metadata: authors: 0: author: Docquier,Frederic
1: author: Lodigiani, Elisabetta
2: author: Rapoport,Hillel
3: author: Schiff,Maurice
count: World
docna: 0: docna: Emigration and democracy
docty: Policy Research Working Paper
subtopic: Judicial System Reform,Human Migrations & Resettlements,Educational Sciences,International Trade and Trade Rules,Migration and Development
teratopic: Macroeconomics and Economic Growth,Health, Nutrition and Population,International Economics and Trade,Social Development,Communities and Human Settlements
abstracts: cdata!: Migration is an important yet neglected
            determinant of institutions. This paper documents the
            channels through which emigration affects home country
            institutions and considers dynamic-panel regressions for a
            large sample of developing countries. The authors find that
            emigration and human capital both increase democracy and
            economic freedom. This implies that unskilled (skilled)
            emigration has a positive (ambiguous) impact on
            institutional quality. Simulations show an impact of skilled
            emigration that is generally positive, significant for a few
            countries and for many countries once incentive effects of
            emigration on human capital formation are accounted for.
repnme: repnme: Emigration and democracy
display_title: Emigration and democracy
listing_relative_url: /research/2011/02/13716766/emigration-democracy
topicv3: Justice m1326106 840,Trade m1326924 698,Education m1327048 470,Emigration m1504169 2844,Human Capital Flight m1504170 2845
publishtoextweb_dt: 2010-07-01T00:00:00Z
historic_topic: Macroeconomics and Economic Growth,Health, Nutrition and Population,International Economics and Trade,Social Development,Communities and Human Settlements
no_of_pages: 49
author_keys: 0: author_key: 741294
1: author_key: 857958
2: author_key: 92053
model_extractions: WPS5557 Policy Research Working Paper 5557

# Emigration and Democracy

_Frédéric Docquier Elisabetta Lodigiani Hillel Rapoport Maurice Schiff_ The World Bank Latin America and Caribbean Region Office of the Chief Economist February 2011
Policy Research Working Paper 5557

# **Abstract**

Migration is an important yet neglected determinant of institutions. This paper documents the channels through which emigration affects home country institutions and considers dynamic-panel regressions for a large sample of developing countries. The authors find that emigration and human capital both increase democracy and economic freedom. This implies that unskilled (skilled) emigration has a positive (ambiguous) impact on institutional quality. Simulations show an impact of skilled emigration that is generally positive, significant for a few countries and for many countries once incentive effects of emigration on human capital formation are accounted for This paper is a product of the Chief Economist, in the Latin America and Caribbean Region. It is part of a larger effort by the World Bank to provide open access to its research and make a contribution to development policy discussions around the world. Policy Research Working Papers are also posted on the Web at http://econ.worldbank.org. The author may be contacted at mschiff@worldbank.org.

_The Policy Research Working Paper Series disseminates the findings of work in progress to encourage the exchange of ideas about development issues. An objective of the series is to get the findings out quickly, even if the presentations are less than fully polished. The papers carry the names of the authors and should be cited accordingly. The findings, interpretations, and conclusions expressed in this paper are entirely those of the authors. They do not necessarily represent the views of the International Bank for Reconstruction and Development/World Bank and its affiliated organizations, or those of the Executive Directors of the World Bank or the governments they represent._ Produced by the Research Support Team
# Emigration and democracy<sup>�</sup>

Frédéric Docquier<sup>a</sup> , Elisabetta Lodigiani<sup>b</sup> , Hillel Rapoport<sup>c</sup> and Maurice Schi¤<sup>d</sup>

- a FNRS and IRES, Université Catholique de Louvain

- b CREA, Université du Luxembourg; and Centro Studi Luca d’Agliano

- c CID, Harvard University; Bar-Ilan University; and EQUIPPE

- d World Bank; University of Chile; and IZA-Bonn

January 2011 Abstract Migration is an important and yet neglected determinant of institutions. The paper documents the channels through which emigration a¤ects home country institutions and considers dynamic-panel regressions for a large sample of developing countries. We ...nd that emigration and human capital both increase democracy and economic freedom. This implies that unskilled (skilled) emigration has a positive (ambiguous) impact on institutional quality. Simulations show an impact of skilled emigration that is generally positive, signi...cant for a few countries in the short run and for many countries in the long run once incentive e¤ects of emigration on human capital formation are accounted for.

JEL codes: O1, F22.

Keywords: Migration, institutions, democracy, diaspora e¤ects, brain drain.

> �Corresponding author: Hillel Rapoport, Center for International Development, Kennedy School of Government, Harvard University, 79 JFK Street, Cambridge, MA 02138. Email: hillel_rapoport@hks.harvard.edu. This paper is part of the World Bank Research Program on International Migration and Development. We thank Michel Beine, Eckhardt Bode, David McKenzie, Anna Maria Mayda, Caglar Ozden, Robert Vermeulen, Je¤rey Williamson, and participants at seminars and conferences at the World Bank, Louvain, Luxembourg, Paris I, Maastricht, Boston University, Kiel, Georgetown, Harvard, and the Final Conference of the TOM Marie-Curie Network, Venice, September 2010, for comments and suggestions. We are grateful to Pierre Yared and Cecily Defoort for sharing their data with us.

1
# 1 Introduction

Recent research has emphasized the importance of institutions for economic growth and development (Acemoglu, Johnson and Robinson, 2005, Rodrik, 2007) and explored the determinants of institutions.<sup>1</sup> This paper argues that migration is an important determinant of institutions, not considered so far in the economic growth literature.<sup>2</sup> Migration ...rst a¤ects institutions by providing people with exit options, thereby changing their incentives to voice (as well as their voicing technology); the existence of an exit option and –for those who stay –the possibility of receiving remittance income tend to act as a safety net that can alleviate social, political and economic pressures to reform. For example, it is commonly argued that emigration to the U.S. has contributed to delay political change in countries such as Mexico or Haiti.<sup>3</sup> On the other hand, once abroad, migrants can engage in political activities (e.g., lobby the host-country government to encourage or block ...nancial aid, or impose economic sanctions) that a¤ect the institutional evolution of their home country, for good or bad. A well-known illustration of this strategy is the very active antiCastro lobby in the United States which, under the leadership of the Cuban American Nation Foundation, has long succeeded in maintaining a total embargo on economic relations with Cuba. While it is unclear whether this has strengthened the radical or the moderate factions in Cuba, it seems the recent immigrants, who left Cuba more for economic than for political reasons, and the second generation of CubanAmericans, are more supportive of a dialogue with the communist regime in Cuba and a softening of economic sanctions; and indeed, the Obama administration was able in 2009 to relax restrictions on travel and remittances to Cuba. A lesser known but maybe more e¤ective illustration (in terms of in‡uence on home country politics) is the Croatian diaspora in the United States and Western Europe, which strongly supported secession from the former Yugoslavia and the transition to a market-led economy, provided huge ...nancial support to Tudjman’s Croatian Democratic Union (CDU) party and, following the latter’s victory in the ...rst post-communist elections

> 1For example, Rodrik et al. (2004) show that once institutions are controlled for, geography measures have a weak direct e¤ect on income though they have a strong indirect e¤ect through their impact on the quality of institutions.

> 2 We use the terms "democracy" and "institutions" indi¤erently as three out of four of our institutional quality indicators are standard democracy indices.

> 3See for example Hansen (1988) on Mexico and Fergusson (2003) on Haiti.

2
in 1990, saw its e¤orts rewarded by the allocation of 12 out of 120 seats at the national assembly to diaspora Croats. Since then, the Croatian diaspora has remained very active, raising funds, organizing demonstrations, petitions, media campaigns and other lobbying activities that proved e¤ective in obtaining o¢ cial recognition of independence or in shaping European and American attitudes during the Yugoslavia war.<sup>4</sup> Diasporas may also at times side with a speci...c group in a con‡ict that opposes various groups in their country of origin. For instance, Irish Catholics in the US have historically provided ...nancial and other forms of support to the Catholic community in Northern Ireland. However, the continued support provided during the con‡ict opposing Protestants and Catholics in that country made it more di¢ cult for these communities to reach a peace agreement.<sup>5</sup> A second channel through which migration a¤ects institutions has to do with the fact that migration is a selective process. Migrants are not randomly selected out of the country’s population but tend to self-select along a variety of dimension. First and foremost, migrants are typically positively self-selected on education (migrants’ positive self-selection on education is a rule that admits very few exceptions). Given that more educated individuals – and the middle class in general (Easterly, 2001) –tend to have a higher degree of political participation and generally contribute a greater deal to public policy debates, emigration is likely to hurt the quality of domestic institutions as well as the process through which sound policies are formulated and implemented. On the other hand, migration raises the expected return to human capital, thus inducing people to invest more (or more people to invest) in education (Mountford, 1997, Beine et al., 2001, Katz and Rapoport, 2005) and to reallocate talent toward productive and internationally transferable skills (Mariani, 2007);<sup>6</sup> such e¤ects on the skill distribution can mitigate or even reverse any adverse brain drain impact on political institutions. Another characteristic on which migrants are not randomly self-selected is ethnicity, with an over-representation of ethnic minorities among emigrants. This tends to recompose the home-country population towards 4See Eckstein (2009), Haney and Vanderbush (1999, 2005), and Vanderbush (2009) on Cuba, and Djuric (2003) or Ragazzi (2009) on Croatia.

> 5Similar analyses have been proposed notably in the cases of Lebanon and Sri Lanka. Studies providing detailed accounts and analysis of the role of the Irish diaspora include Holland (1999) and Wilson (1995).

> 6Other political economy analyses of the interaction between emigration and institutions in developing countries include Esptein et al. (1999), Docquier and Rapoport (2003) and Wilson (2011).

