dataesr/scientific-paragraphs-categorization huggingface dataset:
This prevents from comparison between studies and hampers the conduct of meta-analyses. Nonetheless, validated scales exist such as the Morisky Medication Adherence Scale (MMAS, also known as Medication Adherence Questionnaire), which is the first published and the most commonly used adherence scale. [32, 33]. Though there is no gold standard scale for measuring adherence to medication, MMAS is very often recommended because it has a good reliability, is the quick to administer and score and has been validated in the broadest range of diseases  [34, 35]. Refill data from pharmacy administrative databases can also be useful for measuring medication adherence, but the analysis of such data need trained researchers to correctly defined and interpreted the adherence indicators  [36]. Future research should also attempt to clearly describe all the components of the intervention and to try to identify which specific component is necessary to enhance adherence.
Materials and Methods The study protocol was approved by the Australian Catholic University Human Research Ethics Committee (V2009-91) on December 18 th 2009 (S1 and S2 Texts). The authors confirm that all ongoing and related trials for this intervention are registered with the Australian New Zealand Clinical Trials Registry (Identifier: ACTRN12612001017819) and the CONSORT reporting guidelines for clinical trials were followed (S1 Table ). Data were collected between August 2010 and February 2012. Written informed consent was obtained from all participants.
Testing measures Survey data. A self-administered lifestyle survey was completed to provide data on (i) health status and medical conditions, (ii) nutrition (including alcohol consumption), and (iii) current physical activity habits. The lifestyle survey (S3 Text) was developed specifically for the study and validated using the process of face validation  [21]. Anthropometric assessment. Body composition was assessed via waist circumference (WC), hip circumference, body mass index (BMI), and body mass. WC was measured to the nearest 0. 1 cm in the horizontal plane at the level of the midpoint between the iliac crest and lower costal margin  [11]. For WC, CV = 1. 26%, ICC (3, 1) = 0. 986 and ME = 1. 34%, which equates to an error range of ± 2. 6 cm. Body mass was measured to the nearest 0. 1 kg using digital scales (Tanita, Tokyo, Japan), and height was estimated to the nearest 0.
Statistical analyses Data were analysed using IBM SPSS Statistics, Version 20 for Windows (SPSS Inc, Chicago IL). Data were tested for normal distribution  [33] , with log transformation performed on data not normally distributed. All data are presented as means ± standard deviation. Statistical significance was set at P 0. 05. A linear mixed-model analysis was used to calculate the differences between groups and across time for the intervention and control groups. Hedge's g effect size was used to assess the magnitude of effect. An effect size ! 0. 2 was considered small, ! 0. 5 medium, and ! 0. 8 large  [34]. Mean differences and 95% confidence intervals (CI) are reported. An additional linear mixed-model calculation was determined for only the participants in each group who started and completed the study.
Acknowledgements The authors thank two anonymous referees and the editor for their comments. The authors are also grateful to  Jean-Charles Rochet ,  Helmuth Cremer ,  Philippe Choné ,  Claude Montmarquette ,  Laurent Linnemer ,  Laurent Flochel ,  Romain Lesur ,  Jorge Ferrando ,  Dan Kovenock ,  Anna Toldra ,  Elena Argentesi  and  Dario Maldonado  for their helpful comments.
Population selection and study design Between January 2008 and April 2012, 4192 older community-dwellers were recruited in 8 French Health Examination Centers (HEC) in Eastern France during a free and full medical examination. Sampling and data collection procedures have been described elsewhere in detail  [23]. The study was based on a cross-sectional design. The exclusion criteria were: inability to understand and speak French, an acute medical illness in the past 3 months; neurological diseases such as Parkinson's disease, cerebellar disease, myelopathy, peripheral neuropathy; major orthopedic diagnoses (e. g. , osteoarthritis) involving the lumbar vertebra, pelvis or lower extremities, inability to walk 6 meters unassisted and being younger than 65 years of age. The exclusion criteria for the present analysis were: missing values, dementia, depression symptoms defined as a score of the 4-item geriatric depression scale (GDS) 1, institutionalization and the use of walking aids  [24].
Clinical and Gait Assessment Clinical assessment corresponded to a full medical examination along with collecting age, gender, and measures of height and weight. The number of drug classes taken daily was also recorded. Body mass index (BMI, in kg/m 2 ) was calculated based on anthropometry measurements (i. e. , weight in kilograms and height in meters). The maximal isometric voluntary contraction (MVC) strength of hand was measured with computerized hydraulic dynamometers (Martin Vigorimeter, Medizin Tecnik, Tutlingen, Germany). The test was performed three times with the dominant arm. The mean value of MVC of all trials was used in the present data analysis. Distance binocular vision was measured at 5 m with a standard Monoyer letter chart and score from 0 (i. e. , worst performance) to 10 (i.
e. , best performance)  [27]. Vision was assessed with corrective lenses on if needed. Lower-limb proprioception was evaluated with a graduated tuning fork placed on the tibial tuberosity measuring vibration threshold  [28]. The participants were asked to indicate when the vibration stimulus was felt for the first time (perception threshold) and when this stimulus disappeared (disappearance threshold). The latter value was used in our study and ranged between 0 (i. e. , worst performance) to 8 (i. e. , best performance). The mean value obtained for the left and right sides was used in the present data analysis. Cognition was evaluated with two cognitive tests. First, the S-MMSE was used to explore the episodic memory  [25]. Its score ranged from 0 (i. e. , worst performance) to 6 (i. e. , best performance) and a score 5 was considered as impairment in episodic memory performance  [25].
Second, multiple linear regression analyses were performed to examine the association between TUG scores (i. e. , pTUG, iTUG and delta TUG) used as the dependent variables and the previous 15 subgroups of individuals with impairments in subsystems (i. e. , muscle strength, distance vision, lower limb proprioception and cognition) used as the independent variables adjusted on participants' clinical characteristics (i. e. , age, gender, number of drug classes daily taken and BMI). P-values less than 0. 05 were considered as statistically significant for the linear regression analyses. All statistics were performed using SPSS (version 19. 0; SPSS, Inc. , Chicago, IL).
In this aim, it is necessary to have at disposal an analytical age-dependent model of CSF. Unfortunately, to our best knowledge, such a model does not exist. Since CSF data are nevertheless available at different ages, this paper aims at building such a CSF model upon them. In the following, we first review the prior works, which are dealing with the decline of CSF with age. Then, we extend Barten's analytical model of the CSF  [17] , which is based on vision mechanisms, in order to propose an age-dependent CSF. In Section 3, we describe Barten's model and focus in Section 4 on the optical and neural factors which can possibly 2 The Scientific World Journal contribute to the contrast sensitivity decline with age. In Sections 5 and 6, we propose an age-dependent CSF model with the same structure as Barten's age-independent model.
In the photopic domain, the photon conversion factor is set to  = 1. 285 in the following, as in  [17]. The Scientific World Journal 4. 2. 1. Quantum Efficiency. The quantum efficiency is the rate of photons which activate photoreceptors  [49]. Van  Meeteren measured values as low as 2%  [50]. Due to the increasing scattering in ocular media with age, one may expect that the quantum efficiency depends on age. Moreover,  may refer to rods or cone quantum efficiency; Barten only takes into account the cone quantum efficiency, which is set to  = 3% in his model  [17]. Very few studies have associated  with age. Hallett has estimated a range of rod quantum efficiency from 0. 17 to 0. 48%  [51] , but these results are discussed by Bennett et al. [52]. We found these data too sparse to build a quantitative age-dependent model on it.
We also used Gao's data for  = 45 ∘ , as well as Curcio's data  [44]  (see Figure  2 ). The cone density is estimated as 𝑁 𝑐 (𝐴, 𝑒) = (6952. 7 -38. 70𝐴) 𝑒 -0. 35𝑒 + 300. ( 17 ) The cone density in the fovea is different from Barten's model, which was based on experimental data, where the observer's age was not reported  [67] [68] [69].
