dataesr/scientific-paragraphs-categorization huggingface dataset:
e. < 0. 05 mg/kg food), only a limited data set is needed. More detailed information on the required data is available in the SCF guidelines  (European Commission, 2001). The assessment was conducted in line with the principles described in the EFSA Guidance on transparency in the scientific aspects of risk assessment (EFSA, 2009a) and considering the relevant guidance from the EFSA Scientific Committee. According to the general principles of the safety assessment of active or intelligent substances present in active and intelligent materials and articles intended to come into contact with food  (EFSA, 2009b) , this safety assessment focuses on the risks related to any dietary exposure to chemicals arising from the intended application. It should be noted that the EFSA evaluation cannot be considered as proof of the technical efficacy of an active and/or intelligent material and article.
5 dm 2 /30 mL of food simulant. Inductively coupled plasma-mass spectrometry (ICP-MS) analysis was applied to measure selenium in the food simulants and in the hazelnuts. In all cases, migration of selenium was not detectable at a detection limit of 2. 3 lg/kg food simulant or, in case of hazelnuts, 0. 46 lg/kg. In these test films, the SeNPs level was determined to be 0. 2 mg/m 2 corresponding to 0. 002 mg/dm². The Panel noted that under these test conditions the maximum use level of 30 lg/dm 2 was not simulated. However, based on published data  (Franz and Welle, 2017; Stoermer et al. , 2017)  on diffusion in and migration from polymers of nanoparticles, migration of SeNPs is not to be expected also at this higher use level. Due to the high conversion rate of selenite into SeNPs (99. 87%) and taking inherently low diffusion characteristics of polyolefin polymers for inorganic species into account, also migration of ionic selenium such as residual selenite is not expected.
Toxicological data Selenium is an essential trace element. In the human diet, selenium is present mainly in organic compounds, as L-selenomethionine and L-selenocysteine, with lower amounts in inorganic compounds, as selenate and selenite. The EFSA Panel on Dietetic Products, Nutrition and Allergies (NDA) set in 2014, adequate intake (AI) values for selenium in the range of 15 lg/day for children aged one to three years up to 70 lg/day for adults. The SCF (2000) set tolerable upper intake levels (UL) in the range of 60 lg/day for children aged 1-3 years up to 300 lg/day for adults. The UL has not been reconsidered in the EFSA NDA Panel (2014) opinion. Since no migration and therefore no exposure to selenium is to be expected for this multilayer application, the CEF Panel did not consider it necessary to propose restrictions or specifications on the particle size, the concentration of selenium in the plastic materials or on the thickness of the barrier layer.
Altogether these data show that the phenol moiety is mainly as a Cu(II) coordinated phenolato at pH 7. 1 whereas LH is bound to Cu(II) in its protonated form in the solid state, both phenolate (solution) or phenol (solid-state) groups lying in the apical position (see Supporting Information for details). Based on the value of its redox potential, it was anticipated that 2 + should be resistant to the reduction by ascorbate that shows an anodic potential under the very same recording conditions at 0. l V vs. SCE,  [24]  which is the very first step of ROS production by Cu(II) complexes. We confirmed this by measuring the catalytic consumption of Asc under different conditions. The absence of Asc consumption or its preclusion was observed, respectively. This indicates that 1 + is able to remove Cu(II) from A leading to 2 + , which is not competent for Asc oxidation.
Study design and sample size A cross-sectional study was conducted in Cotonou, during April-May 2016. The numbers of caregivers to interview was calculated by the Schwartz' formula  [24] : where z represents the z-score fixed at 1. 96; e indicates the desired margin of error fixed at 0. 05  [25] , and p the proportion of children under 12 which have already contracted malaria. This latter proportion was unknown, and was fixed to 50% in order to maximize the sample size  [26]. A total of 384 caregivers of children under 12 should be included in the study. Because of the absence of relevant data to perform a simple random sampling, a GPS sampling method was used to access caregivers. The sampling method consisted of random selection of a calculated number of GPS points into the study area. Buildings identified by GPS points were visited for the survey.
