dataesr/scientific-paragraphs-categorization huggingface dataset:
Illustration of outcomes The dataset provided allows analysis and comparisons of the food days across the countries based on the computation of the distribution of meals or food intakes according to the spatiality of their preparation and incorporation and their sociality as well as their temporal distribution across the time of the day. A usual statistical approach to the analysis of the variance can be applied. Figure  4  illustrates the important contrast regarding the distribution of the spatiality of food between Singapore and France-where the percentages of meals purchased out of home and either consumed at home or out of home are 50 and 13. 5%, respectively. The comparison between the temporal distribution of food intakes eaten out in Indonesia and Malaysia presented in Figure  5  shows the difference in terms of the percentage of breakfast eaten out or the synchronization of the lunch eaten out where 35% of the Indonesian population eaten out at noon while 21% does in Malaysia.
In view of future data collections, the data collected   from early 2020 offers a baseline on food practices prior to the COVID-19 pandemic and related lockdowns. Limitations could possibly be found in the representativeness of the national samples in relation to the online collection, and the invisibility of some fluctuations in one's definition of what is home and out of home, for example, in the case of eating to another's-i. e. , friend, neighbor, and family-home. Nonetheless, the analysis of the "Eating Out" dataset by researchers, public and private decision-makers, and students could benefit the food (service) industry to understand the organization of the demand of the food market, public health, as a complement to nutritional surveys in designing policies focusing on the food environment.
Construction of recombinant Lactococcus lactis (pExu:gdf11) All DNA manipulations were performed following  Sambrook and Russel (2001)  protocols. To construct the eukaryotic expression vector pExu:gdf11 the coding sequence of murine gdf11 (GenBank accession number: NM_010272. 2) was acquired in commercial plasmid pCloneEZ-NRS-Blunt-Amp:gdf11, and digested with restriction enzymes BamHI (10 units) and NotI (20 units) for obtaining a 1,241 bp DNA fragment. Simultaneously, the plasmid pExu was digested with the same enzymes. DNA insert and vector were purified after running an agarose gel electrophoresis using Illustra TM GFXTM PCR DNA kit (GE Healthcare, Chicago, IL, USA) following manufacturer instructions, and the molecular ligation step was performed with T4 DNA ligase (Invitrogen, Carlsbad, CA, USA) for 16 h at 4 • C.
, 1996). Results were presented as a total sum of all parameters per animal per group. Posteriorly, image acquisition was performed with a 20x magnification objective using Olympus BX41 (Tokyo, Japan) to measure 20 villi and 20 crypts randomly selected per animal per group to measure crypt depth and villi height. Images were analyzed using ImageJ software (NIH, Bethesda, MD, USA). The assessment of goblet cells was performed in PAS-stained slides, where 10 field/slides were counted with a 40x magnification objective utilizing ImageJ software, and results were presented as average cells per field per group of animals.
Statistical analysis All statistical analyses were performed with GraphPad Prism 8. 0 software. Data normality was assessed utilizing the Shapiro-Wilk test. Non-parametric data were submitted to Kruskal-Wallis analysis and Dunn's post-hoc test. Standard distribution data were submitted to one-way ANOVA following Tukey's post-test. Statistical differences were considered using a p-value < 0. 05.
Background The role of metals and trace elements in the progression of cancer can be both passive and active. While some metals have clearly emerged as carcinogens, the homeostasis of other trace elements only trails cancer evolution and therefore offers some potential prognostic values. At this stage, modern-standard datasets including a large number of elements are missing. The present analysis established a rst metallomic spectrum by relating the blood concentration of metals and trace elements in patients with sarcoma with survival data.
Methods Patients with sarcoma and controls were retrospectively selected from the International Sarcoma Kindred Study database. Blood samples were prospectively collected at the Leon Bérard Cancer Center from February 2012 to July 2019. Stable specimens and copper isotopes (65Cu/63Cu) were analyzed using Triple Quadrupole ICP-MS and the MC-ICP-MS Nu Plasma HR 500. Wilcoxon rank sum test, logrank test, and multivariate Cox regression models were used for statistics.
