dataesr/scientific-paragraphs-categorization huggingface dataset:
1 kg (Body Composition Monitor Scale Tanita BC-543, Tokyo, Japan). Height was measured by using a height measuring device with a precision of 0. 1 cm (wooden height board, UNICEF). Anthropometric z-scores were calculated using the National Center for Health Statistics/WHO growth reference data of 2006  [9]. For women, body mass index (BMI) was calculated as the body weight (in kg) divided by the square of height (in meters). Women were classified using the BMI cut-off points endorsed for Asian populations: underweight (BMI < 18. 5 kg/m 2 ), healthy weight (BMI 18. 5-22. 9 kg/m 2 ), overweight (BMI 23. 0-27. 49 kg/m 2 ), and obese (BMI ≥ 27. 5 kg/m 2 )  [10]. After anthropometry, a non-fasting blood sample was collected by venipuncture in trace-element free heparinized sampling tubes (Vacuette, Greiner Bio One, Kremsmünster, Austria).
Plasma was aliquoted into 200 μL pre-labeled Eppendorf tubes and kept frozen at -20 °C at the Provincial Health Centre before being sent (within two weeks) on dry ice to the National Institute of Nutrition (NIN) where samples were stored at -70 °C until analysis. Food intakes of children and women included in this study were extracted from the food consumption data at the household level and the individual consumption of children aged less than 5 years old measured during the 2009 Food Consumption Survey (FCS) using the 24-h recall method combined with controlled food weighing  [11]. The 24-h recall was conducted by teams of dietitians or trained personnel from the provincial medical centers. For children under 5 years of age, a specific questionnaire was implemented to estimate, through the 24-h recall, the child consumption.
Anemia Prevalence The etiologies of iron deficiency and zinc deficiency have much in common, as both are abundant in the same food items (meat, eggs) and absorption of both is inhibited by phytates. Therefore, the prevalence of anemia could perhaps be used as a proxy indicator of zinc status. This would provide the big advantage that anemia prevalence data available for most countries, is cheap to obtain, and field friendly methods such as the Hemocue exist to perform national surveys. We therefore included anemia and other measures of iron status (ferritin) in the present analyses, keeping in mind of course, anemia is not only due to iron deficiency. Indeed, in some Vietnamese populations, iron deficiency accounts for much less than 50% of the anemia found  [19].
Results To evaluate for associations or discrepancies between the different indicators of zinc status that are listed above, we examined data on indicators for zinc status from the recent large, nation-wide micronutrient survey in Vietnam described above  [8]. In total, 1526 women and 586 children from 1526 households in 19 provinces were surveyed. Roughly half of them lived in an urban area. The different indicators measured in the study to estimate the "prevalence" of zinc deficiency showed very different prevalences of zinc deficiency Table  1. Prevalence of low "zinc status" in Vietnamese women of reproductive age (n = 1526) and their children aged 6-60 months (n = 586) participating in a national wide micronutrient survey in 2010 as defined by low plasma zinc concentration (<9. 9 μmol/L for children and <10.
Materials and Methods Population The rationale and design of the EPIC study have been previously reported  [10, 11]. The EPIC cohort consists of more than 500,000 subjects distributed among 23 centres in 10 European countries (Denmark, France, Greece, Germany, Italy, the Netherlands, Norway, Spain, Sweden and United Kingdom). Between 1992 and 2000, country-specific dietary questionnaires (food frequency questionnaires or diet history questionnaires), standardized lifestyle, anthropometric data and blood samples were collected at baseline from the study participants. Blood samples were collected from most participants at baseline  (1992) (1993) (1994) (1995) (1996) (1997) (1998). In each of the 23 centres, blood samples of at least 30mL were drawn from most participants and stored at 5-10°C protected from light and transported to local laboratories for processing and aliquoting.
No follow-up data were available from Ragusa and Turin centers in Italy. As the follow-up times differed by center, we calculated the weight change at 5 years (kg/5y) as (weight at follow-up-weight at baseline) x 5/years of follow-up. The weight at 5 years, determined adding the weight change at 5 years to the weight at baseline, and the BMI at 5 years were also obtained. The outcome measure used in our analysis was the percent of weight change at 5 years, computed as (weight at 5 years minus weight at baseline/weight at baseline) x100, and expressed as a percentage.
Models were adjusted by length of follow-up (years), age (years), energy intake (kcal/day), alcohol intake (g/day), smoking status (never, former, current), physical activity (inactive, moderately inactive, moderately active, active), and region. Analyses were carried out for women and men separately. Statistical tests were 2-sided, and p-values <0. 05 were considered significant. All statistical analyses were performed using SAS statistical software (version 9. 4, SAS Institute Inc, Cary, NC, USA).