3
more homogeneity, again, for good or bad.<sup>7</sup> Finally, emigration increases the home country population’s exposure to democratic values and norms, be it directly, through contacts with return migrants and relatives abroad, or indirectly, through the broader scope of migration and diaspora networks. Such networks have been shown to foster trade (Gould, 1994, Rauch and Trindade, 2002, Rauch and Casella, 2003, Iranzo and Peri, 2009) and FDI in‡ows (Kugler and Rapoport, 2007, Javorcik et al., 2011) and to contribute to the di¤usion of technology (Kerr, 2008, Agrawal et al., 2011) as well as to the transfer of norms of low fertility (Fargues, 2007, Beine, Docquier and Schi¤, 2008) and, in the case of foreign students, to the di¤usion of democracy (Spilimbergo, 2009). In particular, Spilimbergo (2009) shows that foreign-trained individuals promote democracy at home, but only if foreign education is acquired in democratic countries. While he does not identify the exact mechanisms through which such an in‡uence may materialize, he suggests a number of possibilities (e.g., access to foreign media, acquisition of norms and values while abroad that di¤use at home upon return, etc.) that can be generalized to other migration experiences.

Two recent micro studies come in support of this claim. The ...rst context we report on is Cape Verde, a nine-island tropical country o¤ the coast of West Africa with a population of half a million, good institutional scores by African standards, and a long tradition of migration (current migrants represent one-...fth of the population, and skilled emigration rates are extremely high).<sup>8</sup> In this context, Batista and Vicente (2011) set up a "voting experiment" along the following lines: following a survey on perceived corruption in public services, respondents were asked to mail a pre-stamped postcard if they wanted the results of the survey to be made publicly available in the national media. Controlling for individual, household and locality characteristics, they regressed participation in the voting experiment, which they interpret as demand for accountability, on migration prevalence at the locality level. They show that current

> 7In the penultimate paragraph of their article on "arti...cial states", Alesina, Easterly and Matuszeski (2008) write: "probably the single most important issue that we have not addressed is that of migrations. One consequence of arti...cial borders is that people may want to move, if they can. ... In some cases, migrations that respond to arti...cial borders may be partly responsible for economic costs, wars, dislocation of people, refugee crises and a host of undesirable circumstances. ... But sometimes the movement of people may correct for the arti...cial nature of borders."

> 8Brain drain ...gures for Cape Verde are 67 percent in Docquier and Marfouk (2006) and remain very high (60 percent) even after excluding people who emigrated before age 18 and acquired their tertiary education abroad (Beine et al., 2007).

4
<!-- Start of picture text --> Figure 1:<br>EMIGRATION TO THE EAST AND WEST AND CHANGE IN COMMUNIST PARTY<br>VOTE SHARES BETWEEN 2005 AND 2009, BY DISTRICT<br>(based on census data and official election results)<br>0 .02 .04 .06 .08<br>prevalence of migration to russia 2004<br>0 .02 .04 .06 .08<br>prevalence of migration to western europe 2004<br>.3<br>.2<br>.1<br>0<br>change in communist votes' shares 2005-2009 -.1<br>.3<br>.2<br>.1<br>0<br>change in communist votes' shares 2005-2009 -.1<br><!-- End of picture text --> as well as return migrants signi...cantly increase participation rates, and more so for the latter. Interestingly, in the spirit of Spilimbergo’s ...ndings, they ...nd that only migrants to the US seem to make an impact, while migrants to Portugal, the other main destination, do not. In contrast, they do not ...nd evidence of additional e¤ects for skilled migrants. The other context is that of Moldova, a former Soviet Republic with virtually no emigration before 1990 and which has seen a recent surge in migration out‡ows, estimated at half-a-million for a population of 3.6 million in 2008. The evidence we present for Moldova, which is purely descriptive, comes from the analysis of election outcomes in 2005 and 2009 (Omar Mahmoud et al., 2010). It shows that higher votes for the communist party are associated at the district level with migration to Russia while a negative correlation obtains for migration to the EU. Moreover, changes in the share of votes gained by the communist party between 2005 and 2009 follow the same pattern (see Figure 1) and there is evidence of spillover e¤ects to non-migrant households as the same voting patterns are observed even after excluding households with a (current or past) migrant member.

At a macro level, the only paper attempting to assess the overall e¤ect of emigration on institutions we are aware of is Li and McHale (2009), who use the World Bank 5
governance indicators (Kau¤man, Kraay and Mastruzzi, 2005) (henceforth KKM) and the Docquier and Marfouk (2006) migration data set in their cross-sectional analysis. Focusing on skilled migration, they examine the impact of the brain drain on sending country’s institutional development and ...nd a positive e¤ect on “political” institutions (i.e., on “political stability”and “voice and accountability”) but a negative e¤ect on “economic”institutions at home (i.e., on “government e¤ectiveness”, “regulatory quality”, “rule of law”, and “control of corruption”). However, their results su¤er from the limits of a cross-sectional analysis<sup>9</sup> and, as they themselves acknowledge, from the weakness of their instrumentation strategy (they instrument skilled emigration rates using countries’ geographical characteristics). In this paper we look instead at migration in general, focus on democratic institutions, and consider dynamic-panel regressions. We ...nd that the emigration rate and the level of human capital both positively a¤ect democracy and economic freedom at home. This implies that unskilled migration has a positive impact while skilled migration has an ambiguous impact on institutional quality. Using the point estimates from our regressions, we simulate the marginal e¤ect of skilled emigration on institutional quality. In general the simulations con...rm the ambiguous e¤ect of high-skill emigration. It is only when the incentive e¤ects of emigration on human capital formation are taken into account that a signi...cant institutional gain obtains for some countries in the short run, and for many countries in the long-run.

# 2 Empirical analysis

## 2.1 General Considerations

Empirical investigation of the e¤ect of emigration on institutions in a cross-section or a panel setting raises a di¢ cult trade-o¤. In a cross-sectional dimension, it is possible to use better data both for migration and institutional quality. In particular, for migration, it is possible to use the Docquier and Marfouk (2006) data set, which considers international migration by educational attainment. This data set describes the emigration of skilled workers to the OECD for 195 source countries in 1990 and 2000. For institutional quality, the World Bank Governance data by Kaufmann, Kray and

> 9The KKM (2005) data set starts in the late 1990s and is therefore not long enough to allow for panel data analysis. Similarly, the Docquier and Marfouk (2006) dataset o¤ers estimates of emigration rates by skill levels for 1990 and 2000 only.

6
Mastruzzi (2005) measures six dimensions of governance from 1996 to 2005: voice and accountability, political stability and absence of violence, government e¤ectiveness, regulatory quality, rule of law, and control of corruption. It covers 213 countries and territories for 1996, 1998, 2000, and annually for 2002-2005.

In unreported regressions, we consider OLS regressions using these data sets. We ...nd a signi...cant and positive correlation between the emigration rate and institutional quality indexes, but these regressions su¤er from a lot of shortcomings. First, it is di¢ cult to ...nd an appropriate baseline speci...cation, because di¤erent economic, political and cultural factors can be important in explaining the quality of institutions. As Alesina et al. (2003) noted, various explanatory variables have been used in the literature on the determinants of institutions, such as log of gdp per capita, legal origin dummies, religious variables, latitude, fractionalisation indices, etc. The main problem with these variables relates to the fact that the pattern of cross-correlations between explanatory variables cannot be ignored and that in many cases the results of cross-country regressions are sensitive to the econometric speci...cation. For example, they point out that their index of ethnic fractionalization is highly correlated with latitude and with the log of gdp per capita (which, in addition, is very likely endogenous). Moreover, legal origin dummies are highly correlated with religious variables etc. In a panel dimension instead, it is possible to control for unobservable heterogeneity and for all time-invariant variables a¤ecting institutional quality.

Another problem of cross-sectional analysis refers to endogeneity and reverse causality problems (i.e., bad institutions can cause migration). Attempting to confront the endogeneity issue directly requires ...nding a suitable instrument. This is not easy in our context. To properly instrument for migration we need a variable that is correlated with the emigration rate but not directly correlated with our endogenous variable, institutional quality. In the migration literature, country’s geographical features are often used to instrument for emigration. However, in the institutions and growth literature, the very same geographical characteristics, such as latitude or country size, are also used as determinants of institutions, which would seem to question their theoretical validity as candidate instruments. Finally, an additional problem in cross-section analyses has to do with the fact that institutional quality is a quite persistent variable, therefore a dynamic model would seem to be more suited to study the relationship between emigration and institutions. Moreover, several papers discuss the in‡uence of education on institutional quality, therefore it is worth to include 7
in our speci...cations a variable related to education or to human capital (of course, this would su¤er from endogeneity). In the next section, therefore, we will study the impact of emigration on home-country institutions using dynamic-panel regressions. In particular, we will use the system-GMM estimator, and we will be able to control for unobservable heterogeneity and account for endogeneity and persistency of some of the variables, using internal instruments. As far as we know, this is the best suited technique available when it is di¢ cult to ...nd good external instruments, as in our case.

# 2.2 Panel analysis

We follow the literature on democracy and education (Acemoglu et al., 2005, Bobba and Coviello, 2007, Castello-Climent, 2008) and Spilimbergo’s (2009) study on democracy and foreign education and consider the impact of emigration on institutional quality using dynamic-panel regressions.

## 2.2.1 The econometric model

As in previous studies on democracy and education, we consider the level of democracy as our dependent variable and we estimate the following dynamic model: where i is the country, t is the period. All explanatory variables are lagged ...ve years. The lagged dependent enters the set of explanatory variables to account for persistence in democracy scores. Our coe¢ cient of interest is �2; which re‡ects whether emigration (measured by the total emigration) a¤ects democracy at home. The coef...cient �1 captures the e¤ect of human capital on democracy. �3 is a vector of coe¢ - cients re‡ecting the importance of other control variables such as population size and gdp per capita (both in logs), as in Acemoglu et al. (2005). We also control for time ...xed e¤ects, �t, and country ...xed e¤ects, �i. The advantage of a panel estimation is that it is possible to control for unobservable variables that are country-speci...c and whose omission in cross-sectional analyses can bias the estimated coe¢ cients. Therefore, the results are robust to all country-speci...c time invariant explanatory 8
variables used in the cross-section literature on institutional quality, including ethnic fractionalisation, religions, legal origins, colonial ties, geographical variables etc.