They were split into three groups with mean ages of 30, 50, and 70 years ( = 94). The adaptation luminance was set to 100 cd/m 2 , with 5. 5 ∘ of field of view. The data was recorded in binocular vision. In Tulunay-Keesey's experiment, the 63 observers were aged from 10 to 70 years  [66]. They were split into six groups with mean ages of  17, 25, 34, 45, 54 , and 62 years. The adaptation luminance was 60 cd/m 2 , with 7. 0 ∘ of field of view. The data was recorded monocular vision. In Elliott's experiment, the 24 observers were split into two groups with mean ages of 23 and 69 years  [21]. The adaptation luminance was 300 cd/m 2 , with 7. 0 ∘ of field of view, and data was recorded in monocular vision. In order to estimate the best parameter values according to these data, we used a Lagrangian optimization, implemented in Matlab.
Statistical analyses. We detailed and evaluated the postures and behaviours of NB from the start of the recording until someone touched or spoke to them. Thus these interruptions caused important interindividual variations in the durations of recorded time suitable for analysis (table 1). Therefore, we did not compare raw numbers of occurrences (scans) but we compared percentages of scans presenting each item. Percentages cited in the text represent the median [range] of the data set. Data were analysed with non-parametric statistics, using R. All tests were twotailed. When data could be obtained for an item concerning both sides of the NB (hand posture for instance), we investigated side effect. As none could be evidenced (Wilcoxon tests, P. 0. 05 for all comparisons), data for both sides were pooled for further analyses.
Acknowledgments We warmly thank the babies and their parents who accepted to participate to this study, as well as the  NICU  staff for their help. We also thank  Ann Cloarec  for helping with the spelling and writing in English and  Emmanuel de Margerie  for the pictures of the different baby clothing. Financial support was provided by  GIS ''Cerveau-Comportement-Societe'' , the  CNRS , the  University of Rennes 1  and the  CHU Morvan at Brest.
Study setting The Africa Centre for Health and Population Studies has hosted a socio-demographic household surveillance in a rural sub-district of uMkhanyakude in northern KwaZulu-Natal (South Africa) since 2000. The surveillance area is 438 km 2 in size and includes a population of approximately 90 000 isiZulu-speaking people  [1]. The study area is characterized by high adult HIV prevalence (24% in adults aged 15 years and older in 2011) and high levels of poverty and unemployment (in 2010, 67% of adults over the age of 18 were unemployed). At any point in time, about one-third of the population under demographic surveillance does not physically reside in the surveillance area, although they are considered to be household members (membership is defined by household head). Demographic events and socio-economic data are collected on a regular basis from a key household informant.
Starting in 2003, a nested HIV surveillance was conducted among resident adults, who were invited to respond to a health and sexual behaviour questionnaire and to provide a small blood sample which was tested for HIV  [14]. For each survey round, teams of two trained fieldworkers visited each eligible individual in their households. If a person was absent, the field workers made up to four repeat visits to the same household. Except for the first HIV surveillance round, which took place over 18 months starting in 2003, all subsequent rounds were done on annual basis. For this analysis, we used data collected between 2003 and 2012, corresponding to a total of nine survey rounds.
Eligibility to participate in HIV surveillance All adults residing in the area and who were able to provide informed written consent were eligible to participate in HIV surveillance. From 2003 to 2006, eligibility was restricted to women aged 15-49 years and men aged 15-54. From 2007 onwards, all persons aged 15 years and older were eligible. The population of eligible resident participants changes substantially on a yearly basis. Thus from 2004 onwards, at the beginning of each calendar year, a list of all resident persons eligible to participate in HIV surveillance was generated from information available in the demographic database. During fieldwork operations, some persons became ineligible "a posteriori", because the information of death, out-migration or sickness was not available at the time the eligibility list was generated or because their situation changed.
Dissimilarity between sequences was calculated using optimal matching techniques before dividing the population into several groups (participation profiles) using hierarchical classification and describing participation sequences classes. We used the Longest Common Subsequence (LCS) distance to compute distances between sequences (see example on  Fig 1). LCS distance is a special case of optimal matching distance  [38]. A dendrogram was computed using the Wald algorithm. We used the higher relative loss of inertia criterion to determine the optimal number of partitions (see function HCPC in FactoMineR package  [39, 40] ). We used odds ratio as effect size indicator to describe participation profiles. Sankey diagrams (flow diagrams in which the thickness of the lines is proportional to the flow quantity) were used to represent the dynamic of the eligible population over time and the participation dynamic by sequence position of each participation profile.