Behavioral Data The profile video sequence recorded for each participant was divided into 16 segments, corresponding to each odorant condition, using appropriate software (Volcan R , Lyon, France; see  Rinck et al. , 2011). For each segment, olfactory exploration of the jar was quantified, starting when the participant moved the jar in front of his nose/lip, or even earlier if a strong focus of the odor was observed (e. g. , head movement or marked diminution of the approach movement), and ending when the participant moved the jar away from his nose. Four variables were analyzed: (i) number of olfactory explorations per stimulus; (ii) total duration of olfactory exploration; (iii) mean duration of olfactory exploration (total duration/number of explorations); and (iv) duration of the first olfactory exploration.
These issues of exclusion of participants (two children for concentration and verbal problems), and missing data from 3 other children (particularly those who could not complete the entire task due to strong affective reactions to the smells) have an unknown impact on the study findings that extends beyond sample size and power limitations. Since not all children were able to test all 16 stimuli, additional analyses of the influence of odor intensity on odor pleasantness could not be assessed. Nevertheless, this issue provided important information about the number of stimuli that ASD children can experience in a reasonable amount of time (10 odorant conditions seems adequate according to the present findings). Another sample bias that may have affected some of the null findings is sample heterogeneity since our ASD group included six typical ASD children and four Asperger syndromes.
Acknowledgements. We thank all past and present colleagues from  Gérard Ailhaud 's and  Ez-Zoubir Amri 's team who were involved in these studies. Special thanks are due to  Dr P. Guesnet  for his contribution over the years. The works cited in this review were supported by  CNRS ,  EU   FP7  project  DIABAT  ( HEALTH-F2-2011-278373 ),  French Agence Nationale de la Recherche  ( ANR-05-PNRA-007 LI-PADIP ,  ANR-10-BLAN-1105  miRBAT),  Nutricia Research Foundation  (2011Foundation ( -2025) ) and  Société Française de Nutrition  ( 2012 Research Prize ). Disclosure. The authors declare no conflict of interest.
Adipose tissue cellularity To determine adipocyte diameter, frozen samples of SCAT were sectioned at 12 μm thickness using a cryostat (2800 Frigocut Reicher-Jung, Francheville, France) at -30°C. Cross sections were mounted on slides, and stained with Oil Red O solution to reveal lipids  [21]  and counterstained with a crystal violet solution (0. 05%) to reveal membranes. Images of adipocytes were obtained at 10-fold magnification with a digital camera system (CV-M90, Jai, Glostrup, Denmark). Three slides were prepared per sample, and the best membrane integrity images were retained for cellular analyses (at least 200 adipocytes per sample). Cross section area of each adipocyte in the image was measured using a digitizing table and image analysis software (Visilog 6. 0 Imaging software, Noesis, Courtaboeuf, France).
The present study was supported by  Research Grants  from  ADISSEO  and  INRA  and both have contributed to the study design and manuscript preparation. The funder INRA also contributed to the conduct of the study, analysis of the samples and data, and interpretation of the findings. Funders did not interfere with the full presentation of this research, objective interpretation of the data and decision to submit for publication. The present study was supported by  Research Grants  from  ADISSEO  and  INRA  and both have contributed to the study design and manuscript preparation. The funder INRA also contributed to the conduct of the study,.
The Pfaffl method  [6]  was used to calculate the expression levels of the target genes in the post-treatment samples relative to the corresponding baseline control samples within each subject and normalized against HPRT1 and GUSB. Individual amplification efficiencies were analyzed for each reaction by LinRegPCR software (HFRC version 2014. 2,  [7] ) and ΔCt values were corrected by their corresponding individual efficiencies.
Oxylipin profiling Oxylipins were analyzed as described in Yang et al. [12]. Briefly, samples were extracted by solid phase extraction (SPE) and separated by liquid chromatography, followed by QTrap tandem mass spectrometry. The instrument was operated in negative multiple reaction monitoring (MRM) mode. Quality control samples were analyzed at a minimum frequency of 10 samples. Analyst software 1. 4. 2 was used to quantify the peaks according to the standard curves. Oxylipin data were quantified and are presented as mol/L of plasma. Six batches of the standard mixtures and three further dilutions were used to determine the Limit of Quantification (LOQ) and linearity range. The calibration curves were calculated by least-squares linear regression using an 1/x weighting factor. The standard concentrations were back-calculated from the constructed calibrations curves for each analyte.