A general approach to estimate such an equation is to use a transformation that removes unobserved e¤ects and uses instrumental variables. The well-known ArellanoBond (1991) method considers the ...rst-di¤erence of the explanatory variables which are instrumented by their lagged values in levels.<sup>10</sup> Acemoglu et al. (2005) used this method to study the e¤ect of education on democracy without ...nding any signi...cant e¤ect. One of the shortcomings of this method is that, as Bond, Hoe- er and Temple (2001) point out, the ...rst-di¤erence GMM estimator can behave poorly when time series are persistent and the lagged levels of the explanatory variables turn out to be weak instruments of the explanatory variables in ...rst-di¤erence. In small samples, this can cause serious estimation bias.<sup>11</sup> To overcome these problems, Bond et al. (2001) suggest to use a more informative set of instruments within the framework developed by Arellano and Bover (1995) and Blundell and Bond (1998). From our perspective, and given that democracy varies signi...cantly across countries but is quite persistent over time, it is clear that the Blundell and Bond system GMM is most appropriate. New results on the relationship between democracy and education were found using the system GMM estimator.<sup>12</sup> Following this literature, we use the Blundell and Bond system GMM estimator that combines the regression in di¤erences with the regression in levels in a single system. The instruments used in the ...rst di¤erentiated equation are the same as in Arellano-Bond (1991), but the instruments for the equation in level are the lagged di¤erences of the corresponding variables. In order to use these additional instruments, a moment condition for the level equation, which implies that ...rst di¤erences of pre-determined explanatory

> 10Under the assumptions that the error term is not serially correlated and that the explanatory variables are weakly exogenous or predetermined (i.e. the explanatory variables are not correlated with future realizations of the error term), the following moment conditions are applied for the ...rst di¤erence equations:

where Wit�s are the lagged dependent and all the pre-determined variables in the model.

> 11Simulation results show that the Di¤erence GMM may be subject to a large downward ...nitesample bias when time series are persistent, particularly when T is small. The higher the persistence of the series used as instruments, the weaker the correlation between levels and di¤erences (see Blundell and Bond (1998) for the weak instrumentation problem).

> 12Bobba and Coviello (2007), and Castello-Climent (2008). Splimbergo (2009) also uses system GMM.

9
variables are orthogonal to the country ...xed e¤ects, must be satis...ed.<sup>13</sup> We test the validity of moments conditions by using the test of overidentifying restrictions proposed by Hansen and by testing the null hypothesis that the error term is not second order serially correlated. Furthermore, we test the validity of the additional moment conditions associated with the level equation using the Hansen di¤erence test for all GMM instruments.<sup>14</sup> A particular concern related to this method is the risk of instrument proliferation. In fact, if the use of the entire set of instruments in a GMM context gives signi...cant e¢ ciency gains, on the other hand, a large collection of instruments could over...t endogenous variables as well as weaken the Hansen test of the instruments’ joint validity.<sup>15</sup> The instrument proliferation problem is particular important in small samples, but unfortunately there is no formal test to detect it, even if a possible rule of thumb is to keep the number of instruments lower than or equal to the number of groups.<sup>16</sup> In our analysis, we consider the lagged dependent and all the control variables of interest as predetermined, instrumented with "internal instruments", using their own one-period and further lags, according to the speci...cation.

# 2.2.2 Data

Our data set is a ...ve-year unbalanced panel spanning the period between 1980 and 2005, where the start of the date refers to the dependent variable (i.e., t = 1980, t � 1 = 1975). In our sample, we are considering only developing countries, and they enter the panel if they are independent at time t � 1. The data set employed in our analysis is an updated version of that used by Acemoglu et al. (2005) for the democracy indicators (except for economic freedom) and all the control variables. The migration data come from Defoort (2008).

# Democracy

Data on democracy are taken from the Freedom House data set, from the POLITY IV data set, and from the Economic Freedom of the World project (Simon Fraser

> 13For the level equation the following moment conditions are to be satis...ed:

> 14This test is not reported in the tables, but it is available upon request.

> 15See Roodman (2009)

> 16The xtabond2 command, implemented in Stata, gives a warning when instruments exceed the number of groups.

10
Institute).

The Freedom House measures political rights (PR) and civil liberties (CL) using, respectively, an index which ranges from 1 to 7, with a higher score indicating more freedom. The ratings are determined by a list of questions. For the political rights index, for example, the questions are grouped into three sub-categories: electoral processes; political pluralism and participation; and functioning of the government. The civil liberties questions are grouped into four subcategories: freedom of expression and belief; association and organization rights; rule of law and personal autonomy; and individual rights. The sum of each country’s sub-category scores translates to a rating from 1 to 7. Following Acemoglu et al. (2005) we transform the indexes so that they lie between 0 and 1, with 1 corresponding to the most-democratic set of institutions.

Another measure of democracy from the POLITY IV data set is considered. Indicators of democracy measure the general openness of political institutions and combines several aspects such as: the presence of institutions and procedures through which citizens can express e¤ective preferences about alternative policies and leaders; the existence of institutionalized constraints on the exercise of power by the executive power; and the guarantee of civil liberties to all citizens in their daily lives and in acts of political participation. In our data set we consider a composite index (Polity2), that ranges from -10 to + 10. This index is also normalized from 0 to 1, with 1 corresponding to the most democratic set of institutions.

Finally, we also consider Economic Freedom of the World (EFW), an index which measures the degree to which countries’policies and institutions support economic freedom. Five broad areas are distinguished: (1) size of government; (2) legal structure and security of property rights; (3) access to sound money; (4) freedom to trade internationally; and (5) regulation of credit, labor and business. This index is also normalized between 0-1.

# Migration

For emigration data, we use the estimates provided in Defoort (2008). Focusing on the six major destination countries (USA, Canada, Australia, Germany, UK and France), she computed skilled emigration stocks and rates by educational attainment from 1975 to 2000 (one observation every 5 years). On the whole, the six destination countries represent about 75 percent of the OECD total immigration stock.<sup>17</sup>

> 17However, for some sending countries, the coverage by the Defoort dataset may be quite low. For

11
# Other data

Data on human capital are based on Barro and Lee (2001). Data on GDP per capita and population data are taken from the PWT and from the World Development Indicators. Data on legal origins are taken from La Porta et al. (1999).

# 2.2.3 Regression results

Tables 1, 2, 3, 4 present our main general results from estimating equation 1 and using the Freedom House PR and CL indicators, the Polity2 measure from the Polity IV data set, and the Economic Freedom Indicator (EFW). We start by considering as variables of interest the lagged dependent, the total emigration rate, the share of tertiary educated workers over the total resident labor force, and the log of population size.

Column 1 of each table shows the pooled OLS relationship between the total emigration rate and democracy by estimating equation 1. The results show a positive correlation between openness to migration and democracy, statistically signi...cant, however, only when considering the Polity2 and EFW indexes (all standard errors are robust and clustered by country group). In column 2, when we control for ...xed e¤ect, the coe¢ cient related to the total emigration rate becomes negative (except for EFW), and statistically not signi...cant. We know that in a dynamic panel data model, the standard ...xed e¤ect estimator is biased and inconsistent in panels with a short time dimension (the so called Nickell bias (Nickell, 1981)). Moreover, both in our ...xed e¤ect and pooled OLS estimations, explanatory variables are considered as exogenous. To deal with these problems we use the system GMM estimator that is consistent in dynamic panel estimations and rely on "internal instruments" to control for a weak form of exogeneity of all explanatory variables. We consider the explanatory variables of interest as predetermined, i.e. instrumented using their own one-period and further lags, in order to use a relevant number of instruments for e¢ ciency reasons and at the same time keeping the number of instruments lower than or equal to the number of country groups in all speci...cations.<sup>18</sup> In column (3) example, Surinamese emigrants mainly live in the Netherlands, with just 3 percent of Surinamese emigrants living in the six receiving countries in Defoort’s sample. We will therefore conduct a sensitivity analysis to check the robustness of the results to the exclusion of low-coverage countries in the Defoort dataset.

> 18A problem of the GMM estimator is that too many instruments can over ...t the endogenous variable. As rule of thumb, the number of instruments should be less or at least equal to the number

12
of tables 1, 2, 3, 4 the estimates for the total emigration rate are now positive and highly signi...cant at the one percent level for all four indicators. Column (4) shows the same speci...cation, but now reducing the number of instruments for robustness check. Our previous results are con...rmed.<sup>19</sup> The share of tertiary educated workers over the total resident labor force, as a proxy for resident human capital, is another variable of interest in our model. As for the total emigration rate, the results show a statistically signi...cant and positive correlation between the share of total educated workers and democracy in pooled OLS regressions. The coe¢ cients turn out to be negative (except for EFW) and not statistically signi...cant in ...xed e¤ect regressions. Column (3) of tables 1, 2, 3, 4 shows the SYS GMM estimates. The estimated coe¢ cients of the share of tertiary educated workers are now positive and statistically signi...cant at usual signi...cance levels, except for the Polity2 indicators. The results are con...rmed when reducing the number of instruments in column (4).

In our basic speci...cation, we add also as a regressor the logarithm of population size (lagged), which is positive and statistically signi...cant for two indicators out of four when using the SYS GMM estimator. Including population size in our model is important to avoid omitted variable bias. Indeed, population size can a¤ect institutional quality and is often considered as an explanatory variable in the relevant literature (see for example Acemoglu et al., 2005, and Bobba and Coviello, 2007). At the same time, population size is negatively correlated with the emigration rate (big countries have small emigration rates); therefore, including population size is important to make sure the emigration rate is not simply capturing a country-size e¤ect.

