dataesr/scientific-paragraphs-categorization huggingface dataset:
Data The PREVAGAY survey was conducted in commercial gay venues in Paris in 2009  [6]. MSM were eligible for the survey if they were at least 18 years old, had had sex with men in the previous 12 months, and could read and speak French quite well. Eight hundred eighty-six (886) MSM reported socio-demographic data and sexual behavior. They categorized the venues they attended as "bar/clubs without backrooms" (clubs), "saunas with sex" (saunas) and "backrooms/darkrooms/videoclubs/sexclubs" (backrooms). For each participant, a blood sample was obtained concomitantly to test for HIV infection. We used logistic regression to analyze HIV serostatus (positive/negative) according to individual MSM characteristics including number of partners, risky anal intercourse, age and places visited to meet sexual partners.
Limitations We modeled casual sexual partners network according to venue type and on partner allocation in each venue. As such, our model did not account for other individual characteristics that can impact the risk of HIV infection, such as the type of sexual acts or use of prevention, nor on other characteristics affecting new partnerships formation such as age preference or knowledge of serological status. Indeed, individual characteristics will change how partnerships are made within venue types rather than between venues. Additional characteristics could be added to define more precisely the sexual network and the effect of PrEP. We did not use incidence data to calibrate the model, but only number of partners in the PREVAGAY study and the literature to document the natural history of infection.
For example condom use is reportedly decreasing which could affect transmission  [66]. Longitudinal surveys are needed to document how sexual behavior change over time. For this reason, we only assessed short term outcomes for PrEP efficicency. Last, real number of sexual contact made in different venues was unknown in our dataset and led us to arbitrary allocation rules. These were chosen with a view to explore different densities of contact between places, providing a sensitivity analysis to the effect of such rules. Allocating the same density to each subnetwork in a network with correlation at random was the only situation where results of heterogeneous and homogeneous coverage were similar. In other more realistic networks settings, we found similar qualitative effect of different PrEP coverage.
Natural minerals often have multiple functional surface groups, which makes the surface speciation more complex. In this context, this study has employed the aluminium oxide corundum (a-Al 2 O 3 ) as a model phase for reactive aluminol groups on the montmorillonite mineral surface. We have conducted batch sorption and desorption experiments to quantify the uptake of neptunium(V) by the minerals and the extent of desorption from the mineral surfaces, respectively. The neptunium(V) batch sorption data on montmorillonite has been modelled with the Diffuse Double-Layer model to extract complexation constant for the formed neptunium(V) surface species. Detailed information on the coordination environment of neptunium(V) on the mineral surfaces was obtained by Attenuated Total Reflection Fourier-Transform Infrared (ATR FT-IR) and X-ray absorption spectroscopies (XAS).
The spectra were collected at 15 K in fluorescence mode with gas-filled ionization chambers (I 0 and I ref ) and a 13-element Ge solid state detector (I F , Canberra). Energy calibration of the collected spectra was performed by the simultaneous measurement of reference Y foil (Y K-edge defined as 17038 eV at the first XANES inflection point). At least four spectra were collected for each sample and the obtained spectra were averaged for further data analysis. The acquired spectra were analysed according to a standard procedure  (Koningsberger and Prins, 1988)  on the programme WinXAS (version 3. 2)  (Ressler, 1998). EXAFS theoretical fitting was performed both in k-space (i. e. EXAFS oscillation spectra) and R-space (i. e. Fourier transforms: FTs). EXAFS theoretical phase and amplitude required for the theoretical fitting were calculated by the programme code FEFF 8.
20  (Ankudinov et al. , 1998)  based on the hypothetical cluster ''hydrated Np V O 2 + sorbed on gibbsite" employed in the study by Gu ¨ckel et al. (  2013 ) and  Virtanen et al. (2016). The threshold energy, E k=0 , was defined as the first XANES inflection point of each spectrum. The amplitude reduction factor, S 0 2 , was fixed at 0. 9, while the shifts in E k=0 were varied but constrained to be the same value for all the shells. XAS measurements were performed for the neptunium (V)-corundum samples only, due to a zirconium impurity in the natural montmorillonite mineral interfering with the Np EXAFS region. Thus, our XAS data is limited to investigations on the interaction of neptunium(V) with surface aluminol groups. On the montmorillonite surface, two functional groups, silanol and aluminol, are known to participate in metal adsorption.