Pearson product-moment correlation analysis was also used to examine the correlations between BMI and the fold changes in gene expression and % changes in oxylipins, FA, and oxylipin/FA ratios. Significance was set at α 0. 05. The Fisher transformation was used to evaluate statistical significance and to obtain 95% confidence intervals. No adjustments were made for multiple testing due to the exploratory nature of the analyses. The data were analyzed using JMP12 Pro software (SAS Institute, Inc. , Cary, NC).
Funding was provided in part by The  Center for Health and Nutrition Research (CHNR)  Pilot Grant Program,  National Institute of Diabetes and Digestive and Kidney Diseases (NIDDK)  grant  R01 DK49368 ; The  University of California Discovery Program  ( 05GEB01NHB ); the  National Institute of Environmental Health Sciences (NIEHS)   P42ES004699 ,  NIEHS   R01 ES002710 , and  NIEHS Results.
Calculations and statistical analysis Apparent transfer of 20:5n-3, 22:5n-3, and 22:6n-3 from FO into milk was calculated as: [g milk FA yield × (g FA/100 g milk fatg FA/ 100 g in control milk fat) / (DMI × g FA intake)] × 100. Experimental data were subjected to Analysis of Variance using the general linear model procedure of Statistical Analysis Systems software package version 8. 2 (SAS, SAS Institute, Cary, NC, USA) with a model that included the fixed effects of period and treatment and random effects of goat. Least square means ± SEM are reported and treatment effects were declared significant at P < 0. 05 and considered a trend towards significance at P < 0. 10. Pearson correlation coefficients (r) were generated for the association between individual FA in milk fat and between the abundance of specific milk FA with milk fat content using the CORR procedure of SAS.
Acknowledgments The present study was supported by  Apis-Gene  and the  Agence Nationale de la Recherche  ( ANR, France ;  ANR-GANI-014 , coordinated by  Patrice Martin ). Authors gratefully acknowledge the staff of  Unité Expérimentale des Ruminants de Theix (INRA, France)  for the diligent care of the experimental animals and  P. Capitan , E.
Lyophilized apotransferrin (iron free transferrin (Tf)) isolated from human plasma was dissolved in sterile BSS solution at a concentration of 48mg/ml (T5391, Sigma Aldrich Chemical Co, Saint-Quentin en Yvelines, Fr). Rats were anesthetized using intramuscular injection of 35:25 mix of ketamine (Virbac, Carros, Fr) and xylazine (Bayer, Lyon, Fr) (1ml/100mg) and intravitreal injections (5µl,) were performed in inferior quadrant of both rat eyes using a 30-gauge needle under an operating microscope. This content was determined as the most efficient to protect photoreceptors (data not shown). Rats were sacrificed at different time points after light exposure. For in vivo analysis and histology, rats were examined or sacrificed 8 or 16 days after light exposure. Additional time points were used for immunohistochemistry and RT-qPCR at 1, 3 or 8 days after light exposure.
Microglia cells activation 3 days after end of light-exposed was determined in outer plexiform layer, outer nuclear layer and segments layers, identified after DAPI nuclei stain. Measurement of microglia/macrophages staining was performed on pictures (60X) taken in the overall retina with same exposure time. The rapport of CD68 intensity staining to total microglia cells revealed by Iba1 intensity staining was measured with ImageJ software.
Histology and outer nuclear layer thickness measurement Oriented ocular globes were fixed with 4% PAF, 0. 5% glutaraldehyde (LADD, Inland Europe, Fr) in PBS for 2 hours. After fixation, samples were washed, dehydrated and transferred into the infiltration solution of the Leica Historesin embedding kit (Leica, Nanterre, France) over night at 4°C. Samples were embedded in resin (Leica) and 5 µm thick sections passing through the optic nerve head were prepared along the superior and inferior pole of the eye using a microtome (Leica), stained with 1% Toluidin Blue solution. Sections were observed on a Leitz microscope and photographed with a Leica camera. Thicknesses of outer nuclear layer (ONL) were measured every 500 µm using Visilog 5. 3 software (Noesis, Courtabouef, Fr). Histological sections measurements were performed across the whole retina, considering the inferior pole to 0 from -4,000µm of optic nerve and superior pole to 0 from 4,000µm of optic nerve.
s/m 2 , flash duration of 40 ms, and the amplifier set to 0. 5 Hz. Five responses were averaged. Amplitudes of a-waves (negative waves) were measured from the baseline to the bottom of the a-wave trough, and b-wave amplitudes (positive waves) were measured from the bottom of the a-wave trough to the peak of the b-wave. Implicit times of the a-and b-waves were measured from time of stimulus to peaks. Results were expressed in microvolts (µV) for amplitudes and milliseconds (ms) for implicit times. The data obtained from each eye belonging to the same experimental group were averaged.
RT-PCR Inflammation-focused genes array and data analysis Neural retinas were isolated on ice and directly frozen until RNA isolation. Total RNA was isolated with RNeasy mini kit (Qiagen, Courtaboeuf, Fr) according to the manufacturer's protocols. RNA concentration, purity, and integrity were determined with an Agilent Bio-analyzer. All RNA used had RNA integrity number superior to 8. First-strand cDNA was generated by reverse transcription using 0. 7µg total RNA and the RT2 First Strand Kit (Qiagen). Genomic DNA was removed on RNeasy columns and before reverse transcription according to the manufacturer's protocols. Expression of 84 inflammatory-related genes and 5 housekeeping genes were evaluated in a 96-well plate (including five housekeeping and seven control genes) by the Rat Inflammatory-Autoimmunity RT2 Profiler PCR Array (PARN-077Z, SABiosciences, Qiagen).
Gene arrays were processed according to the manufacturer's instructions. Each PCR reaction was performed following manufacturer's instructions, and dissociation curves were performed to control product of amplification. The threshold for calculating cycle threshold (Ct) values was calculated automatically using RQ software (SABiosciences). A fixed threshold was assigned manually, as suggested by the manufacturer. The relative expression of each gene was calculated using the ∆∆Ct method. Ct values were analyzed with Web-Based PCR Array Data Analysis tools: (http://www. sabiosciences. com/pcr/arrayanalysis. php, SABiosciences) to determine the best housekeeping gene (Rplp1), the fold change and p value of each gene (t-test Student). Fold changes ≥ ±2-fold were defined as biologically relevant changes.
Statistical analysis Results are presented as mean ± Standard error on the mean (SEM). Analysis were performed using GraphPad Prism 5 software. Normal distribution of data was checked by the Shapiro-Wilk test. Comparisons between 2 groups were analyzed by unpaired two-tailed Student's t-test, and multiples comparisons by one-way ANOVA followed by Bonferroni post-test as appropriate. Non-normally distributed were analysed using nonparametric Kruskal-Wallis test. p<0. 05 was considered statistically significant.
Acknowledgements We thank  Dr. Torriglia  and  Dr. de Kozack  ( UMRS1138 ,  Centre de Recherche des Cordeliers, INSERM ) for their guidance and stimulating discussion. We thank  Dr. Reed  and  Mélanie Glaettli  for the english correction and the staff at the animal facility at  Centre de Recherche des Cordeliers. The authors wish to thank  Paolo Santambrogio  ( Department Biological and Technological Research, Instituto de Ricovero e Cure a Carattere Scientifico, San Rafaelle, Milan, Italy ) for rabbit polyclonal specific for the High and Light subunits of Ferritin;  John Saari  ( University of Washington, Seattle, USA ) for rabbit anti-cellular retinaldehyde binding protein and  Robert S. Molday  ( University of British Columbia, Vancouver, Canada ) for anti-rhodopsin antibody. This study was supported by  INSERM ,  ANR Emergence 2012  ( R11086DD ),  Retina France  and  Fondation de France-Fondation  de l'oeil,  Berthe Fouassier.
1%, phase A) and methanol : formic acid (0. 1%, phase B). A split system was used allowing the HPLC eluate to enter the MS detector at a flow rate of 0. 2 mL/min. The injection volume was 20 L. UV spectral data were acquired at 275 nm (the chromatogram was presented in Supplementary Material available online at http://dx. doi. org/10. 1155/2015/859048). The extract was prepared at a 10 mg/mL stock solution concentration which was then diluted in 1× phosphate-buffered saline (PBS), pH 7. 4 (Gibco, Invitrogen) as previously described  [18]. Cells were cultured for 48 hours before all treatments. The antioxidant compounds (200 to 1000 pg/mM for the EGCG and 100 to 1000 g/mL for the RWPs) were added to cells seeded in 96-well treated microplates (BD Falcon, Franklin Lakes, USA) at 30,000 cells/well and incubated for 1 hour.
All antibodies were diluted in blocking buffer from the WesternBreeze Chemiluminescent Kit (Invitrogen, Grand Island, USA) overnight at 4 ∘ C. Secondary antibody solution (anti-mouse (1/2000) or anti-rabbit (1/4000) coupled to alkaline phosphatase) was incubated with the membranes for 30 minutes with continuous rotation as described in the kit. Membranes were then exposed with a Bio-Rad Chemi-Doc XRS System for 600 seconds, and the captured images were analysed using Quantity One software. Expression of CAT and MnSOD proteins was normalized to the quantity of -actin and expressed as a percentage compared to the appropriate negative controls.