Collected data Questionnaire for data collection was translated into the local dialect "fon", the most common spoken in Cotonou by non-French speakers. In the households, caregivers were interviewed. A questionnaire was administered by investigators who graduated in sociology with substantial knowledge of the field surveys. Questions were about the health-seeking behaviour during the most recent malaria episode among their children under 12 in the household. The episode date was collected and caregivers were asked to cite any symptoms which leaded them to recognize that the child had malaria. Afterward, the first action done by caregivers after they recognized symptoms were collected. Action could then be either home treatment or consultation with a healthcare professional. Information were collected on the type of treatments used at home or prescribed (pharmaceutical drugs or traditional remedies), treatment name and galenic form of pharmaceutical drugs.
Data analysis Data were analysed using STATA version 13 statistical software (Stata Corp. , TX USA). Descriptive analyses were performed to characterize socio-demographic aspects of caregivers, and management of the disease. Median and length were calculated for continuous variables and percentages for categorical variables. To assess the significance of differences between proportions the Chi square test or Fisher's exact test, were used as appropriate. Forgetting the name of drugs used over time can be a consequence of a memory time-related bias. To identify any possible memory time-related bias, the date of the most recent episode was quantified and grouped by months, and Chi square tests were conducted based on information related to the forgetfulness of the used treatments names, and secondly with therapeutic classes of cited drugs.
Results Among the 340 caregivers, 27% reported that children had malaria during the month preceding the interview, 36% had malaria in the last 1-3 months, 15% within the last 4-6 months, and 22% declared that the most recent episode dates back more than 6 months. The median time was 2 months. There was no evidence for memory time-related bias; neither for forgetfulness of the used treatment names, nor for the medicines therapeutic class (see Additional file 1). Based on these results, all data were included in subsequent analyses.
IMPD versus formal market The places of purchase were recorded only in the case of home treatment, and not after consulting a healthcare professional. Table  5  presents data on locations provided by 185 caregivers who bought a pharmaceutical treatment. Various commercial drug names were cited, underlining the availability of a wide variety of pharmaceutical drugs available for purchase without prescription (see Additional file 2 for the name of pharmaceutical drugs cited). There was no difference in the use of anti-malarials in relation to the purchase place. However, ACT (p < 0. 05) was more often purchased in formal market, whereas chloroquine (p < 0. 02) was more often purchased in IMPD. When drugs were used alone, anti-malarials (p < 0. 001) was the most often purchased in the formal market.
Statistical analyses All statistical analyses were performed using GraphPad Prism 6 software. Data sets were tested for normality using Kolmogorov Smirnov, Shapiro-Wilk and D'Agostino-Pearson tests. In the time course experiments, where 2 or more groups are compared, Kruskall-Wallis tests were performed with Dunn's post-hoc test for multiple comparisons. All other comparisons between groups were Mann-Whitney tests, adjusted for multiple comparisons where necessary. Correlations were Spearman's Rank Correlations.
Statistical Analysis To test the significance of the antagonistic potential of each beverage against the Shigella strains, Principal Component Analysis (PCA) was applied to the percentage pathogen clearance data set through multivariate exploratory techniques using XLSTAT software (version 2015. 6, Addinsoft, SARL, Paris, France). A data matrix was constructed where the samples from each interval, that is 0, 7 and 14 days, were inserted in rows and the antagonistic potential against each strain at each hour of co-incubation were placed in columns and 2D plots were generated to predict the variability among the principal components. All total phenolic content (TPC) data are as an average of triplicate experiments with standard deviation.
Acknowledgments The work was supported by  European Union Funds  ( INTERACT-NORTE-01-0145-FEDER-000017-Linha Vital-ityWineON 0013 ) and  Portuguese national funds (FCT-Portuguese Foundation for Science and Technology)  under the Projects  UID/ AGR/04033/2013  and  UID/BIA/04050/2013. HN was supported by postdoctoral grant from  FCT  ( SFRH/BPD/115518/2016 ). Open Access This article is distributed under the terms of the Creative Commons Attribution 4. 0 International License (http://creat iveco mmons. org/licenses/by/4. 0/),which permits use, duplication, adaptation, distribution and reproduction in any medium or format, as long as you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license and indicate if changes were made.