Population For this case-control study, patients and their relatives healthy controls were retrospectively selected from the ISKS database  (17). Brie y, ISKS is a biological, epidemiological, and clinical resource active across four continents with more than 3500 families participating, established in Australia in 2009. The main goal of this resource is to investigate the role of heritable events in sarcoma and set up an international sarcoma database and biobank (18). From the ISKS patients  (19) , we included those who had been treated for sarcoma at the Leon Berard Cancer Center and died from the disease before January 31, 2020, as well as their respective healthy controls who had no history of cancer, in this retrospective study. The study was conducted in accordance with the guidelines of the Declaration of Helsinki and was approved by the Institutional Review Board, through the local data protection o cer, on behalf of French data protection authorities (Commission Nationale de l'Informatique et des Libertés, CNIL) in accordance with the MR004 methodology.
Data collection Patients' clinical history (date of diagnosis, age at diagnosis, sex, date of death), tumor characteristics (sarcoma subtype, location, grade and stage) and treatment information (type of treatment, date of treatment administration, ongoing systemic or local treatment) were collected from electronic medical records, hospitalization and pharmacy records. In particular, the date of blood samples collection for the purpose of the ISKS was recorded. Patients who had completed systemic or local treatment for localized disease more than one year ago were considered to be in follow-up, while those who had not received any therapy within the last three months were considered to be free of systemic or local treatments. It should be noted that all diagnoses were con rmed by sarcoma expert pathologists of NETSARC + network, who conducted a central review  (20).
Acknowledgements We thank the  ITMO Cancer et IReSP  in the context of « Plan Cancer 2014-2019 » for the NETSARC prospective national cohort on the link between genetics and sarcoma,  Liddy SHRIVER  for the project  « International Sarcoma Kindred Study » , the  Fondation ARC  for the project " Genetic susceptibility to response to treatment among sarcoma patients ",  Info Sarcomes  for the project " VAPS: Vehicles , Association , and  Progression in Sarcoma ", the  Ligue Nationale Contre le Cancer  for the project " Next generation sequencing for the identi cation of sarcoma susceptibility alleles in the French component of the International Sarcoma Kindred Study ", and the  Ligue contre le   Cancer Rhône  pour le projet «  Predictive factors for early mortality in patients  with sarcoma».
Sensory characterisation The flavour of the 28 wine samples was characterised using a labelled sorting task. To evaluate the generalisability of our results, three sorting tasks were performed on three sets of wines, with different expected sensory variability. The results obtained for the three sets were similar, with three dimensional solutions showing stress values of 0. 150, 0. 169 and 0. 150 for set 1, set 2 and set 3 respectively (data not shown). Figure  1  shows the dendrograms derived from the cluster analysis calculated with all the MDS dimensions obtained from the three sorting tasks. Figure  1 (a) shows the results for Sorting Task 1 (S1), which consisted of grouping a total of 10 wines (half NWs and half CWs), with all sharing their origin (Catalonia). The hierarchical cluster analysis shows the presence of three main groups of wines differing in their sensory profile.
ACKNOWLEDGEMENTS This work was supported by the  Spanish Plan of Innovation , Technical and Scientific Research 2017-2020through the programs funded by  AEI  and  MICIU: Ramón y Cajal  ( RYC2018-024025-I for EPD  and  RYC2019-027995-I for MPSN ) and  Juan de la Cierva-Incorporación  ( IJC2018-037830-I  for MB), and the  Spanish Ministry of Science and Innovation , the  Spanish Research Agency  and  FEDER  (projects:  PID2021-126272OA-I00 ,  PID2021-126031OB-C21  and  PID2021-126031OB-C22 ). The manuscript was proof-edited by  Guido Jones , currently funded by the  Cabildo de Tenerife , under the  TFinnova Programme  supported by  MEDI  and FDCAN funds.
| M E T H O D S 2. 1 | Patients Patients were included in the ELDER-BIOME study (clinicaltrials. gov identifier NCT02928367)  [6, 16]  or through the Amsterdam UMC COVID-19 biobank. We prospectively enrolled COVID-19 patients admitted to the ward, in 2 hospitals in The Netherlands (Amsterdam UMC, location Academic Medical Center  [AMC] , in Amsterdam and the Flevo Hospital in Almere), between October 2020 and December 2021. SARS-CoV-2 infection was confirmed by polymerase chain reaction of material obtained by nasopharyngeal swab. Patients using antiplatelet drugs were excluded from the current analyses. Clinical characteristics were recorded as part of standard care, until 90 days after admission. Controls were hospital employees or patients visiting the outpatient clinic without infectious disease symptoms.
Data were analyzed using Bruker TASQ 2. 1. 22. 3 software (Bruker Daltonic). For metabolomics, all metabolites LÉOPOLD ET AL. - 3 of 18   were standardized to internal controls and to total protein content in samples, determined using a Pierce BCA Protein Assay Kit. For fluxomics, 13 C enrichment was calculated based on mass distribution isotopomer analysis; results were corrected for their natural 13 C abundance by solving the associated set of linear equations using nonnegative least squares  [22, 23]. Metabolite measurements are semi-quantitative, expressed in arbitrary units (calculated using peak areas that are corrected for internal standards and protein content) and not in absolute concentration  [20]. Only direct comparisons of metabolites within samples were performed. Differences between groups were determined using Mann-Whitney U-test and metabolite levels were considered different in case of a P value <.
Together these data suggest that the loss of platelet ΔΨm is due to mitochondrial dysfunction rather than loss of mitochondrial mass. Mitochondria go through morphologic changes during platelets' short life  [13, 33]. Diverse pathologic and physiological conditions can  LÉOPOLD ET AL. -7 of 18 of multi-subunit protein complexes, responsible for ΔΨm generation and ATP production, of which the subunits are encoded by either nuclear or mitochondrial DNA (mtDNA)  [35]. Publicly available platelet transcriptomics data from COVID-19 patients (NCBI sequence read archives PRJNA63448)  [5]  further pointed at mitochondrial dysfunction: in an analysis of metabolic pathways using the reactome database  [17]  the only significantly differentially regulated pathway was "respiratory electron transport, ATP synthesis by chemiosmotic coupling, and heat production by uncoupling proteins" (Id: R-HSA-163200.
Methods Participants and data. We used prospective, longitudinal data from the Karonga HDSS in northern Malawi. The HDSS is situated in the southern part of the Karonga District and includes 42,000 individuals living in 7000 households  24, 25. Most of the population lives in rural areas, and a majority of them engage in subsistence farming, fishing, and trading. The HDSS undertakes continuous demographic surveillance in the area to collect socioeconomic, demographic, and household-level data and information on vital events and migration of individuals of all ages  26. It started with a baseline census between 2002 and 2004. Births to women in the baseline survey were reported, and field staff enrolled the children as part of the demographic surveillance follow-up visits  27. Data were collected on maternal and child characteristics, including child anthropometry, birth characteristics, breastfeeding and other feeding practices, and household socioeconomic status when the children were 0-3 months old.
The birth cohort was revisited at age 12 months, and the feeding data and other infant and family characteristics were updated. Annual surveys and re-census were conducted in the HDSS to periodically update existing data and collect new information, including children's schooling, anthropometry, and vital events. For the present analysis, we restricted the study population to birth cohort members between the ages of six and 13 (primary school age in Malawi) with at least one data point on current primary school grade. In Malawi, school enrolment at public primary schools is free, and children do not have to pass an entrance examination to enrol in school  24. Study measures. Outcome variable. The main outcome of this study was age-for-grade, defined as the age at which a child would be expected to enter a given grade if they had begun primary school on time and advanced without repeating or skipping a grade  28.
In this cohort, 96. 3% (n = 953) of the children started primary school at age six or earlier, 3. 4% (n = 34) started at age 7, and 0. 3% (n = 3) started at age 8, so age-for-grade was primarily a measure of progress. Information on the current grade of each child in the cohort was collected at multiple time points starting in 2007, when they were about four years old and updated annually until 2015, when they were about thirteen years old. Public primary schools in Malawi consist of eight grades, and children are expected to enter grade 1 at age six and continue for eight years until they complete grade eight at age thirteen. For example, children are expected to enter grades 5, 6, and 7 at ages 10, 11, and 12, respectively. We calculated age-for-grade based on whether a child was at, over, or under the official expected age for entry into a grade for all the time points for which data were available for a given child.
Data analysis. We estimated the number of children exclusively breastfed for 0-2 months, 3-5 months, and 6 months to determine the prevalence of exclusive breastfeeding. The characteristics of the children were summarised and stratified by the exclusive breastfeeding groups. Age-for-grade was recoded as a binary response variable with 1 = over-age for grade and 0 = underage/on-time for grade. Three sets of analyses were performed to determine the association between exclusive breastfeeding and age-for-grade. First, binary logistic regression was used to model the association between exclusive breastfeeding and being over-age for grade using one observation per child and restricting the analysis to schooling assessments at the point closest to age 11. 5 years (mid-point between 10 and 13), as most children had information on current grade at these ages.
We used the trajectory with better grade progression as the reference group. In all the analyses, we adjusted for the baseline confounders outlined in the directed acyclic graph in Fig. 2 , with these covariates included as categorical variables using the groupings presented in Table  1. All analyses were performed using Stata version 17. Missing data. The amount of data missing at baseline was low, ranging from 0. 3% (maternal education and maternal occupation) to 5. 4% (paternal occupation) (see online Supplementary Table  1 ). Missing data mechanisms of baseline confounding variables were investigated and assumed to be missing at random. We performed multiple imputations by chained equations (MICE) in Stata to minimise bias and loss of precision and power from discarding observations with missing values  47.
Thirty imputed datasets were generated under fifteen iterations for each imputation model. All variables in the substantive analyses were included in the imputation models to predict the distribution of the missing values. However, only six of the ten baseline confounding variables with missing data were imputed (maternal education, maternal occupation, paternal education, paternal occupation, household wealth, and birth order). We did not impute missing values in the outcome variable. The substantive analyses described above were conducted on the imputed dataset, and the estimates combined and standard errors estimated using Rubin's rules  48. For the multinomial logistic regression analysis, separate MICE models were fitted for the entire sample as well as for boys and girls. In sensitivity analysis, we repeated the binary logistic regression, multinomial logistic regression, and GEE analyses using only individuals with complete data to assess the reliability of our substantive analysis that used imputed data.
The order of births was associated with exclusive breastfeeding, with a greater percentage of children of higher birth order more likely to be exclusively breastfed for 6 months than those of lower birth order. Age-for-grade. Of the eight possible time points at which age-for-grade was assessed, 1. 9% had all eight recorded, 24. 1% had 7, 43. 3% had 6, and 13. 8% had 5, and the remainder had between one and four school assessments. At age six, data on age-for-grade was collected for 895 children. The number of children increased   3A ). The earliest children began to fall behind in school was age eight, and the proportion of children under-age or on time for grades steadily decreased. By age 13, no child was underage-for-grade, and 41. 9% of the children were 1 year older than their grade level.
Discussion We used prospective, longitudinal data to examine whether exclusive breastfeeding duration in the first 6 months after birth is associated with educational attainment and age-for-grade trajectories between ages 6 and 13. We saw some evidence of a reduced likelihood of over-age for grade in children exclusively breastfed for 6 months Age at school assessment compared to those exclusively breastfed for less than 3 months. Latent class growth analysis indicated that the effect was on those falling behind in the early grades of primary school rather than those who fell behind later. While the width of the confidence intervals and modest effects should be interpreted with caution, they are similar to the association found in the saving brains cohort in KwaZulu-Natal, South Africa, where researchers investigated the effects of exclusive breastfeeding on grade repetition in children aged 7-11 years  22.
Since data on exclusive breastfeeding duration were based on maternal recall, we cannot completely rule out the possibility of overreporting due to recall and social desirability bias. However, given that the data were collected in the first 3 months after birth and updated only a few months after the recommended duration for exclusive breastfeeding, any such effects should be minimal. Indeed, our estimated prevalence of Table  5. Multinomial logistic regression analysis of the association between exclusive breastfeeding duration and age-for-grade trajectories among children aged six to thirteen in Malawi. P-values are from the test for linear trend. Note: We controlled for child's sex, household wealth at birth, age of mother at birth, birth order of child, maternal HIV status, mother education, father education, mother occupation, father occupation, and distance to a tarmac road in the adjusted analysis.