All statistical analyses were performed using R 3. 0. 1  [41]. Sankey diagrams were constructed using an adapted version of Mike Bostock's script for D3. js (http://bost. ocks. org/mike/sankey/). Sequence analysis was performed using the TraMineR package  [42]. Color palettes were chosen from http://colorbrewer2. org/ to be colorblind safe. All figures were edited with Inkscape 0. 48. Although the effective HIV surveillance participation rate in any single survey round might appear to be low, it is important to consider multiple recruitment opportunities in a longitudinal setting. Thus, cumulatively after five rounds, 68% of all eligible persons participated at least once, 48% at least twice and 31% at least three times (Fig  4 ). Due to the fact that a minimum of one blood sample is required for estimating HIV prevalence and two blood samples for HIV  incidence, only two-thirds of the sample was used for prevalence and half of the sample for incidence estimation.
Funding for the  Africa Centre's Demographic Surveillance Information System and Population-based HIV Survey  was received from the  Wellcome Trust, UK  (grants  065377/2/01/B  and  082384/Z/07/Z ). JL was supported by the  Institut de Recherche pour le Développement (IRD)  and JM received partial financial support from the  German government through the Centre for International Migration and Development (CIM). TB has been supported by the  Wellcome Trust  and by  NIH  and by grant  1R01-HD058482-01  from the  National Institute of Child Health and Human Development. Bärnighausen and Marie-Louise Newell are PLOS ONE  Editorial Board members. However,.
Acknowledgements This article is part of a special collection on stepped wedge trials. Contributions from LSHTM authors form part the work of the  LSHTM Centre for Evaluation , which aims to improve the design and conduct of public health evaluations through the development, application and dissemination of rigorous methods, and to facilitate the use of robust evidence to inform policy and practice decisions. We thank other members of our writing group, including  James Hargreaves ,  Katherine Fielding ,  Rumana Omar ,  Gianluca Baio ,  Jennifer Thompson ,  Sam Ononge ,  Calum Davey  and  Emma Beard , for their input during the development of this article. We received no dedicated project funding for this work. D Osrin  is funded through a  Wellcome Trust Senior Research Fellowship in Clinical Science  ( 091561/Z/10/Z ).
Data Collection A structured questionnaire was administered face-to-face, in the official language (French) and/or in national languages (Lingala or Kutumba). All questionnaires were completed by the medical personnel conducting the interviews. The following data were collected: socio-demographic circumstances, domestic characteristics (age, gender, occupation, residence, size of household, type of house, water resource, usage of mosquito nets), environmental characteristics (animal contacts and/or consumption), travel outside the country during their lifetime, history of haemorrhagic fever (in family or personal). Serum Venous blood samples were drawn using two 4 mL plain tubes which were immediately centrifuged. Sera were kept at -80°C until use. Aliquots were inactivated at 56°C for 30 min and transferred to the Virology Laboratory of the Bernhard-Nocht-Institut (BNI) in Hamburg for serological assays.
Statistical Analysis Statistical analyses were performed using the IBM SPSS statistic 21 software. Analyses aiming at analysing risk factors for seropositivity included univariate, stratified and multivariate analyses. The Fisher's exact test was used to compare proportions in univariate analysis and the ANOVA test to compare means. The Pearson's test was used for stratified analysis. All statistical analyses were performed at the 95% confidence level. The association between anti-EBOV IgG seropositivity and risk factors was determined by binary logistic regression analysis. Stratified analysis based on sex, age and area were performed. The significant variables in univariate analysis were entered in the multivariate model. The quality of the multivariate model was assessed with Hosmer-Lemeshow's test.
