dataesr/scientific-paragraphs-categorization huggingface dataset:
Furthermore, this analysis was performed with participants with all type of TB and was replicated in a subsample of participants with pulmonary TB only. Since data were provided by a longitudinal database, the estimates were presented as risk ratios (RR) and 95% confidence intervals (95%CI). Effect of cash transfer program on TB treatment outcome. People covered by governmental social programs of cash transfer must meet eligibility criteria, including low income and compliance with conditions related to education and health  [25]. However, this governmental benefit is not universal; there are some people who meet these criteria but are not beneficiaries of national cash transfer programs. As SINAN did not incorporate information about eligibility to social programs, non-beneficiaries of the cash transfer program are a heterogeneous group.
The average effect of being beneficiary of cash transfer program was estimated by propensity-score matching in a 1:1 ratio (we consider a pair of observations a match if the absolute difference in the propensity score was less than 0. 05)  [27, 28]. In this analysis, the outcomes were dichotomized as cured versus not cured and repeated for participants with pulmonary TB. The results were presented as coefficients, which are the difference between the effects for beneficiaries of cash transfer program compared to non-beneficiaries, and 95%CI. We also assessed whether assignment to DOT moderated the association of being a beneficiary of cash transfer program and cure rates of TB treatment. Sensitivity analyses. In addition, all analyses mentioned above were replicated using a dataset which included only individuals without any missing SINAN data (so, not subject to imputation).
Determinants of TB treatment outcome In a Brazilian longitudinal database of people newly diagnosed with TB in 2015, we identified several determinants of TB treatment outcomes. Among the total population with pulmonary TB only, males, older subjects, those with 5-8 years of schooling, blacks, those living in the Southeast and South region and urban areas were less likely to be cured. Also were less likely to be cured those not deprived of their freedom, homeless, who smoke tobacco, living with alcohol use disorder, substance abuse or drug abuse disorder, HIV AIDS, and those assigned to DOT. However, among the cash transfer group, the association disappeared among males, blacks, region of residence, not deprived of their freedom, and who smoke tobacco products. Previous assessment of SINAN database found similar associations among TB determinants  [16].
New variables such as tobacco smoking, drug or substance use disorder, homeless, healthcare worker and immigrant status were recently included in the SINAN dataset based on evidence of high vulnerability among these people. Our results reinforce the role of these determinants in Brazil. In general, studies evaluating the determinants of TB treatment outcome among beneficiaries of cash transfer programs are scarce. Torrens et. al. found, among people who were beneficiaries of BFP during TB treatment and after TB treatment, that cure was less likely in older subjects, illiterates, blacks, PLHIV/AIDS, those with unknown HIV status, and those not assigned to DOT  [14]. In our present study, the effect of some determinants of TB treatment outcome in the total population was not maintained in the cash transfer group, suggesting that there might be an indirect effect of governmental social programs of cash transfer on TB treatment outcome in agreement with previous evidence  [29].
To our knowledge, in Brazil, only two previous studies assessed the effect of a TB-sensitive program of cash transfer, the BFP, on TB treatment outcome  [13, 14]. In the first published study, an analysis using secondary data, the authors found a positive association between BFP and TB cure and thus hypothesized an indirect effect of BFP through changes in behaviors and response to treatment  [14]. The second study, based on a cohort of people with TB, estimated the average effect of being a BFP beneficiary on TB treatment outcomes and observed that the average effect for cure was 0. 076 (IC 95% 0. 037-0. 116), for default was -0. 070 (IC 95% -0. 105 --0. 036) and for death it was -0. 002 (IC 95% -0. 021-0. 017) [13]. Based on the same theoretical model to assess the direct effect of cash transfer, but using a secondary database, our study found similar results.
Directly observed therapy Evaluation based on the SINAN database with people notified with TB, in 2011, revealed that the DOT strategy targets vulnerable populations, as it is designed to do, and that it had an important impact on improving the TB cure rate in these populations  [37]. Our results, with data from 2015, suggest an impact of DOT on TB treatment outcome even higher, suggesting that the role of DOT should not be disregarded in the struggle for TB control. In agreement with previous findings  [13, 14] , our study showed that the direct effect of cash transfer was moderated by DOT, meaning that people not assigned to DOT had a higher direct effect of BFP. DOT improves the communication between health services and people with TB  [37]  and our hypothesis is that cash transfer benefit also work through this same mechanism.
Strengths and limitations The strengths of this study include the large longitudinal database with a countrywide sample, allowing a wide national representativeness. Moreover, we built the analytic models based on a rigorous theoretical model specific to Brazil and used multiple imputation techniques to deal with missing data. In spite of the known variation of missing data between states, and geographical regions, the reasons for such absence are related to health facilities characteristics, leading to a non-differential measurement error which was dealt with through multiple imputation. In the present study, we performed a sensitivity analysis to assess the likelihood of bias due to imputation by replicating our models with a dataset of people with completed information. Results with inclusive confidence intervals allow us to conclude that the main findings are consistent.
Acknowledgments. The authors thank for their support INSERM,  CNRS ,  AHO  ( Association Hémochromatose Ouest ),  FFAMH  ( Fédération Française des Associations de Malades de l'Hémochromatose ), and  AFeMERS (Association Fer-Métaux Essentiels-Recherche-Santé ). Links of interest. The authors declare no links of interest for this article.
The inorganic elements were monitored using a fully validated in-house ISO 17025-accredited method based on microwave digestion and inductively coupled plasma-mass spectrometry (ICP-MS) determination. The analytical methods used have already been described in detail  (Chevallier et al. , 2015; Guérin et al. , 2017 Guérin et al. , , 2018)). The separate contribution of common and infant foods to the total average elemental concentrations is given. We also compared our occurrence data with those from other international studies.
Statistical analysis and data management The descriptive statistics including the arithmetical means, standard deviation (SD), minimum (min), maximum (max) of samples of food categories were calculated using Microsoft Excel 2010 software. The management of left-censored (LC) data (results reported below the limit of detection (LOD) and/or LOQ) were managed by adapting the WHO recommendations (WHO, 2013), i. e. by using a lower-bound hypothesis (LB) and an upper-bound hypothesis (UB). Values lower than LOD were replaced by 0 under LB or by the LOD under UB, and values lower than the LOQ, but higher than the LOD were replaced by the LOD under LB or the LOQ under UB. Because mean LB and UB concentrations were generally quite similar or equal due to the low LOD/LOQ values in this study, we present and discuss the results according to the UB approach.
The LB results are available in the supplementary material (Table  SM-2 ). For each element, a mean value was calculated for infant foods and for common foods. Their sum represents 100% of the total element content in infant feeding. Then the percentage contribution (%) of each food type (i. e. infant foods and common foods) to the total element content was calculated. Moreover, we carried out statistical comparisons of the median element contamination values in infant and common foods and some of food categories. Given that the infant and common foods were composed of distinct food categories, that the sample populations were of different sizes and the non-normal distribution of the data, data analysis was performed using a non-parametric test on the median contamination values. Mann-Whitney and Kruskal-Wallis tests were applied for comparison of two or more groups, using StatGraphics Software Centurion XVI.
Acknowledgments This work was carried out in the framework of the  FolEA  project, which is part of the  ERA-Net «Developing African-European joint collaboration for Science and Technology» (ERAfrica) , financially supported by the  European Commission  under the 7 th  Framework Programme. The authors would like to thank  Dounia Gueye ,  Nelly Fioroni  and  Oboulbiga Bahanla Edwige  for their help with the experiments.
Assessment of Primary Exposure Drug use for hypertension was explicitly differentiated from other uses as previously reported. 3 At baseline and each follow-up, drug use during the preceding month was determined by interview, and the medications themselves were seen by the interviewer. The name of the medication was recorded, and all drugs were subsequently coded according to the Anatomic Therapeutic Chemical classification of the World Health Organization. 4 For approximately one-half of the 3C Study cohort, it was also possible to obtain additional data on medication use via database linkage with the French National Health Insurance System. Antihypertensive and lipid-lowering drugs were administered by primary care physicians outside the study. Participants' exposure to more than 1 blood pressure lowering drug was permitted because elderly patients often require combination therapy for hypertension.
Stage of chronic kidney disease was calculated from estimated glomerular filtration rate (mL/min/1. 73 m 2 ) according to the Guidelines of the National Kidney Foundation 6 ; stage 1 (!90), stage 2 (60e89), stage 3 (30e59), stage 4 (15e29), stage 5 (<15 or dialysis), as validated in a French population cohort. 7 Data about depression symptoms were collected during face-to-face interviews with the Center for Epidemiologic StudieseDepression scale. 8 enter for Epidemiologic StudieseDepression scores !16 are indicative of mild to severe depressive symptoms and was used as the cut-off here. The protocol and criteria used to define prevalent and incident stroke have been previously defined. 9 Stroke was confirmed if the participant had a new focal neurologic deficit of sudden onset attributable to a cerebrovascular event that persisted for more than 24 hours.
However, the latter survey is not publicly available and hence will not be used for the analysis presented below. In this study, we aim to compare the disability measures provided by these three nationally representative datasets and to do so by using an external standard, namely the WG definition of disability used in the Han-diVIH. More specifically, the following questions are addressed: What does each of these surveys measure as being a disability? Are there actually any differences in the adult disability prevalence that they measure? How do the different surveys observe the differentials among age, sex, education and socioeconomic groups? Are these differentials consistent across the surveys? Answering these questions is very important. In fact, although these surveys contain great quantities of socioeconomic and demographic information, it is hard to say how accurate and comparable they are in terms of the results that could be obtained from crossing this information with disability.
Data This study used four datasets. The first was the Third Population and Housing Census (3RGPH) dataset. This census was conducted in November 2005 by the Central Bureau of the Census and Population Studies (BUCREP) of the state of Cameroon with the aim of updating the sociodemographic characteristics of the population. In this study, we use the 10% sample of this census (1,772, 359 individuals) provided by Integrated Public Use Microdata Series (IPUMS) International  [21]. The second dataset that we used is the third Cameroonian Household survey (ECAM3), produced in 2007 by the Cameroon National Institute of Statistics (INS). The purpose of this survey was to update the economic conditions of the population and to evaluate the impact of major policies and programmes implemented to fight against poverty  [22].
Only this subsample of 35,177 individuals is analysed in this work. Finally, we used the Disability and HIV study (HandiVIH) data as a "gold standard" for our comparison purpose. HandiVIH is a study conducted by the French Research Institute for Sustainable Development (IRD) and the Cameroonian Institute for Demographic Research and Training (IFORD) in the city of Yaoundé between October 2014 and November 2015. The aim of this study was to provide quantitative and qualitative insight into the complex links between disability and HIV in order to help decisionmakers prioritise their interventions  [24]. HandiVIH used a two-phase random sampling method. During the first phase, people were screened for disability from the general population using the WG disability questionnaire. Some basic socioeconomic information was also collected.
In the second phase, their eligibility was confirmed for the interview. Only the screening dataset is used in our paper. One hundred seventy-seven enumeration areas in the town of Yaoundé were drawn from the national sampling framework that was provided by BUCREP, from each of which 200 households were randomly selected and all adults ages 15-49 were screened for disability. The sample was representative of the population of Yaoundé. Because HandiVIH is limited to adults aged 15-49, all the analyses of this paper are done for this age group only.
The variables age group, education, marital status and tercile of socioeconomic status (SES) are used as dependent variables to assess their associations with disability. The age group variable is a three-age-group categorical variable (15-24, 25-34 and 35-49 age groups). Education is a dummy variable taking the value 0 if the individual has no education or did not complete primary school and 1 if (s)he completed primary school or studied more years. The marital status indicates whether the individual is in a union or not. The SES for the 3RGPH and for HandiVIH surveys has been calculated from household assets using the principal component analysis method  [28]. That variable was provided with the DHS-MICS dataset and was calculated by the data producers using a similar methodology to that of the 3RGPH and HandiVIH  [23].
Our results confirm that researchers should exercise extreme caution when comparing surveys used to analyse the prevalence of disability, as they each use different tools. It is worth mentioning that because Cameroon has two official languages, French and English questionnaires were available for each of the four surveys and census. The language used was the one the interviewee felt more comfortable with. In addition, interviewers were allowed to translate the questions in local languages if the respondents were comfortable with none of the two official languages. The language used could impact the reporting of disability. DHS-MICS was the only survey to provide such information in the database and we found no statistical association between disability and the language of the questionnaire.
Availability of data and materials The 3RGPH data that were analysed during the current study are available in the IPUMS international repository at https://international. ipums. org/ international/index. shtml. The DHS-MICS data are available in the DHS Programme repository at https://dhsprogram. com/what-we-do/survey-Types/ dHs. cfm. The ECAM3 data are available from the INS upon reasonable request at http://www. statistics-cameroon. org/index. php. The HandiVIH data are available from the principal investigators Pierre Debeaudrap and Gervais Beninguisse upon reasonable request. Consent for publication Not applicable.
Materials The HEK293, LNCaP and PNT1A cells line used in this study were purchased from Life Technologies (Carlsbad, CA, USA, Cat. # R75007 and R71407), ATCC (Manassas, VA, USA, Cat. # CRL-1740) and SIGMA (Saint-Louis, MO, USA, Cat. # 95012614), respectively. The HEK293 cell line expressing Luc UGA/Gpx4 in a stable way was generated and validated in References  [15, 16, 22]. Fetal calf serum (FCS), cell culture media and supplements were purchased from Life Technologies. Transferrin, insulin, 3,5,3 -triiodothyronine, hydrocortisone, sodium selenite and sodium selenate were purchased from Sigma-Aldrich (Saint-Louis, MO, USA). Antibodies were purchased from Abcam (Cambridge, UK) (glutathione peroxidase-1 (Gpx1), #ab108429; glutathione peroxidase-4 Gpx4, #ab125066; thioredoxin reductase-1 (TxnRD1), #ab124954) and Sigma-Aldrich (thioredoxin reductase-2 (Txnrd2), #HPA003323; Actin, #A1978).
Protein Gels and Western Immunoblotting Equal protein amounts (20 µg) were separated in Bis-Tris NuPAGE Novex Midi Gels and transferred onto nitrocellulose membranes using iBlot®dry blotting system (Life Technologies). Membranes were probed with primary antibodies (as indicated) and HRP-conjugated anti-rabbit or anti-mouse secondary antibodies (Sigma, #A9044 and #A6154, respectively). The chemiluminescence signal was detected using the ECL select Western blotting detection kit (GE Healthcare, Chicago, IL, USA) and the PXi 4 CCD camera (Ozyme). Image acquisition and data quantifications were performed with the Syngene softwares, GeneSys and Genetools, respectively.
Funding: This research was funded by  Agence Nationale de la Recherche  ( ANR-09-BLAN-0048 , R. L. and L. C. ),  Institut National de la Santé et de la Recherche Médicale: INSERM (L. C. ) ,  Centre National de la Recherche Scientifique :  CNRS (ATIP program , L. C. ),  Ecole normale supérieure de Lyon: ENS lyon  ( Emerging  Project, L. C. ). J. S. (Jordan Sonet) was a recipient of a Ph. D. fellowship from the  Université de Pau et des Pays de l'Adour (UPPA).
Abstract: Serum ferritin concentration is the preferred biomarker to assess population iron status in the absence of inflammation. Interpretation of this biomarker is complicated in populations with a high burden of infection, however, because inflammation increases serum ferritin concentration independently of iron status. We aimed to compare estimates of iron status of Kenyan pregnant women, with circulating ferritin concentrations adjusted for inflammation using newly proposed methods by the BRINDA project, or using previously proposed adjustment methods. We re-analyzed data from pregnant Kenyan women living in a rural area where malaria is highly endemic (n = 470) or in an urban area (n = 402). As proposed by the BRINDA group, we adjusted individual ferritin concentration by internal regression for circulating concentrations of C-reactive protein (CRP) and α 1 -acid glycoprotein (AGP).
By contrast, α 1 -acid glycoprotein (AGP) increases and declines slowly with these events. To our knowledge, although the regression correction method proposed by the BRINDA group has been tested in children and women of reproductive age, no data have been reported so far on prevalence estimates of iron deficiency in pregnancy using this method. In this paper, we re-analyzed two datasets of Kenyan pregnant women-urban and rural-to assess to what extent this newly developed regression method adjusting for inflammation will change the assessment of ferritin concentrations and the prevalence of iron deficiency in pregnancy.
Materials and Methods Study design and population: We used data from studies that were conducted from 2011 to 2014 in two distinct regions in Kenya-a rural area (Kisumu County, Kisumu, Kenya; henceforth referred to as the Kisumu data), and an urban area (Nairobi County, Nairobi, Kenya; henceforth referred to as the Nairobi data). Plasmodium infection is highly endemic in the Kisumu study area but is uncommon in Nairobi study area due to its high altitude (around 1,650-1,800 m above sea level). In Nairobi, Plasmodium infection is mostly imported from other regions. The main results of these studies have been published elsewhere  [8, 9]. Rural area (Kisumu) data: The prenatal iron and malaria (PIMAL) study concerned a randomized placebo-controlled trial to measure the effect of antenatal iron supplementation on maternal Plasmodium infection risk, and maternal and neonatal outcomes at delivery and one-month post-partum.
For the current study, we used data from samples collected at baseline. The study was conducted in the administrative areas of Ojolla, Kanyawegi, Osiri, and Rota Sub-Locations, Kisumu County, Kisumu, Kenya. Pregnant women were recruited when aged 15-45 years, with singleton pregnancies, gestational age 13-23 weeks (determined by obstetric ultrasonography), and hemoglobin concentration >90 g/L. Venous blood samples were collected in EDTA tubes. Plasma concentrations of ferritin, soluble transferrin receptor, transferrin, CRP, and AGP were assessed on a Beckman Coulter Unicel DxC 880i analyzer at Meander Medical Centre, Amersfoort, The Netherlands  [9]. For CRP, data below the assay limit of detection (LOD) of 1 mg/L were censored and reported by the laboratory as imputed values at LOD/2 (i.
The subjects recruited were sampled consecutively and proportionately to the daily turnover of women in their second pregnancy trimester for each of these three facilities, until the sample size for each facility was attained. Experienced research staff were trained on study-specific procedures of data collection, specimen handling, and analysis. Venous blood was collected in EDTA tubes. Plasmodium infection tests were done on site using rapid diagnostic tests specific for P. falciparum (histidine-rich protein 2). Serum concentrations of ferritin, soluble transferrin receptor, CRP, and AGP were measured by a multiplex enzyme immunoassay sandwich method with fluorescence detection  [10]. No limit of detection was reported for CRP. Sample size requirements were calculated for the original purposes of each study and not reported because they are irrelevant to the present article.
Ethics and Registration The PIMAL study was approved by independent ethics committees from London School of Hygiene and Tropical Medicine, UK, and the Kenyatta National Hospital/University of Nairobi, Kenya. It was registered at Clinicaltrials. gov (identifier: NCT 01308112). For re-analysis of the Kisumu data for the current article, the authors obtained additional approval from the Kenyatta National Hospital/University of Nairobi Ethical Review Board. The MNS 2014 study was approved by the Kenya Medical Research Institute Scientific and Ethics Review Unit (KEMRI/CPHR/SERU/2769www. kemri. org) and the Aga Khan University Research Ethics Committee (2014/REC-53). Written informed consent was obtained from all study subjects in both studies.
Statistical Analysis The following data, collected in the second pregnancy trimester, were used for this article: Kisumu 2011-2013 data and Nairobi 2014 data. Statistical Package for Social Sciences (SPSS) software version 22 and SAS 9. 4 software (SAS Institute, Cary, NC, USA) were used for data analysis. As per recommendations by the BRINDA group, we used the Internal Regression Correction (IRC) approach  (10)  to adjust for inflammation using CRP and AGP. The IRC approach uses linear regression to adjust a biomarker by the concentration of CRP or AGP on a continuous scale and Plasmodium infection as a dichotomous variable. Ferritin concentration was log-transformed to normalize its distribution and to stabilize its variance, and concentrations of CRP and AGP concentrations were log-transformed under the assumption that this would linearize their relationship with the log-transformed ferritin concentration.