OxyS and FnrS regulate iscR expression by binding to the iscR mRNA 5'UTR We used the in-silico structure prediction program Mfold to investigate the potential basepairing and mode of action of the sRNAs on the iscR mRNA  (48). This analysis showed that the 5' part of the iscR mRNA could form a stem-loop structure which may partially block the access of the ribosome to its binding site (Fig. 3A ). FnrS has previously been predicted and then experimentally confirmed to base-pair at the level the ribosome binding site (RBS) of the iscR mRNA, thus likely inhibiting ribosome access at this site, which is consistent with its repressing activity on iscR expression we observed (Fig. 3B )  (45). Interestingly, using Mfold, the OxyS sRNA was predicted to base-pair on the 5'-part of this stem loop structure, which could induce its opening and release the access of the RBS for the ribosome, consistent with an activating role of OxyS in the translation of iscR (Fig.
Acknowledgments We would like to thank  Gisela Storz  for providing strains and precious advices along the course of this study. We deeply thank  Ciaran Condon ,  Delphine Allouche ,  Jonathan Jagodnik  and  Noella Amiot  for help with EMSA experiments. We would like to thank also  Samuel Carien  for plasmid construction and  Yohann Duverger  for technical advices and for reading the manuscript. This work was funded by the  Centre National de la Recherche Scientifique  (CNRS, http://www. cnrs. fr),  Aix Marseille Université  (AMU, https://www. univ-amu. fr) and by the  Agence Nationale de la Recherche  ( ANR-21-CE12-002 , Kinebiotics). CB received fundings from the  Fondation pour la Recherche Médicale  (number:  ECO201906009080  and  FDT202204014707 ).
Study design and data collection We based this study on the data from the Bacterial Infections and Antibiotic Resistant Diseases in Young Children (BIRDY) cohort studies which aimed to determine the incidence of antibiotic-resistant infection in young infants across LMICs. We selected Senegal, Madagascar, and Cambodia as study countries because they are LMICs located in different world regions, each contains an Institut Pasteur with a microbiology laboratory and an epidemiology unit, facilitating the implementation of the study, and our funders were willing to fund the study in each of these countries. Together, the BIRDY studies include data from BIRDY1 (Madagascar, Cambodia, and Senegal, 2012-2018) and BIRDY2 (Madagascar, 2018-2021). The study areas in Cambodia were the Steung Meanchey district of Phnom Penh (urban) and two districts of Kampong Speu province (rural), 50 km west of Phnom Penh.
We previously described the maternal inclusion criteria and the protocol for infant follow-up between birth and three months of age elsewhere  [10, 11]. Briefly, we exhaustively identified pregnant women in the geographic study areas through community health care workers. We included pregnant women monthly until delivery and newborns at birth whom we followed up by regular home visits (at birth and then at three, seven, 14, 28 and 60 days). We collected standardized data regarding socio-demographic data, clinical signs, anthropometric data, symptoms, and care pathways at each home visit. Among mothers attending partner health care facilities at delivery or in case of health events, medical staff documented standardized data, including delivery circumstances, symptoms, diagnosis severity, and treatment prescribed.
Statistical analyses We presented the results as count (percentage) or mean (standard deviation) for normally distributed variables and median (interquartile range) for non-normally distributed variables. For descriptive statistics, we compared proportions using χ 2 tests, means using Student's tests, and medians using Kruskal-Wallis tests. We estimated the probability of survival over time with a Kaplan-Meier curve. We calculated incidences of stillbirth and neonatal mortality and their corresponding 95% confidence intervals (CIs). We selected risk factors for stillbirth and neonatal death based on data from published literature. To maximize sample size, we pooled data across countries and forced the country variable in all models. We performed univariate logistic regression, subsequently including variables with P < 0.