Acknowledgments The authors are deeply indebted to the personnel of the  Centre National de Transfusion Sanguine  for their collaboration and assistance, to  Dr. Stephan Becker  ( Institute of Virology, University of Marburg ) for providing the anti-NP-Ebola mouse monoclonal antibody, to  Corinna Thome-Bolduan  ( Bernhard Nocht Institute for Tropical Medicine, Hamburg, Germany ) for technical assistance during serological analyses and to  Anderson Loundou  ( Faculty of Medicine, Marseille, France ) for technical assistance in database management. We acknowledge a contribution from the  EU 7th Framework Predemics  Project-Agreement No. 278433.
Methods and data The analysis of physicians' migrations between Romania and France is mainly based on the results of a survey carried out in 2011 and 2012, and consisting in close and open-ended questions, the latter providing participants with the possibility to comment on some points, heightening the qualitative side of the study. In total, 182 Romanian physicians practising in the West of France (n= 75), Alsace and Lorraine (n= 72), as well as in Paris (n= 35) were interviewed. Western France is interesting for the key issue of the shortage of physicians in rural areas and small towns. In Alsace and Lorraine, the Romanian doctors represent a particularly important part of the total of physicians. In Paris, which is the gateway for many migrants to France, the grouping of all hospitals in the APHP (the Public Hospitals of Paris) facilitates access to employment for Romanian doctors.
The gender distribution (male: 55, female: n: 127) is fully representative: women represent 70% of all Romanian physicians practising in France. At the same time, the average age was 38. 6, the group 31-40 being best represented with 63. 8% of the total number of doctors; finally 54% were living in France with their family. A snowball technique of sampling was used. Building upon data provided by national health and social affairs institutions (ADELI file from the French ministry for social affairs and health which give information on each healthcare professional: civil status, professional situation, activities carried out) and relating to the more interesting places for the study, we first contacted Romanian physicians in several hospitals, asking each respondent to give us the names of other Romanian physicians working in the same or an other hospital in France, as well in office practices.
Data recording Balance control was assessed using two force platforms (AMTI, model BP400600NC-1000, Watertown, MA, USA) and upper body kinematics was recorded using an electromagnetic system (Polhemus-model Liberty 240/8, Colchester, VT, USA). In order to track upper body kinematics, three sensors were attached to each participant; one on the sacrum (L5/S1), one on the seventh cervical vertebra (C7) and one on the forehead (H). A microcontroller (model Basic Stamp BS2px, Parallax, Rocklin, CA, USA) controlled the timing of all equipment. Data were acquired through a digital-to-analogue data acquisition board (model PCI-6224-16 bit, National Instruments, Austin, TX, USA) using custom-made software developed in Matlab (MathWorks, Natick, MA, USA).
Data analysis To assess postural control, the root mean square (RMS) values of the C7 horizontal displacement was calculated for each interval. To single out balance control resulting from a pure vestibulomotor response versus from the sensorimotor integration of vestibular and proprioceptive information, during the vestibular stimulation epoch, the sum of the lateral force (net lateral force) was studied during two intervals. For instance, the vestibulomotor response (pure feedforward vestibular reaction) was calculated from the impulse of the net lateral force (i. e. , time integration of the net lateral force) from 320 ms to 500 ms after the GVS onset. This period was chosen because it occurred before noticeable movements of the head and torso were observed. Consequently, this initial motor response is probably purely vestibular in origin  [31, 32].
The quotas also ensured that the control group had the same distribution as the overall population for the number of children aged o15 years living in the household, conditional on age. Like the cases, children who had been adopted, or whose biological mother had died or did not speak French were not eligible as controls. In all, 747 of the 803 eligible CL cases (93%) including 714 cases of ALL and 1421 of the 1662 eligible controls (86%) participated in the ESTELLE study. Data collection. The same trained interviewers carried out the interviews with the cases' and controls' mothers using structured questionnaires with computer-assisted telephone interviewing). The cases' mothers were interviewed on average 6 months after diagnosis. The questionnaire elicited information on demographic and socioeconomic characteristics, childhood environment and lifestyle, family and personal medical history, maternal reproductive history and child-care history as determined by maternal statements, the mother's reading of her child's health-care record, or both sources.