English)

PARIS, Nov 25 (Reuters) - Following are the main public deficit and consumer-price inflation projections from the

Organisation for Economic Cooperation and Development's latest Economic Outlook, released on Tuesday. ...

(Document LBA0000020141125eabp00blg)

Interfax Russia & CIS Business and Financial Daily

Interfax: Russia & CIS Business and Financial Daily, 03:51 PM, 6 November 2014, 13258 words, (English)

07.11.14 06.11.14 Official Exchange Rate of Ruble to Dollar (ruble/$1) 45.1854 44.3993 Official Exchange Rate of Ruble to

Euro (ruble/EUR1) 56.5450 55.6234 ...
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(Document DAFIR00020141107eab600001)

“Who Says We Do Not Work?” (No. of pages: 8)

Economic & Political Weekly, 15 November 2014, 9035 words, Sujata Gothoskar, Apoorva Kaiwar, (English)

SPECIAL ARTICLE november 15, 2014 vol xlix no 46 EPW Economic & Political Weekly 54 “Who Says We Do Not Work?”

Looking at Sex Work Sujata Gothoskar, Apoorva Kaiwar Sex workers’ organisations have argued against trafficking and see

it ...

(Document ECPOLW0020141202eabf0002t)

Economics

Turan Information Agency (Azerbaijan), 08:04 AM, 28 November 2014, 2927 words, (English)

Milli Majlis Approves Draft Budget 2015Decline Expected in the Oil and Gas SectorAzerbaijan Exports Iron Ore at a Price

2.5 Times Lower than the World PriceAccord Corporation Launches Kutaisi Bypass RoadPlacing a Large Batch of Bonds of

the ...

(Document TURNAG0020141128eabs0005q)

Interfax Russia & CIS Business and Investment Weekly

Interfax: Russia & CIS Business & Investment Weekly, 04:44 PM, 7 November 2014, 26782 words, (English)

07.11.2014 31.10.2014 Official Exchange Rate of Ruble to Dollar (ruble/$1) 45.1854 43.3943 Official Exchange Rate of

Ruble to Euro (ruble/EUR1) 56.5450 54.6378 ...

(Document INVST00020141121eab700001)

Investing in real estate abroad and at home

Today.az, 28 November 2014, 1832 words, (English)

/AzerNews/By Gulgiz Dadashova Buying a house is without a doubt one of the most important decisions that you will make

in your life. Besides turning a house into a home, real estate is also an alluring investment.

(Document DLSDAZ0020141128eabs0000d)

Why China's Easing Measures Are Failing -- Market Talk

Dow Jones Institutional News, 02:27 AM, 6 November 2014, 1532 words, (English)

0727 GMT [Dow Jones] Beijing's targeted easing measures are not bolstering economic growth this year and sentiment

remains weak, Standard Chartered economists Li Wei says. "It started as a deleveraging process and a property market ...

(Document DJDN000020141106eab600154)

EU passenger car registrations rise 6.5% y/y during October – ACEA

IHS Global Insight Daily Analysis, 18 November 2014, 2555 words, Ian Fletcher, (English)

Passenger car registrations in the European Union (EU) have grown again in October, but the improvement is very much

relative to how poor the performance in this market has been.

(Document WDAN000020141118eabi00008)

Analyzing Whether Countries Are Equally Efficient at Improving

Longevity for Men and Women

American Journal of Public Health, 1 November 2014, 4089 words, Douglas Barthold; Arijit Nandi; José M Mendoza Rodríguez; Jody Heymann,

(English)

Objectives. We examined the efficiency of country-specific health care spending in improving life expectancies for men and

women. Methods. We estimated efficiencies of health care spending for 27 Organisation for Economic Co-operation and ...

(Document GAPH000020141106eab10000s)

BBC Monitoring quotes from China, Taiwan press 18 Nov 14

BBC Monitoring Asia Pacific, 01:28 AM, 18 November 2014, 1677 words, (English)

The following is a selection of quotes from editorials and commentaries carried in 18 November 2014 website editions of

mainland Chinese, Hong Kong and Taiwan newspapers and news portals available to BBC Monitoring. Unless otherwise

stated, ...

(Document BBCAPP0020141118eabi0012x)

(Insight-EU-Dossier) TiSA: EU pushes to lock in liberalisation of services

worldwide By Craig James Willy, dpa
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dpa Insight EU, 12:57 PM, 20 November 2014, 4321 words, (English)

The European Commission is pushing for a deal to free up as many services as possible to international competition, with

potential big gains for companies and consumers. But critics fear liberalisation could mean deregulation, privatisation ...

(Document DPAINSE020141120eabk00001)

Cyprus’s Shipping Tax Regime

Mondaq Business Briefing, 18 November 2014, 1993 words, Philippos Aristotelous, (English)

Cyprus is among the world's top shipping centres, with a government policy which actively attracts investment to the island.

This article looks at the features and exemptions which make it so attractive to shipping businesses.

(Document BBPUB00020141118eabi000ht)

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