Statistical Analysis We calculated the mean and standard deviation of the LF, IgA, and LZ content before pasteurization. We evaluated the impact of pasteurization on LF, IgA, and LZ concentrations by expressing the results as the difference between the concentration before and after pasteurization and finally as the percentage of retention after pasteurization. This was calculated for both pasteurizers. Differences in absolute value and percentage of pre-treatment value were compared by a Wilcoxon matched sample test. The threshold of significance was set at 0. 05. The software used for analysis was SPSS R version 19 (IBM SPSS Statistics, Boigny-sur-Bionne, France).
Acknowledgments  A. M. M. B. Morais  and  R. M. S. C. Morais  acknowledge the support of the National Funds from FCT, Fundacão para a Ciência e Tecnologia, through Project  UID/Multi/50016/2013. P. J. A. Sobral (13/07914-8 ),  I. Dammak  ( 15/02879-5 ), and  J. Bonilla  ( 14/03288-8 ) acknowledge the financial support and postdoctoral fellowships from the  São Paulo Research Foundation (FAPESP)  and the  Brazilian National Council for Scientific and Technological Development (CNPq)  for the Research fellowship of P. J. A. Sobral. E. Ramalhosa is grateful to FCT and  FEDER  under Programme  PT2020  for financial support to CIMO ( UID/AGR/00690/2013 ).
The XRD patterns of the assynthesized samples and calcined samples were recorded using PANalytical X'Pert and STOE STADI P diffractometers, respectively. These were operated with Cu Ka radiation (l ¼ 1. 5406 Å) for 2q values of 3-70 with steps of 0. 02 or 0. 28 s À1 at room temperature. X'Pert HighScore soware was used to identify the crystalline phases present in the samples by comparison of the experimental diffraction patterns with reference patterns provided by the International Center for Diffraction Data (ICDD) (i. e. , PDF-4+ powder diffraction les). 43 The compositions of the samples were determined by inductively coupled plasma atomic emission spectrometry (ICP-AES). The morphology of the samples was determined by scanning electron microscopy (SEM) using a Philips XL30 microscope under a vacuum of 10 À5 mbar.
4 mm). 48 Fluorescence and reection images were taken at the same time at 6 different locations on each material sample. Excitation sources at 488 nm and 405 nm, respectively, and a 490-555 nm bandpass emission lter were used for uorescence data capture. At each location, stacks of 2D x,y images (at intervals of 1 mm in the z-direction) were acquired. In each experiment, one sample of each type of material was used. The experiment was repeated 6 times. 2. 2. 5. Effect of release of Ag + ions on bacterial viability. The effect of the release of silver ions from Ag nanoparticles on the viability of adherent bacteria was investigated by staining with red-uorescent propidium iodide (PI) (1 g L À1 , $94%, Sigma-Aldrich), which penetrates bacteria with a damaged membrane. 49, 50 As the last rinsing step, the material samples were rinsed with a solution of PI in NaCl with a concentration of 4 mg L À1.
Micro computed tomography (micro-CT) Bone microarchitecture was always assessed using the right hindlimb of each mouse. The samples were fixed for 24h with 4% paraformaldehyde (PFA) in phosphate-buffered saline (PBS) at pH7. 4 and preserved in 70% ethanol until data acquisition by micro-CT with a Skyscan 1272 X-ray computed microtomography (Bruker, Belgium). Samples were wrapped in laboratory film (Parafilm), embedded in distilled water and placed inside 2mL tubes (Sarstedt). For image acquisition, the following parameters were used: X-ray tube potential 70 kV, X-ray tube current 142 μA, 0. 5mm Al filter, rotation step 0. 4˚, isotropic voxel size 5 μm 3 and exposure time 1500ms. For data reconstruction, the NRecon software (v1. 6. 9. 8, Bruker, Belgium) was used, with Gaussian smoothing, ring artefact correction and 40% beam hardening correction applied.