Whether the pH-dependent complex in the circumneutral to slightly alkaline pH-range (species 2) is of outer-sphere character or alternatively bound to different surface groups than species 1 (e. g. silanol vs. aluminol), however, cannot be deduced from the surface complexation model. the ATR-FT IR investigations and N 2 -BET analyses, respectively. This research was financially supported by the European Atomic Energy community's Seventh Framework Programme (FP7/2007-2011) under grant agreement n°295487 and Finnish Research Programme on Nuclear Waste Management (KYT 2018). Additional funding from the German Ministry of Education and Research (BMBF), Project number 02NUK021CX, for travel costs is also acknowledged.
Materials and Methods The data for this article was derived from a survey conducted in Hanoi, Vietnam by a team of professional investigators from Vuong and Associates in September 2016. This study collected data on a range of socio-economic and demographic indicators. Participants were patients, chosen at random with no discriminatory criteria; response rates were approximately 83% (5 out of 6). The questions were direct and simple, and participants were instructed by the interviewer to ensure that each questionnaire was filled correctly. The average time taken to collect a questionnaire was 10-15 min. Investigators have been thoroughly trained in order not to interfere with data sampling. Data was extracted from the dataset of periodic general health examinations, which was collected and prepared by a data team from Vuong and Associates during September to November 2016.
Ethical standards of the survey were regulated in the license of V&A/07/2016  (12 September 2016). Raw data was first recorded in Excel (v. 2010; Microsoft, Redmond, WA, USA) and then executed in R (v3. 3. 1; Bell Labs, Murray Hill, NJ, USA). We acknowledge that the dataset is Hanoi-based and thus presents a major geographical limitation. A nationwide survey would conduct to a different dataset showing regional differences as well as shifting in behaviours. For the time being, such a survey would require resources beyond our capacity.
1. Measures for more details on the variable "SerQual"). The values of this variable, as well as each of its five sub-elements, were shown in the following table among other continuous variables. Table  2  presented the mean value, standard errors, and 95% confidence interval of key variables mentioned in the study. Healthcare service quality was evaluated by patients as a little more than acceptable, given its mean score of 3. 55/5 (95% CI = 3. 51-3. 59). Regarding remaining variables, BMI is at a normal level and the mean age is quite young, reflecting the reality of Vietnam's young population. Figure  1  provides other figures from the dataset. nearly two-thirds of the patients surveyed, health care quality in hospitals scored under 4 points (majorly from 2 to <4 points). While perception of public health was measured as a discrete variable, the quality of health care services as assessed by patients was considered a continuous variable within the scope of this study (refer to Section 2.
1. Measures for more details on the variable "SerQual"). The values of this variable, as well as each of its five sub-elements, were shown in the following table among other continuous variables. Table  2  presented the mean value, standard errors, and 95% confidence interval of key variables mentioned in the study. Healthcare service quality was evaluated by patients as a little more than acceptable, given its mean score of 3. 55/5 (95% CI = 3. 51-3. 59). Regarding remaining variables, BMI is at a normal level and the mean age is quite young, reflecting the reality of Vietnam's young population. Figure  1  provides other figures from the dataset.
Before the medical visit, the OHPs asked eligible workers to fill-in a selfadministered questionnaire to obtain sociodemographic information; during the visit, a second occupational questionnaire was administered face-to-face by the OHP. The computerized medical record system in each occupational health service was declared to the French National Commission for Data Protection. All the volunteer participants gave their informed consent to be enrolled and data were collected anonymously. Because we used anonymised data from routine medical visits, in 2013 according to French law, ethics approval was not required.