Column (5) controls for GDP per capita (in logs). The estimated coe¢ cient of the emigration rate is again positive and statistically signi...cant at 10 and 1 percent when considering the Civil Liberties and Polity2 indicators, but loses its signi...cance when of groups. We follow this rule even if sometimes, given few data observations and speci...cations with additional controls, in the reported regressions the number of instruments is slightly higher than the number of groups. For comparative reasons, we show regressions where explanatory variables are instrumented using their one-period to their second or third lags. In unreported regressions, when instruments outnumber the number of groups, for robustness check, we further reduce the number of instruments using only their one period lag. We ...nd that results do not substantially change. 19In column 3, all the explanatory variables are considered as predetermined and instrumented using their own ...rst to third lags. In column 4, all the variables are instrumented using their own ...rst to second lags.

13
using the Political Rights indicator and Economic Freedom. The share of tertiary educated workers over the total residence labor force is not signi...cant anymore, probably due to the two variables being highly correlated (0.7145). Finally, the coe¢ cient on the GDP per capita is in general positive but not always signi...cant.<sup>20</sup> The estimations con...rm that democracy is very persistent. Moreover, considering the ...rst 3 columns in each table, the coe¢ cient on past democracy ranges between the estimated coe¢ cient in pooled OLS, which is usually biased upwards, and the estimated coe¢ cient for the ...xed e¤ect, which usually displays a downward bias.

The AR(2) test which tests the null hypothesis that the error term is not second order serially correlated, and the Hansen J test of overindentifying restrictions, indicate that the moment conditions are satis...ed and the instruments are valid.

In general, the results appear quite robust across speci...cations and indices.<sup>21</sup> To evaluate whether the skill composition of migration, and not just its size, a¤ects institutional quality at home, we introduce in column 6 the share of tertiary educated amongs migrants. The coe¢ cient of the share of tertiary educated migrants is negative but not statistically signi...cant for 3 indicators out of 4 and is only positive and signi...cant at the 10 percent when considering the EFW indicator. In spite or, rather, because of this inconclusive result, we will further investigate this issue in the next section using numerical simulations.

Finally, one may be concerned, as Acemoglu et al. (2005) were about their own study, that the presence of socialist countries in our sample may largely a¤ect the estimation results. Indeed, most socialist countries had high levels of education in the 1980s and did not experience any particularly increase in educational attainments during or immediately after the transition. In addition, prior to the transition, legal emigration was strongly restricted, while after the transition most socialist countries

> 20In unreported regressions, we also introduce as control variables, the mediam age of the population, and urbanization rate. While human capital loses its signi...cance, probably because of multicollinearity, the total emigration rate remains signi...cant when considering these additional control variables as exogenous. If they are considered as pre-determined, then the emigration rate also loses its signi...cance too, which may be due either to collinearity or instruments proliferation.

21To further assess the robustness of our results, in unreported regressions we considered the total emigration rate divided by a coverage measure in the Defoort (2008) dataset. Recall that the Defoort ...gures are based on the six major destination countries (USA, Canada, Australia, Germany, UK and France). Comparing the emigration stocks in 2000 in the Defoort data set with those in the Docquier and Marfouk (2006) data set (which is based to 30 OECD destination countries) yields a variable indicating the percentage of coverage of the Defoort data set. Dividing the total emigration rate by this coverage measure does not a¤ect the quality of the results.

14
experienced a strong increase in emigration. To control for the speci...c characteristics of these economies, in column (7) of each tables we interact human capital and emigration with legal origin socialist dummies, ...nding in general a statistically signi...cant e¤ect for the interacted terms, in particular for emigration.<sup>22</sup> The interaction term on emigration is negative and signi...cant for all three "political" indicators of democracy, and positive for the "economic" indicator. This suggests that emigration caused socialist regimes to become politically more repressive, an interpretation which ...ts well with the popular historical accounts of the former Communist bloc. If it is correct, however, it should be relevant only prior to the transition. In column (8) of each tables, we therefore consider the same interaction, but now introduce a dummy variable which takes a value equal to 1 in years before (or equal to) 1990. The magnitude and signi...cance levels of the coe¢ cient are thereby increased, which supports our interpretation of these results.

# 2.2.4 Robustness

The evidence found in the previous section reveals that human capital and emigration may improve institutional quality. To control for the robustness of these results, for each indicator we consider in table 5 our benchmark speci...cation in a balanced sample. This allows for checking whether the entry and exit of countries from the unbalanced sample may a¤ect our estimates. The results for PR, CL, Polity2 indicators are very similar to those in previous tables. Moreover, now the estimated coe¢ cient for human capital is also statistically signi...cant at 10 percent for the Polity2 indicator. In the case of the Economic Freedom Indicator, the estimates are not reliable due to the fact that too many observations are lost.

Table 6 provides additional robustness checks in a balanced sample when considering non-linear e¤ects for socialist countries as in columns (7) and (8) of tables 1, 2, 3, 4. Again, the estimates are very similar to the previous ones in an unbalanced sample, with more signi...cant results for interacted terms with human capital. As before, in the case of the Economic Freedom Indicator estimates are not reliable, because too many observations are lost.

Finally, in tables 7, 8, 9, 10, socialist countries are excluded from the sample. The results show that our ...ndings are not driven by socialist countries.

> 22In the regressions, the legal origin dummy is not introduced by itself, because in SYS-GMM ...xed e¤ects are already taken into accounts.

15
Another concern refers to the presence of oil-exporting countries. Several studies have pointed out a negative correlation between oil export dependence and democracy, with oil endowment appearing as a cause for lower democracy (e.g., Ross, 2001, Tsui, 2010). To control for the speci...c characteristics of these economies, in table 11 we consider interaction terms with human capital, total emigration rate and a dummy for oil-exporting countries, both in an unbalaced and balanced sample. The estimated coe¢ cients of human capital and the total emigration rate are in general positive and statistically signi...cant across indicators, as in the baseline regressions. Interaction terms with human capital and a dummy for oil-exporting countries are generally negative and statistically signi...cant (with higher coe¢ cients that the estimated coe¢ cient of human capital). This means that, in the case of oil-exporting countries, human capital has a negative impact on institutional quality. Interaction terms with total emigration rate, instead, are positive, but in general not statistically signi...cant (except for the CL indicator).

Finally, another concern is whether Sub-Saharan African countries, which have sometimes unstable political dynamics, may a¤ect our results. Table 12 shows the estimated results when we include interaction terms with a dummy for Sub-Saharan African countries. Again, the estimated coe¢ cients of human capital and total emigration rate are positive and statistically signi...cant across the various speci...cations and di¤erent institutional quality indicators, con...rming our results. The interaction terms with human capital are in general not statistically signi...cant while those with emigration are generally positive and statistically signi...cant. This would seem to suggest that African countries tend to bene...t more from the institutional gains emigration brings about.<sup>23</sup>

> 23See the appendix for Tables 7 to 12.

16
|SYS<br>GMM<br>(8)<br>0.695***<br>(0.0628)<br>0.659**<br>(0.294)<br>0.513*<br>(0.277)<br>0.00753<br>(0.0209)<br>1.393**<br>(0.655)<br>-2.351***<br>(0.591)<br>yes<br>0.000<br>0.646<br>0.788<br>476<br>91<br>86<br>alanced sample<br>es reported for<br>ented for using<br>n (4) shows the<br>nts, the system|
|---|
|SYS<br>GMM<br>(7)<br>0.680***<br>(0.0556)<br>0.662**<br>(0.290)<br>0.513**<br>(0.237)<br>0.00390<br>(0.0166)<br>0.744<br>(0.611)<br>-1.872*<br>(1.021)<br>yes<br>0.000<br>0.555<br>0.836<br>476<br>91<br>90<br>mple is an unb<br>tions. The valu<br>ey are instrum<br>rticular, colum<br> these instrume|
|SYS<br>GMM<br>(6)<br>0.647***<br>(0.0576)<br>0.670**<br>(0.321)<br>0.673***<br>(0.256)<br>0.0329<br>(0.0204)<br>-0.108<br>(0.126)<br>yes<br>0.000<br>0.571<br>0.620<br>476<br>91<br>91<br>mator. The sa<br> serial correla<br>ermined. Th<br>lumns. In pa<br>n addition to|
|SYS<br>GMM<br>(5)<br>0.626***<br>(0.0605)<br>-0.125<br>(0.426)<br>0.304<br>(0.413)<br>-0.00304<br>(0.0201)<br>0.0773**<br>(0.0319)<br>yes<br>0.000<br>0.427<br>0.471<br>423<br>85<br>76<br> GMM esti<br>ond test for <br>d as pre-det<br> the other co<br>ess check. I<br>one period.|
|SYS<br>GMM<br>(4)<br>0.609***<br>(0.0658)<br>0.796**<br>(0.361)<br>0.914***<br>(0.349)<br>0.0485*<br>(0.0284)<br>yes<br>0.000<br>0.553<br>0.302<br>476<br>91<br>62<br>e step system<br> of Arellano-B<br>les are treate<br>nd lags in all <br>gs for robustn<br>ences lagged|
|SYS<br>GMM<br>(3)<br>0.640***<br>(0.0623)<br>0.642*<br>(0.335)<br>0.885***<br>(0.338)<br>0.0478*<br>(0.0273)<br>yes<br>0.000<br>0.542<br>0.351<br>476<br>91<br>74<br>arentheses. On<br>re the p-values <br> All the variab<br>wn ...rst to seco<br>l the second la<br> the ...rst di¤er|
|F.E.<br>OLS<br>(2)<br>0.355***<br>(0.0520)<br>-0.650<br>(0.700)<br>-0.647<br>(0.661)<br>-0.443***<br>(0.158)<br>yes<br>0.247<br>476<br>91<br>y country in p<br> and AR(2) a<br>ment validity. <br>ed for their o<br>struments til<br>y variables in|
|Pooled<br>OLS<br>(1)<br>PRt�5<br>0.721***<br>(0.0381)<br>Human capitalt�5<br>0.678***<br>(0.243)<br>Total emigration ratet�5<br>0.183<br>(0.112)<br>Log populationt�5<br>-0.00865<br>(0.00663)<br>Log GDP per capitat�5<br>Share tertiary ed. migrantst�5<br>Human capitalt�5*Soc. dummy<br>Total emigration ratet�5*Soc. dummy<br>Human capitalt�5*Soc. dummy*d90<br>Total emigration ratet�5*Soc. dummy*d90<br>Time dummies<br>yes<br>R-squared<br>0.611<br>AR(1) test<br>AR(2) test<br>Hansen J test<br>Observations<br>476<br>N. countries<br>N. instr.<br>*** p<0.01, ** p<0.05, * p<0.1. Robust standard errors clustered b<br>comprising data at ...ve year interval between 1980 and 2005. AR(1) <br>the Hansen J test are the p-values for the null hypothesis of instru<br>their own ...rst to third lags in columns 3 and 6. They are instrument<br>same speci...cation as column (3), but now reducing the number of in<br>GMM also uses as instruments for the level equations the explanator|

17
|SYS<br>GMM<br>(8)<br>0.721***<br>(0.0628)<br>0.432**<br>(0.204)<br>0.434**<br>(0.216)<br>0.00443<br>(0.0135)<br>1.783***<br>(0.374)<br>-2.144***<br>(0.482)<br>yes<br>0.000<br>0.374<br>0.467<br>476<br>91<br>86<br>balanced sample<br>lues reported for<br>mented for using<br>mn (4) shows the<br>ents, the system|
|---|
|SYS<br>GMM<br>(7)<br>0.678***<br>(0.0540)<br>0.497**<br>(0.197)<br>0.473**<br>(0.215)<br>-0.00002<br>(0.0125)<br>0.858*<br>(0.489)<br>-1.702*<br>(0.999)<br>yes<br>0.000<br>0.544<br>0.588<br>476<br>91<br>90<br>mple is an un<br>tions. The va<br>ey are instru<br>rticular, colu<br> these instrum|
|SYS<br>GMM<br>(6)<br>0.648***<br>(0.0571)<br>0.582**<br>(0.238)<br>0.508**<br>(0.215)<br>0.0197<br>(0.0140)<br>-0.126<br>(0.0911)<br>yes<br>0.000<br>0.521<br>0.291<br>476<br>91<br>91<br>mator. The sa<br> serial correla<br>termined. Th<br>lumns. In pa<br>n addition to|
|SYS<br>GMM<br>(5)<br>0.593***<br>(0.0698)<br>0.0112<br>(0.310)<br>0.498*<br>(0.274)<br>0.00452<br>(0.0134)<br>0.0467**<br>(0.0227)<br>yes<br>0.000<br>0.836<br>0.247<br>423<br>85<br>76<br>m GMM esti<br>Bond test for <br>ted as pre-de<br>ll the other co<br>ness check. I<br> one period.|
|SYS<br>GMM<br>(4)<br>0.577***<br>(0.0695)<br>0.676**<br>(0.276)<br>0.754***<br>(0.280)<br>0.0291<br>(0.0185)<br>yes<br>0.000<br>0.604<br>0.0662<br>476<br>91<br>62<br>ne step syste<br>s of Arellano-<br>bles are trea<br>ond lags in a<br>ags for robust<br>erences lagged|
|SYS<br>GMM<br>(3)<br>0.621***<br>(0.0637)<br>0.596**<br>(0.263)<br>0.682***<br>(0.260)<br>0.0271<br>(0.0168)<br>yes<br>0.000<br>0.571<br>0.241<br>476<br>91<br>74<br>arentheses. O<br>re the p-value<br> All the varia<br>wn ...rst to sec<br>l the second l<br> the ...rst di¤|
|F.E.<br>OLS<br>(2)<br>0.352***<br>(0.0550)<br>-0.326<br>(0.492)<br>-0.268<br>(0.454)<br>-0.224*<br>(0.119)<br>yes<br>0.327<br>476<br>91<br>country in p<br>nd AR(2) a<br>ent validity. <br>d for their o<br>truments til<br> variables in|
|Pooled<br>OLS<br>(1)<br>CLt�5<br>0.770***<br>(0.0375)<br>Human capitalt�5<br>0.536***<br>(0.183)<br>Total emigration ratet�5<br>0.144<br>(0.0938)<br>Log populationt�5<br>-0.00656<br>(0.00506)<br>Log GDP per capitat�5<br>Share tertiary ed. migrantst�5<br>Human capitalt�5*Soc. dummy<br>Total emigration ratet�5*Soc. dummy<br>Human capitalt�5*Soc. dummy*d90<br>Total emigration ratet�5*Soc. dummy*d90<br>Time dummies<br>yes<br>R-squared<br>0.692<br>AR(1) test<br>AR(2) test<br>Hansen J test<br>Observations<br>476<br>N. countries<br>N. instr.<br>*** p<0.01, ** p<0.05, * p<0.1. Robust standard errors clustered by <br>comprising data at ...ve year interval between 1980 and 2005. AR(1) a<br>the Hansen J test are the p-values for the null hypothesis of instrum<br>their own ...rst to third lags in columns 3 and 6. They are instrumente<br>same speci...cation as column (3), but now reducing the number of ins<br>GMM also uses as instruments for the level equations the explanatory|

18
|SYS<br>GMM<br>(8)<br>0.638***<br>(0.0682)<br>0.547*<br>(0.293)<br>1.120***<br>(0.370)<br>0.0531*<br>(0.0274)<br>0.833<br>(0.544)<br>-3.032***<br>(0.541)<br>yes<br>0.000<br>0.754<br>0.627<br>459<br>85<br>86<br>alanced sample<br>es reported for<br>ented for using<br>hows the same<br>e system GMM|
|---|
|SYS<br>GMM<br>(7)<br>0.639***<br>(0.0615)<br>0.516*<br>(0.268)<br>0.980***<br>(0.334)<br>0.0337<br>(0.0215)<br>0.997**<br>(0.448)<br>-2.527**<br>(1.023)<br>yes<br>0.000<br>0.742<br>0.605<br>459<br>85<br>90<br>ple is an unb<br>ons. The valu<br>y are instrum<br>, column (4) s<br>struments, th|
|SYS<br>GMM<br>(6)<br>0.594***<br>(0.0606)<br>0.643**<br>(0.309)<br>0.955***<br>(0.309)<br>0.0471**<br>(0.0226)<br>-0.163<br>(0.143)<br>yes<br>0.000<br>0.711<br>0.284<br>459<br>85<br>76<br>ator. The sam<br>erial correlati<br>rmined. The<br> In particular<br>on to these in|
|SYS<br>GMM<br>(5)<br>0.554***<br>(0.0664)<br>0.173<br>(0.557)<br>1.141***<br>(0.400)<br>0.0568**<br>(0.0265)<br>0.0420<br>(0.0418)<br>yes<br>0.000<br>0.663<br>0.243<br>412<br>79<br>76<br> GMM estim<br>ond test for s<br>d as pre-dete<br>her columns. <br>ck. In additi<br>riod.|
|SYS<br>GMM<br>(4)<br>0.560***<br>(0.0661)<br>0.565<br>(0.360)<br>1.486***<br>(0.450)<br>0.0928***<br>(0.0337)<br>yes<br>0.000<br>0.661<br>0.200<br>459<br>85<br>62<br>ne step system<br>s of Arellano-B<br>ables are treate<br>gs in all the ot<br> robustness che<br> lagged one pe|
|SYS<br>GMM<br>(3)<br>0.577***<br>(0.0675)<br>0.520<br>(0.349)<br>1.389***<br>(0.420)<br>0.0894***<br>(0.0307)<br>yes<br>0.000<br>0.664<br>0.279<br>459<br>85<br>74<br> parentheses. O<br> are the p-value<br>y. All the vari<br>rst to second la<br> second lags for<br> ...rst di¤erences|
|F.E.<br>OLS<br>(2)<br>0.365***<br>(0.0558)<br>-0.700<br>(0.693)<br>-0.470<br>(0.745)<br>-0.312**<br>(0.150)<br>yes<br>0.432<br>459<br>85<br>y country in <br> and AR(2) <br>ment validit<br> their own ...<br>ents till the <br>ables in the|
|Pooled<br>OLS<br>(1)<br>Polity2t�5<br>0.723***<br>(0.0415)<br>Human capitalt�5<br>0.662***<br>(0.213)<br>Total emigration ratet�5<br>0.219*<br>(0.127)<br>Log populationt�5<br>-0.00306<br>(0.00745)<br>Log GDP per capitat�5<br>Share tertiary ed. migrantst�5<br>Human capitalt�5*Soc. dummy<br>Total emigration ratet�5*Soc. dummy<br>Human capitalt�5*Soc. dummy*d90<br>Total emigration ratet�5*Soc. dummy*d90<br>Time dummies<br>yes<br>R-squared<br>0.660<br>AR(1) test<br>AR(2) test<br>Hansen J test<br>Observations<br>459<br>N. countries<br>N. instr.<br>*** p<0.01, ** p<0.05, * p<0.1. Robust standard errors clustered b<br>comprising data at ...ve year interval between 1980 and 2005. AR(1) <br>the Hansen J test are the p-values for the null hypothesis of instru<br>their own ...rst to third lags in column 3. They are instrumented for <br>speci...cation as column (3), but now reducing the number of instrum<br>also uses as instruments for the level equations the explanatory vari|