The cross-flow gradient was 4-0 mL/min (35 min). After 35 min a tip flow of 0. 5 mL/min was maintained for 20 min to clean up the channel. The system was coupled with a variable wavelength PN3211 ultraviolet spectrophotometric (UV) detector (Postnova Analytics, Landsberg) using a deuterium lamp set at 254 nm, with a PN3621 Multi Angle Laser Light Scattering Detector/MALLS (Postnova Analytics, Landsberg) and with a DLS detector in line in Zetasizer PN3702 (Malvern Instruments, UK). The acquisition and processing of data were performed using AF2000 Focus Software Version 1. 1. 0. 23. The geometric radius (R g ) of the NC was calculated using the data from the 15 angles analysis with MALLS detector by applying the coated sphere model  [63, 64]. The calculation of the geometric diameter for spherical particles is given by the formula Dg = Rg*0.
Acknowledgements This work was funded by the  Bilateral Research Collaboration CAPES-COFECUB between Brazil and France  ( n°768/13 ). This work was also supported by  NANOBIOMG-Network  (#  00007-14  and # 40/11 ), APQ  01510-14  and PPM grant (#  00432-12 ) from  FAPEMIG ,  Minas Gerais ,  Brazil. VCFM  is as researcher fellow of the  Conselho Nacional de Desenvolvimento Científico e Tecnológico (CNPq) ,  Brazil.
Chemicals Natural (all-E) lycopene from tomato oleoresin (C40H56, M = 536 g•mol -1 , >90%) was obtained from Conesa, Badajoz, Spain. Carotenoid extracts from Bacillus strains HU36 were provided by members of the Colorspore consortium (Small Collaborative Project No. 207948, funded by FP7 and coordinated by the Royal Holloway University of London)  [37]. Synthetic type II (all-E) β-carotene (>95%), α-tocopherol (95%), rutin (≥95%), chlorogenic acid (≥95%), menaquinone K2 (MK-4, ≥99. 9%), polyoxyethyleneglycol 23 lauryl ether (Brij ® 35), (9Z,12Z)-octadecadienoic acid (linoleic acid, >99%), FeSO4•7H2O (>99. 5%), Fe(NO3)3•9H2O (98%), myoglobin from equine heart (>90%, essentially salt-free), and ammonium formate (99. 995%) were purchased from Sigma-Aldrich (St-Quentin-Fallavier, France). The buffers used in the experiments were a 0.
Acknowledgments This work was supported by a grant from the  European Community 's  Seventh Framework Program  (Colorspore, Small Collaborative Project Integrated European Project No. 207948 ). Special thanks are given to  Paul Fraser ,  Laura Perez  and  Reena Khaneja  ( Royal Holloway University of London, UK ) for providing carotenoid-rich bacterial extracts. We thank the company  Conesa (Badajoz, Spain)  for its gift of (all-E)-lycopene.
Methods We analyzed data from 16 cross-sectional nutritional surveys conducted by Action Against Hunger International in South Sudan (13 surveys), the Philippines (1 survey), Chad (1 survey), and Bangladesh (1 survey). The surveys in South Sudan were conducted from 2004 to 2007 in different counties of the Upper Nile, Western Equatoria, Eastern Equatoria, and Bahr El Ghazal regions, mainly amongst agro-pastoralist communities of varying ethnic background. The survey in the Philippines was conducted in 2012 in the city of Cagayan de Oro. The survey in Chad was conducted in 2013 in the North Bahr El Ghazal district, among the Gorane pastoralist, nomadic population. All these surveys followed a two-stage cluster representative sampling methodology. In Bangladesh, data were collected in November 2012, through the regular monthly Growth Monitoring Program for children under 5 years old living in the Rohynguas refugee camps of Kutapalong and Nayapara in Cox's Bazaar district.
To determine age (months), the birth date was either extracted from official documents (e. g. birth certificates, refugee registers) or evaluated by maternal report in reference to locally adapted seasonal calendars when official documents were unavailable. Individual Z-scores for WHZ and HAZ were computed in reference to the WHO 2006 growth standards using the Stata zscore06 command. We computed SSR as (Sitting height/standing height)*100 and generated individual Z-scores for the SSR within strata of 6 months of age of the pooled study population (SSRZ), as SSR is largely age-dependent and no reference distribution exists for SSR  [12]. The initial dataset included 14,682 individuals. Cases of edematous malnutrition were excluded from analysis because the WHZ indicator is not valid in such cases (n = 15).