A two-sided p-value of less than 0. 05 was considered statistically significant in our study. Statistical power was estimated on the basis of a binomial test with unequal group sizes (ratio 1/4). In this case to detect an effect size of RR = 2 with 80% power at a significance level of 0. 05 and a control-group proportion at 5%, 1,245 pregnant workers were required. As the responses were relatively complete, analyses excluded missing data. All the statistical analyses were performed using STATA statistical software, version 14. 0 (Stata Corp, College Station, Texas, USA).
Results During the study time period, the number of workers recruited was 1,581 (Fig. 1 ). The number of cases excluded was 64 workers (non-valid files). Very few women refused to participate, with only 22 cases not included in the study. Thus, our final sample was composed of 1,495 workers. The mean of the proportion of missing data was 1. 8% per variable with two variables above 5%: deprivation (6. 2%) and job duration (6. 5%). Table  1  presents a description of the pregnant workers according to the occurrence of "at least one SL" before a pathological or legal prenatal leaves (Table  1 ). The proportion of "at least one SL" was 74. 9%. SLs were less frequent in the managers/supervisors group and in small companies (<50 workers). Workers with "non-fixed contracts", "pregnancy at risk" or ART had an increased proportion of SL.
Discussion In our study, the rate of SL in pregnant workers was very high. After adjustment, the cumulative index of occupational hazards for pregnancy was clearly associated with SL (for "at least one leave", according to duration and for "early leave") in a dose-response relationship. We also found deprivation, pregnancy at risk, ART, work-family conflicts, home-work commuting felt as difficult, and young age to be associated with a higher risk of SL. For some factors, the results varied according to the trimesters of pregnancy. Moreover, we observed that there were less SL in small companies or for non-fixed term contract to 2nd or 3rd trimester. The study has a number of strengths and limitations. Among its strengths, it is noteworthy that exposure data and outcomes were collected independently of each other.
Information on outcomes was based on retrospectively collected self-reported information which  may lead to errors with respect to both time of occurrence and duration. However, according to some studies, the duration from self-reported data tend to be shorter than those based on recorded data and agreement between self-reported and recorded days of absence decreased as the total number of days increased  [32, 33]. Consequently, our results tend to rather underestimate reality. Also we did not have access to medical records relating to maternity and information on "pregnancy at risk" was based on self-reporting by workers. There was no consensual definition and literature data on this variable are scarce  [34, 35]. In a report from the French National Authority for Health, the rate of "pregnancy at risk" was 20% versus 24.
Methods Participants A previous study from our team proposed a cut-off of stress using VAS in comparison with PSS14 of Cohen  [11]. We used the same methodology and we applied the gray zone approach. Workers were a random sample of workers from five occupational health centres in four different administrative regions in France. Those occupational health centres followed workers from private companies. Workers were recruited during annual work medical examinations. No consent was given because we used anonymous data from standard clinical records, and only access responses in questionnaires. The ethics committee from the university hospital of Clermont-Ferrand, France, assessed that there was no need for ethics approval.
Statistics It was difficult to propose sample size estimation according to literature in order to distinguish an at-risk population among stressed workers, and to establish a threshold over which action is urgently required, via the two cut-off points of the gray zone. Also, the sample size was limited to the available workers from several occupational health centres in different administrative regions in France. However, a posteriori statistical power calculation was proposed and is further clarified in the discussion. Statistical analysis was performed using R software (http://cran. r-project. org/) and Stata software, version 13 (StataCorp, College Station, TX, US). All tests were two-sided, with a Type I error set at an alpha level of 0. 05. Continuous data were expressed as means and standard deviations (SD) or as medians with interquartile ranges [IQR], and categorical parameters were reported as frequencies and relative percentages.
Participants We tested 500 workers (248 men, 252 women), aged 40±11 years, with a PSS14 score of 3. 8 ±1. 4 and a VAS score of 4. 0±2. 4. PSS14 and VAS were correlated (r = 0. 65; p<0. 001) (Fig  1 ). Nine (1. 8%) of the 500 participants had a PSS14 score !7. 2. Considering PSS14 as a binary variable (<7. 2 vs. !7. 2), there was a significant difference between gender (50. 3% men with a PSS14 <7. 2 vs. 11. 1% men with a PSS14 !7. 2, p<0. 05) The VAS score differed between those with a PSS14 <7. 2 (VAS = 3. 8 [2. 2-5. 5] compared with individuals with a PSS14 !7. 2, who had a VAS score of 8. 2 [7. 4-10. 0] (p<0. 001). In contrast, no significant differences were observed in age, education, professional roles, and occupational sectors (Table  1 ), as well as for occupations (Supplemental file S1 Database for complete list of occupations).
VAS of stress: A discriminant tool We confirmed with a larger dataset, the previous finding of a relationship between the VAS and the PSS14 of Cohen (r = 0. 65, p<0. 001 in the current study and r = 0. 68, p<0. 001 in a previous sample  [11] ). Results support the discriminative power of the VAS score to predict a PSS score !7. 2  [11]. Using three different methods to determine cut-off points, we retrieved an optimal VAS threshold of 6. 8 to predict a PSS score !7. 2, which is close to the threshold of 7. 0 previously reported in a smaller sample size  [11]. The gray zone approach: A three-zone analysis Despite confirmation that the VAS is a useful and valid tool for the assessment of stress by occupational physicians, the use of a gray zone shows the limitations of using a single cut-off point to support clinical application  [20].
93, with CI's lower limit greater than 0. 8 (95% CI: 0. 86-1. 00). Furthermore, with n = 311, n = 172 and n = 17 individuals, the statistical power was greater than 95% in order to show a difference between groups [0 to 5[, [5 to 8. 2] and] 8. 2 to 10] (respectively, 2. 49 ± 1. 38 vs. 6. 23 ± 0. 99 vs. 9. 38 ± 0. 70, using sampsi and power one-way commands of Stata software considering inflation of type I error due to multiple comparisons). This statistical power seemed satisfactory despite the imbalanced size of groups  [51]. Moreover, as indicated by Feise  [52] , it is necessary to focus not only on statistical significance, but also on the quality of the research within the study and the magnitude of improvement. Only a modest correlation was observed between the VAS and PSS14 scores (r = 0.
Acknowledgments: To  Lulu Busane , coordinator,  Dumisane Mzamane African Institute of Kidney Disease, Renal Unit, Chris Hani Baragwanath Academic Hospital, Soweto ,  Johannesburg , and to  Cathrine Nkhakhane Tjale , Senior Dietitian,  Department of Human Nutrition, Chris Hani Baragwanath Academic Hospital, Soweto, Johannesburg  for their critical help. To  Susan Finnel  for her careful English review. A preliminary study was presented at the  XVII International Congress on Nutrition and Metabolism in Renal Disease 6-10 May ,  2014 ,  Wurzburg ,  Germany , as a poster presentation. The poster received the award for the best poster in the dietitian section.
Searches We performed a methodological systematic review of all RCTs conducted in SSA and published from 1 January 2014 to 31 March 2015. We relied on a sample of RCTs that was used in a previous work which aimed to describe the epidemiology of RCTs in SSA  [13]. In brief, we searched for all reports of published RCTs indexed in PubMed, the Cochrane Central Register of Controlled Trials (CENTRAL) and the African Index Medicus (AIM) based on the Cochrane Highly Sensitive Search Strategy for identifying randomized trials  [14]  combined to a geographic search filter to identify RCTs in Africa  [15]. The core search string was varied depending on the database (see Additional file 2). The AIM database was developed by the World Health Organization (WHO) in collaboration with the Association for Health Information and Libraries in Africa (AHILA).
Data analysis We entered the details of initial and follow-up ratings of reports into a customized Excel database. All analyses involved the use of SAS for Windows 9. 3 (SAS Inst. , Cary, NC, USA). For each item assessed, and by intervention type, data were summarized descriptively as frequency and percentage or median and interquartile range (IQR). We performed a post hoc analysis, using a chi-square test for categorical data, to assess the link between the endorsement of CONSORT by journals and the completeness of intervention reporting (alpha = 0. 05).
Reports identification The screening process is described in Fig. 1. The search identified 1827 reports after removing duplicates. The initial screening excluded 1627 records. For the remaining 200 reports, the full-text articles were retrieved for analysis. We declared 79 reports ineligible because they concerned secondary analyses of primary RCT reports (81%, n = 64) or were conducted in northern Africa (19%, n = 15). Overall, 121 reports were included for data extraction. All the selected references are reported in the Additional file 3.
Acknowledgements We thank all the corresponding authors for additional data provided. We also thank  Clément Lazarus ,  Romana Haneef  and  Aïda Bafeta  (all from  Centre d'Épidémiologie Clinique, Hôpital Hôtel Dieu, Assistance Publique des Hôpitaux de Paris, Paris ) who participated in the confirmation of the report's eligibility and data extraction; as well as  Laura Smales  ( BioMedEditing, Toronto, Canada ) for editing this manuscript.
Background: A large state-wide tobacco survey was conducted using modified version of pretested, globally validated Global Adult Tobacco Survey (GATS) questionnaire in 2015-22016 in Tamil Nadu, India. Due to resource constrains, data collection was carrid out using paper-based questionnaires (unlike the GATS-India, 2009-2010, which used hand-held computer devices) while data entry was done using open access tools. The objective of this paper is to describe the process of data entry and assess its quality assurance and efficiency. Methods: In EpiData language, a variable is referred to as 'field' and a questionnaire (set of fields) as 'record'. EpiData software was used for double data entry with adequate checks followed by validation. Teamviewer was used for remote training and trouble shooting.
The EpiData databases (one each for each district and each zone in Chennai city) were housed in shared Dropbox folders, which enabled secure sharing of files and automatic back-up. Each database for a district/zone had separate file for data entry of household level and individual level questionnaire. Results: Of 32,945 households, there were 111,363 individuals aged ≥15 years. The average proportion of records with data entry errors for a district/zone in household level and individual level file was 4% and 24%, respectively. These are the errors that would have gone unnoticed if single entry was used. The median (inter-quartile range) time taken for double data entry for a single household level and individual level questionnaire was 30 (24, 40) s and 86 (64, 126) s, respectively. Conclusion: Efficient and quality-assured near-real-time data entry in a large sub-national tobacco survey was performed using innovative, resource-efficient use of open access tools.
Technical support for data entry was provided by The International Union Against Tuberculosis and Lung Disease (The Union), South-East Asia Office, New Delhi, India. Double data entry and validation is considered the gold standard for reducing data entry errors (quality assurance). In this, data are entered independently twice and the two databases are compared for discordances, followed by their resolution by referring to the original data collection forms  [3, 4]. To achieve this, we replicated a model of combining open-access tools for quality-assured data entry (previously described in an operational research setting) in a large sub-national tobacco survey (TNTS) in a resource-constrained setting  [5]. If this model of data entry proves to be quality-assured and efficient, then it has the potential to be replicated in other settings.
Data collection Under TNTS, each of the 31 districts was divided into urban and rural areas except Chennai city which was divided into 15 zones, each zone further divided into slum and non-slum areas. Data were collected from all the 31 districts of the state and 15 zones of Chennai city between March and November, 2015. Estimated sample size of 100,000 people was divided among urban and rural areas of districts and slum and non-slum areas of zones in Chennai city using Probability Proportional to Size sampling  [6]. Primary and secondary sampling units in rural areas were households and villages, respectively. Primary, secondary and tertiary sampling units in urban areas were households, census enumeration blocks and wards, respectively. All individuals (≥15 years), males and females, in the selected household were interviewed.
Open access tools We used the following three open access tools for coordinating data entry: EpiData, TeamViewer and Dropbox  [5]. EpiData was the software used for data entry and data appending/merging  [8]. In EpiData language, a variable is referred to as 'field' and a questionnaire (set of fields) as 'record'. EpiData triplet files used for data entry include a QES (QuEStionnaire) file containing data structure, REC (RECord) file where data entry is carried out and CHK (CHecK) file with data entry checks. TeamViewer was used for remote training and troubleshooting. Dropbox was used for near-real-time file sharing, storing and automatic back-up (Box 1).