19
||SYS<br>SYS<br>GMM<br>GMM<br>(7)<br>(8)<br>0.744***<br>0.713***<br>(0.0542)<br>(0.0561)<br>0.175*<br>0.214**<br>(0.0901)<br>(0.0900)<br>0.169**<br>0.215***<br>(0.0754)<br>(0.0770)<br>-0.000487<br>0.00234<br>(0.00476)<br>(0.00413)<br>-0.178<br>(0.176)<br>1.491*<br>(0.851)<br>-0.861***<br>(0.190)<br>1.982***<br>(0.566)<br>yes<br>yes<br>0.000<br>0.000<br>0.0765<br>0.0997<br>0.896<br>0.846<br>372<br>372<br>74<br>74<br>87<br>83<br>le is an unbalanced sample<br>ns. The values reported for<br> are instrumented for using<br>column (4) shows the same<br>ruments, the system GMM|
|---|---|
|x (EFW)|SYS<br>GMM<br>(6)<br>0.741***<br>(0.0585)<br>0.158**<br>(0.0762)<br>0.238***<br>(0.0878)<br>0.000695<br>(0.00507)<br>0.0666*<br>(0.0365)<br>yes<br>0.000<br>0.0841<br>0.543<br>372<br>74<br>76<br>ator. The samp<br>erial correlatio<br>rmined. They <br> In particular, <br>on to these inst|
|World Inde|SYS<br>GMM<br>(5)<br>0.788***<br>(0.0415)<br>-0.00642<br>(0.134)<br>0.0996<br>(0.0989)<br>-0.00381<br>(0.00541)<br>0.0182*<br>(0.0103)<br>yes<br>0.000<br>0.0472<br>0.716<br>357<br>73<br>76<br>m GMM estim<br>Bond test for s<br>ted as pre-dete<br> other columns. <br>heck. In additi<br>eriod.|
|m of the|SYS<br>GMM<br>(4)<br>0.760***<br>(0.0610)<br>0.173**<br>(0.0805)<br>0.201**<br>(0.0825)<br>0.000484<br>(0.00527)<br>yes<br>0.000<br>0.0754<br>0.308<br>372<br>74<br>62<br>ne step syste<br>s of Arellano-<br>ables are trea<br>ags in all the <br> robustness c<br> lagged one p|
|Table 4: Dependent Variable: Economic Freedo|Pooled<br>F.E.<br>SYS<br>OLS<br>OLS<br>GMM<br>(1)<br>(2)<br>(3)<br>EFWt�5<br>0.760***<br>0.456***<br>0.759***<br>(0.0323)<br>(0.0559)<br>(0.0615)<br>Human capitalt�5<br>0.201***<br>0.0997<br>0.167**<br>(0.0604)<br>(0.203)<br>(0.0767)<br>Total emigration ratet�5<br>0.158***<br>0.382<br>0.203***<br>(0.0432)<br>(0.325)<br>(0.0779)<br>Log populationt�5<br>0.00215<br>-0.0238<br>0.00221<br>(0.00175)<br>(0.0590)<br>(0.00494)<br>Log GDP per capitat�5<br>Share tertiary ed. migrantst�5<br>Human capitalt�5*Soc. dummy<br>Total emigration ratet�5*Soc. dummy<br>Human capitalt�5*Soc. dummy*d90<br>Total emigration ratet�5*Soc. dummy*d90<br>Time dummies<br>yes<br>yes<br>yes<br>R-squared<br>0.708<br>0.579<br>AR(1) test<br>0.000<br>AR(2) test<br>0.0711<br>Hansen J test<br>0.391<br>Observations<br>372<br>372<br>372<br>N. countries<br>74<br>74<br>N. instr.<br>74<br>*** p<0.01, ** p<0.05, * p<0.1. Robust standard errors clustered by country in parentheses. O<br>comprising data at ...ve year interval between 1980 and 2005. AR(1) and AR(2) are the p-value<br>the Hansen J test are the p-values for the null hypothesis of instrument validity. All the vari<br>their own ...rst to third lags in columns 3. They are instrumented for their own ...rst to second l<br>speci...cation as column (3), but now reducing the number of instruments till the second lags for<br>also uses as instruments for the level equations the explanatory variables in the ...rst di¤erences|

20
Table 5: Balanced sample

||P|R|C|L|PO|L2|EFW|
|---|---|---|---|---|---|---|---|
||(1)|(2)|(3)|(4)|(5)|(6)|(7)|
|PRt�5|0.651***<br>(0.0600)|0.619***<br>(0.0650)||||||
|CLt�5|||0.619***<br>(0.0592)|0.565***<br>(0.0662)||||
|Polity2t�5|||||0.577***<br>(0.0634)|0.560***<br>(0.0645)||
|EFWt�5|||||||0.726***<br>(0.0609)|
|Human capitalt�5|0.708**|0.870**|0.631***|0.737***|0.542*|0.557*|0.0342|
||(0.317)|(0.348)|(0.240)|(0.260)|(0.318)|(0.331)|(0.0958)|
|Total emigration ratet�5|0.819***|0.848***|0.518**|0.589**|1.127***|1.203***|0.0616|
||(0.317)|(0.329)|(0.260)|(0.274)|(0.379)|(0.399)|(0.116)|
|Log populationt�5|0.0456*|0.0452*|0.00971|0.0129|0.0644**|0.0673**|-0.00437|
||(0.0246)|(0.0257)|(0.0153)|(0.0171)|(0.0281)|(0.0306)|(0.00657)|
|Time dummies|yes|yes|yes|yes|yes|yes|yes|
|AR(1) test|0.000|0.000|0.000|0.000|0.000|0.000|0.001|
|AR(2) test|0.551|0.562|0.579|0.621|0.856|0.852|0.210|
|Hansen J test|0.414|0.429|0.252|0.113|0.391|0.181|0.997|
|Observations|456|456|456|456|432|432|216|
|N. countries|76|76|76|76|72|72|36|
|N. instr.|74|62|74|62|74|62|62|

*** p<0.01, ** p<0.05, * p<0.1. Robust standard errors clustered by country in parentheses. One step system GMM estimator. The sample is a balanced sample comprising data at ...ve year interval between 1980 and 2005. AR(1) and AR(2) are the p-values of Arellano-Bond test for serial correlations. The values reported for the Hansen J test are the p-values for the null hypothesis of instrument validity. All the variables are treated as pre-determined. They are instrumented for using their own ...rst to third lags in columns 1, 3 , 5. They are instrumented for using their own ...rst to second lags in columns 2, 4, 6, 7. In addition to these instruments, the system GMM also uses as instruments for the level equations the explanatory variables in the ...rst di¤erences lagged one period.

21
|(9)<br>EFW|0.726***<br>(0.0609)<br>0.0342<br>(0.0958)<br>0.0616<br>(0.116)<br>-0.00437<br>(0.00657)<br>yes<br>0.001<br>0.210<br>0.997<br>216<br>36<br>62<br> a balanced sample<br>values reported for<br>umented for using<br>ariables in the ...rst|
|---|---|
|(8)<br>Polity2|0.625***<br>(0.0663)<br>0.514*<br>(0.286)<br>1.008***<br>(0.342)<br>0.884*<br>(0.523)<br>-2.889***<br>(0.550)<br>0.0459*<br>(0.0261)<br>yes<br>0.000<br>0.937<br>0.721<br>432<br>72<br>86<br>he sample is <br>lations. The <br>hey are instr<br>xplanatory v|
|(7)<br>CL|0.708***<br>(0.0582)<br>0.448**<br>(0.204)<br>0.357<br>(0.220)<br>1.805***<br>(0.401)<br>-2.073***<br>(0.553)<br>-0.00480<br>(0.0133)<br>yes<br>0.000<br>0.378<br>0.652<br>456<br>76<br>86<br> estimator. T<br>or serial corre<br>etermined. T<br>quations the e|
|(6)<br>PR|0.709***<br>(0.0600)<br>0.655**<br>(0.286)<br>0.553**<br>(0.269)<br>1.419**<br>(0.632)<br>-2.297***<br>(0.611)<br>0.0105<br>(0.0202)<br>yes<br>0.000<br>0.650<br>0.856<br>456<br>76<br>86<br>ystem GMM <br>o-Bond test f<br>ated as pre-d<br>or the level e|
|(5)<br>EFW|0.726***<br>(0.0609)<br>0.0342<br>(0.0958)<br>0.0616<br>(0.116)<br>-0.00437<br>(0.00657)<br>yes<br>0.001<br>0.210<br>0.997<br>216<br>36<br>62<br>s. One step s<br>es of Arellan<br>iables are tre<br> instruments f|
|(4)<br>Polity2|0.627***<br>(0.0627)<br>0.505*<br>(0.274)<br>0.994***<br>(0.350)<br>0.834*<br>(0.429)<br>-3.042***<br>(0.697)<br>0.0389<br>(0.0252)<br>yes<br>0.000<br>0.904<br>0.795<br>432<br>72<br>90<br> in parenthese<br> are the p-valu<br>y. All the var<br> also uses as|
|(3)<br>CL|0.664***<br>(0.0511)<br>0.516***<br>(0.198)<br>0.518**<br>(0.240)<br>1.106**<br>(0.446)<br>-2.275***<br>(0.804)<br>0.00389<br>(0.0157)<br>yes<br>0.000<br>0.551<br>0.803<br>456<br>76<br>90<br>d by country <br>) and AR(2) <br>ument validit<br> system GMM|
|(1)<br>PR|PRt�5<br>0.683***<br>(0.0546)<br>CLt�5<br>Polity2t�5<br>EFWt�5<br>Human capitalt�5<br>0.667**<br>(0.289)<br>Total emigration ratet�5<br>0.736***<br>(0.282)<br>Human capitalt�5*Soc. dummy<br>1.168***<br>(0.405)<br>Total emigration ratet�5*Soc. dummy<br>-2.804***<br>(0.589)<br>Human capitalt�5*Soc. dummy*d90<br>Total emigration ratet�5*Soc. dummy*d90<br>Log populationt�5<br>0.0238<br>(0.0219)<br>Time dummies<br>yes<br>AR(1) test<br>0.000<br>AR(2) test<br>0.564<br>Hansen J test<br>0.945<br>Observations<br>456<br>N. countries<br>76<br>N. Instruments<br>90<br>*** p<0.01, ** p<0.05, * p<0.1. Robust standard errors clustere<br>comprising data at ...ve year interval between 1980 and 2005. AR(1<br>the Hansen J test are the p-values for the null hypothesis of instr<br>their own ...rst to second lags. In addition to these instruments, the <br>di¤erences lagged one period.|

22
# 3 Country speci...c results for skilled emigration

The estimation results above suggest that both openness to migration (as measured by the total emigration rate) and human capital (as measured by the share of tertiary educated in the resident labor force) have a positive impact on domestic institutional quality. What happens, then, when an educated invidual emigrates? As we have seen, the share of skilled among emigrants is never signi...cant in our regressions. Furthermore, interacting this variable with either human capital or emigration creates multicollinearity problems that further prevent us from testing empirically whether the institutional gain from migration is higher or lower when the composition of emigration becomes more high-skill. In addition, independently of the average e¤ect we would also like to know which countries would gain or lose from having more skilled migration. For these reasons, in what follows we will rely on numerical simulations to address the following questions: i) Which countries would lose/gain from a marginal increase in high-skilled emigration?

ii) And which countries would lose/gain from having a non-selective emigration, that is, from having their high-skilled emigration rates counterfactually reduced so as to equal their low-skilled emigration rate?

To answer these questions we start from the empirical model (1) and then proceed with numerical experiments. To do so, we need to use additional notations and supplement equation (1) with some identities. Let us drop country and time indexes to simplify the notations. Each country at each period is characterized by Nk natives of skill k (with k = s for the highly skilled and k = u for the low skilled) and Mk emigrants. The skill-speci...c emigration rates are de...ned as mk = Mk=Nk. Ex-ante (or before-migration) human capital is measured by the proportion of highly skilled among natives, i.e. H � NsN+sNu<sup>.Withthesenotations,itisclearwecanwritethe</sup> average emigration used in (1) rate as: and the ex-post (or after-migration) proportion of highly skilled in (1) is given by: 23
If we assume that human capital is independent of migration (i.e., we neglect any incentives to acquire additional human capital in a context of migration or, in other words, we take H as given), then we can write the partial derivatives of m and h with respect to ms and mu as: Recalling the empirical model and the estimated equation (1), we may consider that democracy, or more generally let’s denote it institutional quality I, depends on the total emigration rate, m, and on the share of highly skilled human capital in the resident labor force, h.<sup>24</sup> We write: The e¤ect of emigration rates on institutions is then given by: This shows that the e¤ect of low skilled emigration is always positive while the e¤ect of high-skilled emigration is ambiguous. Focusing on skilled emigration, we can see that (i) high-skilled emigration improves institutions i¤

> 24Comparing (1) and (2), we have Ii;t = Democracyi;t+5 � �0:Democracyi;t. In the long-run (indexed by ss), we have Ii;ss = (1��0):Democracyi;ss.Our variable I proxies long-run institutional quality or transitional institutional improvement.

24
(ii) the condition for a positive optimal brain drain ( dm<sup><u>dI</u></sup> s<sup>> 0forms= 0)is</sup> (iii) and the condition for an interior optimal brain drain ( dm<sup><u>dI</u></sup> s<sup>< 0forms= 1)is</sup> In these conditions, variables zs, z0 and z1 are country-speci...c and their distribution can be computed using the Gaussian kernel density estimator. The ratio<sup><u>�2</u></sup> �1 results from our estimation. Using the point estimates from our baseline regressions both in an unbalanced and balanced sample (column (3) of tables 1, 2, 3, 4 for the unbalanced sample, and columns (1), (3), (5) of table 5 for the balanced sample), we can simulate these three conditions.<sup>25</sup> To save place and given that we are mostly interested in the ...rst of these conditions, we do not present simulation results for the last two.<sup>26</sup> Figures 2a to 2d show the kernel distribution of 11��mh<sup>�zsandverticallinesat</sup> values of<sup><u>�2</u>the4indicators(thicklinesfortheunbalancedsample;thinlines</sup> �1<sup>for</sup> for the balanced sample). As can be seen from the ...gures, the marginal e¤ect of the skilled emigration rate is positive for almost all of the countries (the kernel distribution is completely to the left of the thresholds, except for CL in a balanced sample).<sup>27</sup> However, when we calculate 90 percent con...dence intervals (dashed lines) for the vertical lines at values of<sup><u>�2</u>eachofthe4indicators(bothinthebalancedand</sup> �1<sup>for</sup> unbalanced samples<sup>28</sup> ),<sup>29</sup> this result turns out to be not signi...cant since the bulk of the kernel distribution lies between the upper and lower bounds of the con...dence interval.

> 25For the simulations, we consider the unbalanced sample of 91 countries as in column (3) of tables 1 and 2. Data considered refer to year 2000 from Barro and Lee (2001) and Defoort (2008). When Barro and Lee (2001) data on human capital are missing for year 2000, the human capital data from Defoort (2008) are considered (this happens for 11 countries).

> 26 They are available from the authors upon request.

> 27The few "losers" (negative marginal e¤ect) are all with extremely high brain drain rates.

> 28For EFW indicator, we consider only the unbalanced sample as in the balanced sample both �1; �2 are not signi...cant and there are too few observations.

> 29 <u>2</u> Con...dence intervals of<sup><u>�</u>computedusingtheStatacommandnlcom.Calculationsfollows</sup> �1<sup>are</sup> the delta method, a method based on Taylor series expansions used for deriving variance approximations and con...dence intervals for transformed variables.

25
Figure 2.a. Simulation of a marginal increase in high-skilled emigration (PR) <!-- Start of picture text -->
-1 0 1 2 3 4<br>  zs<br>8<br>6<br>4<br>kdensity zs<br>2<br>0<br><!-- End of picture text -->

Legend: Kernel density of zs. Vertical continuous lines = mean value of<sup><u>�2</u>Verticaldashedlines</sup> �1<sup>.</sup> = con...dence interval at 90 percent (thick lines for unbalanced panel, thin lines for balanced panel) Figure 2.b. Simulation of a marginal increase in skilled emigration (CL) <!-- Start of picture text -->
-1 0 1 2 3 4<br>  zs<br>8<br>6<br>4<br>kdensity zs<br>2<br>0<br><!-- End of picture text -->

Legend: Kernel density of zs. Vertical continuous lines = mean value of<sup><u>�2</u>Verticaldashedlines</sup> �1<sup>.</sup> = con...dence interval at 90 percent (thick lines for unbalanced panel, thin lines for balanced panel) 26
Figure 2.c. Simulation of a marginal increase in skilled emigration (Polity2) <!-- Start of picture text -->
-1 0 1 2 3 4 5 6<br>  zs<br>8<br>6<br>4<br>kdensity zs<br>2<br>0<br><!-- End of picture text -->

Legend: Kernel density of zs. Vertical continuous lines = mean value of<sup><u>�2</u>Verticaldashedlines</sup> �1<sup>.</sup> = con...dence interval at 90 percent (thick lines for unbalanced panel, thin lines for balanced panel) Figure 2.d. Simulation of a marginal increase in skilled emigration (EFW) <!-- Start of picture text -->
-1 0 1 2 3 4<br>  zs<br>8<br>6<br>4<br>kdensity zs<br>2<br>0<br><!-- End of picture text -->

Legend: Kernel density of zs. Vertical continuous lines = mean value of<sup><u>�2</u>Verticaldashedlines</sup> �1<sup>.</sup> = con...dence interval at 90 percent obtained with the unbalanced panel.

27
Turning to the second of our questions (i.e., which countries would lose/gain from having a non-selective emigration), we simulate the counterfactual quality of institutions obtained when the skilled emigration rate is set to be equal to the unskilled emigration rate. This assumption implies a decrease in the skilled emigration rate. Noting that: e and assuming ms = mu = m, we have: where and<sup>e</sup> h is the resulting share of skilled in the resident labor force. The change in institutional quality is given by: It is straightforward to see that �I < 0 if: or, similarly, if: Figures 3a to 3d show the kernel distribution of zI and vertical lines at values of <u>�2</u><sup>the4indicators(CL,PR,Polity2andEFW)intheunbalanced(thick</sup> �1<sup>for</sup> lines) and balanced (thin lines) samples. The results from this second simulation are similar to those of the ...rst exercise. The fact that the kernel distribution is almost completely to the left of the thresholds suggests an institutional gain for nearly all the countries in our sample from having positively selected migrants (i.e., the counterfactual simulation from equating migration propensities across education groups yields an institutional loss), however this e¤ect is not statistically signi...cant as the distribution lies between the upper and the lower bounds of the con...dence intervals.

28
Figure 3.a. Counterfactual simulation of the e¤ect of skilled emigration on institutions (ms ! mu) - PR <!-- Start of picture text -->
-1 0 1 2 3 4<br>  zI<br>8<br>6<br>4<br>kdensity zI<br>2<br>0<br><!-- End of picture text -->

Legend: Kernel density of zI . Vertical continuous lines = mean value of<sup><u>�2</u>Verticaldashedlines</sup> �1<sup>.</sup> = con...dence interval at 90 percent (thick lines for unbalanced panel, thin lines for balanced panel) Figure 3.b. Counterfactual simulation of the e¤ect of skilled emigration on institutions (ms ! mu) - CL <!-- Start of picture text -->
-1 0 1 2 3 4<br>  zI<br>8<br>6<br>4<br>kdensity zI<br>2<br>0<br><!-- End of picture text -->

Legend: Kernel density of zI . Vertical continuous lines = mean value of<sup><u>�2</u>Verticaldashedlines</sup> �1<sup>.</sup> = con...dence interval at 90 percent (thick lines for unbalanced panel, thin lines for balanced panel) 29
Figure 3.c. Counterfactual simulation of the e¤ect of skilled emigration on institutions (ms ! mu) - Polity2 <!-- Start of picture text -->
-1 0 1 2 3 4 5 6<br>  zI<br>8<br>6<br>4<br>kdensity zI<br>2<br>0<br><!-- End of picture text -->

Legend: Kernel density of zI . Vertical continuous lines = mean value of<sup><u>�2</u>Verticaldashedlines</sup> �1<sup>.</sup> = con...dence interval at 90 percent (thick lines for unbalanced panel, thin lines for balanced panel) Figure 3.d. Counterfactual simulation of the e¤ect of skilled emigration on institutions (ms ! mu) - EFW <!-- Start of picture text -->
-1 0 1 2 3 4<br>  zI<br>8<br>6<br>4<br>kdensity zI<br>2<br>0<br><!-- End of picture text -->

Legend: Kernel density of zI . Vertical continuous lines = mean value of<sup><u>�2</u>Verticaldashedlines</sup> �1<sup>.</sup> = con...dence interval at 90 percent obtained with the unbalanced panel.

30
In both simulations exercises, however, we have neglected any possible incentive (or "brain gain") e¤ects of migration on human capital formation. Following an important theoretical literature, such incentive e¤ects have been identi...ed in a series of recent micro (e.g., Gibson and McKenzie, 2011) and macro (Beine et al., 2008, 2010) empirical papers.<sup>30</sup> The last question we want to ask, therefore, is the following: which countries would lose/gain from a marginal increase in skilled emigration if incentive e¤ects were accounted for? If we assume there are additional incentives to invest in human capital when there is a positive di¤erential emigration probabilities for highly educated (which is an empirical regularity), then we should write: with H 0 = <u>dH</u><sup>and</sup> <u>dH</u> = � dms<sup>> 0</sup> dms<sup>:</sup><sup><u>ms</u></sup> H<sup>�mu</sup> The derivative of institutional quality with respect to skilled emigration now becomes: After some manipulations, it is easy to see that the marginal impact of skilled emigration on institutional quality will be positive (i.e., dmdIs<sup>> 0);if:</sup> To be able to simulate the marginal impact of an increase in skilled migration in a context of endogenous human capital, we need to give a value to �, the e¤ect of emigration on human capital formation. We will use several values for �, in particular � = 0:05 (closer to the point estimate in Beine, Docquier and Rapoport (2010): � = 0:054)<sup>31</sup> , � = 0:01, � = 0:10 (which correspond to the values of the lower and upper bounds of the 90 percent con...dence interval of the estimated point), and � = 0:23 which corresponds to the long-run elasticity of human capital formation to high-skill migration prospects.<sup>32</sup>

> 30See Docquier and Rapoport (2009) for a survey of this recent brain drain literature.

> 31Note that since this value is for the short-run elasticity of human capital formation to the di¤erential emigration probability, it can be seen as a conservative estimate.

> 32In unreported simulations, we also use the lower and upper bound of the 90 percent con...dence

31
As can be seen from Figures 4a to 4d, which simulate this condition for our four indicators, the kernel distribution shifts downward and to the left for higher values of �: We also include a 90 percent con...dence interval for the threshold<sup><u>�2</u></sup> �1 as we did in the previous simulations (dashed and thick lines for the unbalanced sample, dashed and thin lines for the balanced one). In the presence of incentive e¤ects on human capital, in the short-run the marginal e¤ect of skilled emigration on institutional quality now appears positive and signi...cant for a limited set of countries. For example, if we consider the Polity2 indicator (which has the lowest lower bound of con...dence intervals among all the 4 indicators) in the unbalanced sample and the kernel distribution with � = 0:05, the countries with a marginal positive e¤ect will be: Argentina, Brazil, Bulgaria, Indonesia, Namibia, Russia, Swaziland, Thailand, Turkey, Venezuela. If we consider the PR indicator instead we will have in addition to the previous ones: Bangladesh, Bolivia, Botswana, Burma, Chile, China, Costa Rica, Egypt, India, Lesotho, Lybia, Mexico, Paraguay, Peru, Syria. On the contrary, if we believe in major human capital enhancement e¤ects in the long-run, and we consider the kernel distribution with � = 0:23, the marginal e¤ect of skilled emigration on institutional quality becomes positive for many countries.<sup>33</sup>

# 4 Conclusion

Emigration a¤ects institutions in developing countries in many ways. By providing people with exit options and a safety-net through remittance income, emigration can lower incentives to voice internally and, eventually, delay democratic reform and political change; on the other hand, emigrants can voice from abroad and support diverse political groups and views at home; they can also contribute to the di¤usion of democratic values and norms, be it directly, through return migration and contacts with relatives, or indirectly, through their belonging to social networks connecting diasporas and home-country populations. Finally, since migration is a non-random interval of the long-run estimated elasticity, i.e. � = 0:06, and � = 0:4. See Table 13 of the Appendix for the list of countries in our sample and the simulation results country by country.

> 33Human capital incentive long-run e¤ects take about 50 years to operate (convergence = 20% per decade). We have to observe that the long-run elasticity is calculated considering estimations in Beine et al. (2010), where a beta-convergence model is estimated using OLS. We know that in this case the estimated beta convergence coe¢ cient may be biased. This may cause a larger magnitude of our long-run elasticity. At the same time, we have also to note that larger long-run elasticities were obtained for poor countries in Beine, Docquier and Oden-Defoort (2011), who use panel regressions.

32
process, emigration alters the composition of the home-country population on several dimensions (notably education and ethnicity) that can in turn a¤ect democracy at home.

In this paper we ...rst document these channels and then consider dynamic-panel regressions to investigate the overall impact of emigration on institutions in a large sample of developing countries. We ...nd that openness to migration (measured by the total emigration rate) contributes to improve institutional quality (as measured by standard indicators of democracy and economic freedom) in the migrants’origin countries. This result is robust to the use of balanced/unbalanced panels, to the exclusion of certain groups of countries (e.g., former socialist countries) or to accounting for the low-coverage of certain countries in our migration data. We also ...nd that human capital (measured by the share of tertiary educated in the resident labor force) has a positive and signi...cant e¤ect on institutional quality. Since skilled emigration both increases total emigration and reduces average human capital, this raises the question of whether some countries can achieve an institutional gain through a brain drain. To answer this question we rely on numerical simulations which show a positive but generally statistically insigni...cant e¤ect of skilled emigration. However, once we account for the fact that emigration prospects provide additional incentives to invest in human capital, then the e¤ect of skilled emigration on institutional quality becomes positive for a limited set of countries in the short run and for many countries in the longer run.

33
Figure 4.a. Simulation of a marginal increase in skilled emigration with incentive e¤ects (PR) <!-- Start of picture text -->
-40 -30 -20 -10 0<br>  zh<br>kdensity zh (delta=0.01) kdensity zh (delta=0.05)<br>kdensity zh ( delta =0.1) kdensity zh ( delta =0.23)<br>2<br>1.5<br>1<br>.5<br>0<br><!-- End of picture text -->

Legend: Kernel densities of zh computed with �=(0.01;0.05;0.10;0.23) Vertical continuous lines = mean value of <u>�2</u><sup>Verticaldashedlines=con...denceintervalat90percent(thicklinesforunbalancedpanel,thinlinesfor</sup> �1<sup>.</sup> balanced panel) Figure 4.b. Simulation of a marginal increase in skilled emigration with incentive e¤ects (CL) <!-- Start of picture text -->
-40 -30 -20 -10 0<br>  zh<br>kdensity zh (delta=0.01) kdensity zh (delta=0.05)<br>kdensity zh ( delta =0.1) kdensity zh ( delta =0.23)<br>2<br>1.5<br>1<br>.5<br>0<br><!-- End of picture text -->

Legend: Kernel densities of zh computed with �=(0.01;0.05;0.10; 0.23) Vertical continuous lines = mean value of <u>�2</u><sup>Verticaldashedlines=con...denceintervalat90percent(thicklinesforunbalancedpanel,thinlinesfor</sup> �1<sup>.</sup> balanced panel) 34
Figure 4.c. Simulation of a marginal increase in skilled emigration with incentive e¤ects (Polity2) <!-- Start of picture text -->
-40 -30 -20 -10 0<br>  zh<br>kdensity zh (delta=0.01) kdensity zh (delta=0.05)<br>kdensity zh ( delta =0.1) kdensity zh ( delta =0.23)<br>2<br>1.5<br>1<br>.5<br>0<br><!-- End of picture text -->

Legend: Kernel densities of zh computed with �=(0.01;0.05;0.10; 0.23) Vertical continuous lines = mean value of <u>�2</u><sup>Verticaldashedlines=con...denceintervalat90percent(thicklinesforunbalancedpanel,thinlinesfor</sup> �1<sup>.</sup> balanced panel) Figure 4.d. Simulation of a marginal increase in skilled emigration with incentive e¤ects (EFW) <!-- Start of picture text -->
-40 -30 -20 -10 0<br>  zh<br>kdensity zh (delta=0.01) kdensity zh (delta=0.05)<br>kdensity zh ( delta =0.1) kdensity zh ( delta =0.23)<br>2<br>1.5<br>1<br>.5<br>0<br><!-- End of picture text -->

Legend: Kernel densities of zh computed with �=(0.01;0.05;0.10; 0.23) Vertical continuous lines = mean value of <u>�2</u><sup>Verticaldashedlines=con...denceintervalat90percentobtainedwiththeunbalancedpanel.</sup> �1<sup>.</sup> 35