Using Dataviewer software (v1. 4. 4, Bruker, Belgium) each dataset was normalized regarding its orientation and saved in trans axial (X-Y) projections, and then exported to CTAn software (v1. 13. 11. 0, Bruker, Belgium). To measure bone microarchitecture parameters for each dataset, growth plate plus 0. 25mm was used as structural reference between each sample and then, using CTAn software, the regions of interest (ROI) for 1. 2mm in length were selected and three-dimensional microarchitecture parameters calculated for both the femur and tibia and expressed according with the ASBMR recommendations  [17]. Microarchitecture parameters included bone volume fraction (BV/TV), bone volume (BV), trabecular thickness (Tb. Th), trabecular number (Tb. N), trabecular separation (Tb. Sp), and structural model index (SMI), indicative of trabecular organization  [18].
Acknowledgments We want to dedicate this work to the memory of  I. Jorge Pinto , co-author in this study which unfortunately was deceased during the realization of this work. The authors thank  INSERM 1132 Bioscar, Hopital Lariboisière  for all the laboratory resources made available to Marcio Simão during his stay in Paris and  Caroline Marty  for her technical expertise with histological techniques. This research was partially supported by  National funds through Foundation for Science and Technology (FCT) , under the project " CCMAR/Multi/04326/2013 " and  European Regional Development Fund (FEDER)  with project  Norte-01-0145-FEDER-000012  -" Structured program  on bioengineered therapies for infectious diseases and tissue regeneration".
Data collection Demographic and medical information, including age, sex, height, weight, Acute Physiology and Chronic Health Evaluation II score, SOFA score, and admission category (medical, surgical, or trauma), was collected before the start of study product administration. The volume of administered study product was recorded daily until ICU discharge or day 28 of intervention. In addition, whether the patient received oral or parenteral nutrition was recorded. Reasons were recorded for each day the target intake was not met (startup period, gastrointestinal problems, medical procedures, intake via other routes, and other reasons). In case of gastrointestinal tolerance or energy intake via other routes, a specification was requested. Because of the strong decline in the number of patients in the ICU after day 10, the reported data on nutritional intake represent the first 10 days of intervention unless otherwise indicated.
Outcomes The primary outcome parameter was protein intake from study product in grams per kilogram of body weight (g/kg BW) at day 5 of the intervention period. Secondary outcome parameters included protein and energy intake from study product at each day per kg BW, as a percentage of target (where energy target was defined as 25 kcal/kg BW and protein target as 1. 5 g/kg BW), and as the average intake over the first 10 days of intervention and the total intervention period. Calculations of protein and energy intake were performed both per kg IBW and per kg actual body weight (ABW); IBW and ABW values are reported for the primary parameter, whereas only IBW data are reported for the secondary parameters to ensure consistency with prescribed target volumes. The incidence of diarrhea was assessed using the daily defecation score (DDS), which is the sum of consistency scores for every evacuation per day.
Statistical analysis This study was powered to detect an effect size of 0. 5 g/kg BW for protein intake at day 5  [20]. Assuming a significance level (α) of 0. 05 and a two-sided effect, a sample size of 38 patients resulted in 80% power to observe a statistically significant and clinically relevant difference in protein intake. The study included six additional patients to cover possible unevaluable subjects due to missing data, early terminations, or protocol deviations. All analyses were performed on the intention-to-treat dataset, defined as all subjects randomized. For the primary parameter, least squares (LS) means are reported. LS means provide the average of the estimated effects from the linear mixed model by assuming missing at random for missing data and including the stratification factor of center as a covariate.
For other continuous outcome parameters, mean ± SD or, for skewed distributed data, median and IQR are reported unless otherwise specified. For categorical outcome parameters, count and percent are reported. For all outcome parameters, two-sided P values < 0. 05 were considered statistically significant, without correction for multiple testing. Analyses were performed with SAS version 9. 4 software (SAS Institute Inc. , Cary, NC, USA). A repeated measures mixed model is fitted with intervention group, day, and interaction of group by day, including the stratification factor of center as fixed effects and considering day as a within-subject factor with a compound symmetry variance-covariance structure. When the normality assumption was not satisfied, nonparametric van Elteren tests (stratified Wilcoxon-Mann-Whitney test) were performed to compare the intervention groups.
Another strength is that the study design allowed enteral feeding according to nutritional guidelines to be compared with a control group reflecting current practice. The specific study population of overweight and obese patients was included because a high protein-to-energy ratio was considered especially important in this group. Consequently, these results are not representative of the total ICU population, which is a limitation of this study. