dataesr/scientific-paragraphs-categorization huggingface dataset:
Procedures, content and study design The study was conducted over a 20-week period during the midphase of the competitive season. This mid-season phase was used for the assessment as to ensure minimal fitness changes and subsequent metric changes per training sessions. Only daily analysis from training weeks situated within a 1-game week has been used within the study in order to track the training demands across the 20 microcycle phases. Players included within the data collection were only inclusive of players who had performed greater than 80 min of the competitive match-play at the end of the analysed week. For the reliability and validity of the study, only data from players who performed the full session duration have been used, withdrawing the data from players whose TL was manipulated during this time due to fatigue management or injury.
Training assessment Throughout the investigation, a total number of 80 training session data were collected for assessment and analysis. The data assessed included 20 microcycles consisting of 1-week blocks of full training sessions per player: 20 × MD-4, 20 × MD-3, 20 × MD-2, 20 × MD-1. No other data pre-MD-4 were considered for analysis as they did not have any specific on pitch content of adequate TL. All training sessions within the investigation period were played on an outdoor grass training field with an average temperature of 10. 2 ± 3. 11°C. Goalkeeper's data were excluded from the study and the data analysis. All players were fully familiarised with the use of GPS units worn throughout the investigation. During the investigation, all training sessions were preceded by a standardised warm-up period of 15 min prior to the initiation of the training session.
Load management analysis (GPS data) Developing a multimodal daily and weekly score for both volume and intensity markers in order to represent as both individual and collective load values, a contemporary mechanical load management analysis technique was devised incorporating four volume (TDC; HSR; SpD; SumA:D) and four intensity (TDC. min; HSR. min; SpD. min; SumA:D. min) GPS metrics. In order to attain the daily volume and intensity scores, average individual player data were pooled (i. e. , as shown in the below calculation) to provide a squad average to create an initial session metric outcome score (Table  1 ). The mean individual data assessed were then compared to the average maximum individual competitive match-play metric achieved and reported as a percentage figure. The percentage volume and intensity of the session were generated through the following calculation:.
Results The results are expressed as mean ± standard deviation and all variables were reported followed a normal distribution (P < 0. 05). Differences were found between training days (TDs), and between TDs and competitive MD data in all metrics used and assessed in addition to differences highlighted between days for both volume and intensity session scores (P < 0. 05). Session scores for MD were significantly higher than MD-1 (ES: range 0. 98-1. 34), MD-2 (0. 99-1. 34), MD-3 (0. 41-0. 50) and MD-4 (0. 71-1. 07); MD-3 significantly higher than MD-1 (0. 71-1. 09), MD-2 (0. 74-1. 10) and MD-4 (0. 40-0. 75); MD-4 significantly higher than MD-1 (0. 28-0. 36) and MD-2 (0. 33-0. 42); however, no differences were found between MD-1 and MD-2 (Figure  1 ). Furthermore, each individual day was significantly different in %SumA:D (0.
Background: Chiropractors are primarily concerned with musculoskeletal disorders but have the responsibility to deal also with prevention in other areas. Objectives: To establish the prevalence of chiropractors who have a positive opinion on the use of primary prevention (PP), their actual use of PP, and the proportion of patients who consult for PP in relation to (i) musculoskeletal disorders, (ii) public health issues, or (iii) chiropractic treatment for wellness. Method: A systematic search for literature was done using PubMed, Embase, Index to Chiropractic Literature, and Google Scholar and updated on February 15th 2017. Inclusion criteria were: surveys on chiropractors and/or chiropractic patients, information had to be present on PP in relation to the percentage of patients who consult for PP in chiropractic practice or in a chiropractic student clinic, and/or the percentage of chiropractors who reported using PP, and/or information on chiropractors' opinions of the use of PP, in the English, French, or Scandinavian languages.
Data extraction The information in the selected articles was reviewed in relation to two elements: 1/quality (i. e. representativeness and validity) and 2/results. Three checklists were designed for those aspects. Our requirements were lenient. We did not check contents of references to trace additional or missing information. We sought our information in the methods and result sections but not from the abstract or title. A score was given to each selected article regarding various quality aspects and reported as a percentage. This score was used to determine the weak and strong points in this research field but also to classify the articles in descending order based on their individual total quality score. One point was given for correct answers. When the answer was incorrect or missing, it was given a score of 0.
Analysis and presentations of data Assessment of the articles was done using the checklists independently by two of the authors, after which their respective checklists were compared, followed by a discussion on unclear points. Such queries were always resolved, because usually different interpretations of articles arose from difficulties in finding the relevant text. The articles were arranged in descending order in relation to their classification and their final quality score with a colour-coding of the three subgroups (i. e. 'good' , 'acceptable' , and 'unacceptable'). Results (Table  4 ) were thereafter interpreted for each of the three main concepts of PP (musculoskeletal, public health and wellness) in relation to the three main study objectives of the study. When interpreting the results we disregarded the studies that we considered to be of unacceptable quality.
However, it is possible that we failed to retrieve some relevant surveys on this topic. In the chiropractic field, some professional journals exist that are 'invisible' when searching through the usual library sources. We initially searched two medical databases (PubMed and Embase) later completed with Index to Chiropractic Literature and Google Scholar. This approach added two articles, but we could have missed out on some other relevant work, assuming that they could have been traceable through other library databases. As we did not explicitly search the grey literature, we would have missed surveys published by such media but, probably, studies not published through the peer-review process would have a relatively low methodological standard, which would limit their usefulness. For this review, we were unable to obtain three of the articles found through the literature search, which, potentially, were lost from the review.
Time-frequency analyses: We then analyzed the time-frequency decomposition of each ECoG trial  [55]  using BESA 1 software (BESA GmbH, Gra ¨felfing, Germany;  [56] ). Analyses of evoked responses only detect electrical activity that is precisely time-locked to the stimuli, whereas time-frequency analyses may detect more variable responses, such as bursts induced by the stimulus. Time-frequency analyses indicate which frequencies present the highest powers at specific points in time and space and how their phase angles synchronize across time and space. Because ECoG rhythms are themselves the product of synchronized activity among and within neuronal assemblies, it is often assumed that changes in ECoG power reflect underlying changes in neuronal synchrony. Time-frequency displays, which represent the change in amplitude over time (TFR, Time-Frequency Representation), were generated from the single trials by averaging spectral density amplitudes over trials and normalizing to the baseline for each frequency and each channel.
05) in neighboring time-points, channels and frequencies. To test the probability of significance of these clusters, the null distribution was computed from the data by randomly assigning the condition label to either of the two conditions and performing the same computation of statistic clusters for each of 1000 permutations. Finally, the cluster pvalue was determined by ranking the observed cluster relative to the distribution of surrogate clusters determined with the permutations. Optical data. Optical data were band-pass filtered [0. 03-0. 5 Hz] using a zero-phase filter (Butterworth, order: 6) to eliminate physiological noise (e. g. slow drifts, arterial pulse oscillations). HbO and Hb signals were segmented relative to the onset of each block (-5 to +25s). After applying a linear detrend and baseline correction, the segments were averaged by condition (3 conditions) and channel (8 channels) in each rat (average number of blocks per condition and channel are 35/34/35 for ST/DV/DP).
Relationship between the initial hemodynamic dip and the DC component in ECoG To study the relationship between the initial hemodynamic response and the slow shift of ECoG signal, the area under the curve of the initial HbO dip [0 to 4 sec, across all conditions] and the ECoG amplitude envelope (Hilbert transformed) were computed. We then calculated correlation coefficients across all eight channels for the combined hemodynamic and electrical datasets. A highly significant correlation [r =. 95 (p <. 0001)] was observed for channel 4 (Fig  6 ).
Hippocampal Adult Neurogenesis Is Normal in U-Exposed Rats Proliferation of hippocampal newborn granule cells was quantified in 2-month-old rats from the U-exposed and control dams. Our data revealed that U-exposed rats exhibited similar numbers and spatial distribution of BrdU-positive proliferative cells as compared with controls (Figure  2 ). In addition, we quantified the proportion of BrdU/NeuN co-labeling cells. We used confocal microscopy to count the percentage of double-or single-labeled BrdU-positive cells in the dentate gyrus (DG) and found no statistical difference between exposed and non-exposed groups (control: 95. 1%; U 40: 94. 9%; U 120: 95. 6%; Figure  S1 ). Based on these results, cell proliferation and neuronal differentiation seemed to be preserved in exposed animals as compared with controls.
Acknowledgments: We thank  Frederic Voyer ,  Thierry Loiseau  and  Jean-Michel Guischet  for animal care,  Valérie Holler  for help with analysis of confocal microscopy and  Johanna Stefani  for her technical help. We also thank  Chrystelle Ibanez ,  Karine Tack  and  Per Eriksson  for their expert advice. This study was part of the  ENVIRHOM research program  supported by the  Institute for Radioprotection and Nuclear Safety (IRSN).
Data This study uses data collected during the 2010 Burkina Faso Demographic and Health Survey (DHS), the first nationally-representative survey in Burkina Faso to collect information on previous HIV testing among both women and men. The survey protocol has been published elsewhere  [26]. Briefly, the survey used a stratified, two-stage cluster sampling design. The country was stratified into rural and urban areas. Among each stratum, the first stage consisted of a random sample of clusters (primary sampling unit, PSU) using sampling probabilities proportional to the number of households in the cluster. Clusters were established by a general population and housing census conducted in 1996 (the average cluster populations were 1000 and 1200 in rural and urban areas, respectively). The second stage involved the systematic sampling of households from the selected clusters.
Two multilevel models were fitted for both gender. The first multilevel model adjusted for individual-level variables and each of the main community-level determinants hypothesized to be related to the community variation in HIV testing separately: 2010 HIV prevalence, knowledge about VCT service, HIV/AIDS knowledge and HIV related stigma (model 1). The second multilevel model is fully adjusted for all individual-level and community-level variables enumerated above (model 2). Analyses were restricted to participants reporting having ever had sexual intercourse. All analyses were stratified by gender because attitudes toward HIV testing are likely to vary between women and men  [32, 33]. Statistical analyses were performed using the R statistical software and the "geepack" package was used to fit the regression models  [34].
1  Uptake of HIV testing in Burkina Faso. Proportion of a women and b men that reported having ever been tested for HIV in the country's 13 administrative regions in 2010. (Map is our own)   were found to be high: only 7% of women and 5% of men expressed no stigmatizing attitudes about PLWH. We acknowledge some limitations in this study. The measures used in this paper were self-reported and therefore susceptible to social desirability biases. The use of cross-sectional data also makes the temporal sequences between some covariates and testing uptake in this study unknowns. Furthermore, communities were defined based on PSU memberships. Because social networks do not necessarily follow the dimensions of a PSU, we might have under or overestimated effect size measures of the community-level determinants.
In this paper, we present results using newly available information from the English Longitudinal Study of Ageing (ELSA) linked to administrative data on earnings since 1975 and employment since 1948. With these data, which have not previously been exploited, we can compute measures of lifetime earnings based on a very long panel and relate ratios of wealth to lifetime earnings to the distribution of lifetime earnings. When we use lifetime earnings per year worked as a proxy for earning ability, we find that the ratio of private wealth (i. e. wealth excluding state pension wealth) to lifetime earnings increases monotonically with lifetime earnings, consistent with the conjecture that the 'rich save more'. Even when state pension wealth is included, the top quintile of lifetime earnings exhibits significantly higher wealth to lifetime earnings ratios than the other quintiles.
Data The data we use is a newly available data set based on the linkage of the English ageing survey, ELSA, to administrative data from the UK National Insurance (NI) system. We discuss each in turn. ELSA is a biennial longitudinal survey of a representative sample of the English household population aged 50 and over (plus their partners). The first wave was conducted between April 2002 and March 2003 and sampled 11,391 individuals from 7,934 households. ELSA collects a wide range of information on individuals' circumstances. This includes detailed measures of their financial situation: income from all sources (including earnings, self-employment income, benefits and pensions), non-pension wealth (including the type and amount of financial assets, property, business assets and antiques) and private pension wealth (including information on past contributions and details of current scheme rules).
ELSA also collects information on individuals' physical and mental health, cognitive ability, social participation and expectations of future events (such as surviving to some older age or receiving an inheritance). As complements to our main results, we explore below some interesting associations between wealth accumulation and some of these variables. ELSA has been linked to NI records, which are administrative data collected by the UK government since 1948 in order to keep track of individuals' contributions to the social insurance system and establish their entitlement to benefits, such as state pensions. 4 ELSA respondents were asked for permission to link to their NI records. Among respondents to the 2002-3 wave of ELSA, 79% gave permission for a link to be made to their NI records and 71.
There are 1,937 couples in the first wave of ELSA in which the oldest member was born between 1927 and 1942. For 1,157 of these couples we have linked administrative data on both partners' past earnings. The NI records do not record income of the self-employed; therefore, we exclude from our analysis any couples in which one individual had more than five years in which they paid self-employed NI contributions-this results in us dropping 129 couples. Finally, there are five couples for whom we do not observe full information on wealth or the other covariates of interest. These restrictions yield a sample of 1,023 couples for which we have detailed information on both wealth at retirement and earnings during their lifetime. We examine the relationship between lifetime earnings and a variety of wealth concepts (in 2002/3) 7.
First, we measure total private wealth excluding state pension wealth, including wealth from private pensions, owner-occupied housing, other property, business assets and financial assets. Wealth is the measured net of outstanding secured and unsecured debts. Second, we compute a broader measure of total wealth including state pension wealth, computed as the present discounted value of the future stream of pension income to which an individual is entitled. 8  Turning to the construction of a measure of total lifetime earnings, while our administrative data contains rich and unexploited data, it has three limitations. First, earnings are recorded only if they were above a certain minimum level. This level, the 'Lower Earnings Limit' was equal to £75 per week (£3,900 a year) in our most recent year of data-and over the period covered by our microdata was normally located at about the 10th percentile of the (positive) distribution of earnings.
Acknowledgements We thank  James Banks ,  Richard Blundell ,  Thomas F. Crossley ,  Peter Diamond ,  Richard Disney ,  Michael Hurd ,  Tullio Jappelli ,  Paul Johnson ,  Guy Laroque ,  David Wise ,  Stephen Zeldes , two anonymous referees as well as seminar participants at the  NBER Summer Institute  for useful comments. Responsibility for interpretation of the data, as well as for any errors, is the authors' alone.
Funding This work was supported by the  IFS Retirement Saving Consortium ; the  Economic and Social Research Council  ( 'Centre for the Microeconomic Analysis of Public Policy ' [grant reference:  ES/ M010147/1 ] and  Secondary Data Analysis Initiative Grant 'Adequacy and Optimality of Retirement Provision :  Household Behaviour  and the  Design of Pensions ' [grant reference:  ES/ N011872/1 ] to COD); and the  European Research Council  [grant reference:  ERC-2010-AdG Grant  Agreement Number 269440 -WSCWTBDS] to AB and COD. The  English Longitudinal Study of Ageing (ELSA)  is funded by the  National Institute on Aging  and a consortium of UK government departments.
Participants Participants were phone operators working in the emergency dispatch center of the Mercy Regional Hospital Centre (CHR) of Metz-Thionville, France. Participants were recruited in May 2014 and we obtained complete data by October 2014. We recruited both men and women to better represent the whole team of medical dispatchers. Exclusion criteria were psychiatric disorders including depressive symptoms > 8 on the Hospital and Anxiety Scale  [26] , recent extraprofessional life stress event (such as death of a near relative, divorce)  [27] , alcohol consumption > 3 drinks per day for men and > 2 for women  [28] , endocrine disorder  [29] , oral contraceptive  [25, 30]  and pregnancy  [31] , any medications used to modulate inflammatory diseases taken over the previous three months (corticosteroids, anti-inflammatory drugs, immunomodulatory drugs)  [32] , intensive sports > 3 hours per week of intense physical activity  [33] , and any current illness/infection  [34]  at the time of measurements (feeling feverish sensations or having hyperthermia above 38.
5˚C) [35]. The protocol was approved by the Human Ethics Committee of the University Hospital of Nancy, France (Clinical Trials identifier NCT02075424). The study was explained to the phone operators, who provided their written informed consent. We did not exclude non-menopausal women because basal cortisol levels do not differ during the menstrual cycle  [31]. In addition, studies involving work stress and cortisol levels in acute care settings have mainly involved women  [36, 37, 38, 39].
Shift randomization For each phone operator, we measured outcomes during a control day and during the three types of shifts: Incoming emergency call, Dispatch and Re-assessment. Latin squares were used to randomize first the order between Incoming emergency call and control day. The Incoming emergency call shift was always before the two other types of shifts. However, after measurements were made during the Incoming emergency call shift, Latin squares were used to randomize the pattern of shifts between Dispatch and Re-assessment. All outcome data remained blinded until the end of the study.
Statistics The sample size calculation was estimated on the basis of a previous study by members of our team  [6]  which showed a 22. 8% increase in cortisol levels in emergency medical dispatchers compared with control participants. Following the recommendations of Cohen  [46] , who has defined effect-size bounds as small (ES: 0. 2), medium (ES: 0. 5) and large (ES: 0. 8, "'grossly perceptible and therefore large"), we decided to include 22 participants to evidence an effect-size equals 0. 7 at +120min for a two-sided type I-error at 0. 017 (correction due to multiple comparisons), a statistical power of 80%, and within subject variability at 0. 5 (due to the experimental design). Statistical analyses were performed with Stata software (version 13, StataCorp, College Station, TX, US). Data were presented as mean ± standard deviation (SD).
Participants We recruited 22 phone operators, out of a potential pool of 28 (Fig  1 ). We obtained complete data for 22 of the 22 phone operators. They were aged 36. 4+/-10. 8 years (14 women aged 37. 9+/-10. 7 years, 8 men aged 33. 8+/-11. 2 years). Men and women did not differ in age (p =. 35) but female emergency medical dispatchers had greater experience: 86% of the women had a >5 year experience as against 25% of the men, p =. 004. None of the participants were taking routine medications and none took occasional medications during the study. No participant reported not having lunch before cortisol measurements during shifts.
We considered a single variable 'depression', recoded with these three modalities (history of depression, current state of depression, never depression). We coded as a "current state of depression" any patient with both a history of depression and a current state of depression at baseline. Between-group comparisons of distributions for categorical data (Richmond tests, Prochaska and DiClemente) were done with the Chi 2 test. Student's t test was used to compare means (number of cigarettes; Fagerstro ¨m). Multivariate logistic regression was used to investigate the association between abstinence and other factors. To check the absence of collinearity, we computed correlation coefficients for all pairs of variables. All variables were included in one step. The variable « duration of the longest temporary abstinence » was excluded due to the absence of convergence of the iterative process of estimation.
ACKNOwLeDgMeNTS This research was funded by the Vinci Foundation, the MAIF Foundation, and the Henri Laborit Hospital Center. The authors wish to thank Dr. Rizk for providing language help as well as valuable comments on the manuscript. They also wish to thank Dr. Marcelli and his colleagues for providing them with the original version of the questionnaire used in this research and Mr. Vincent, head of the documentation center at the Henri Laborit Hospital Center, who gave them full access to major references.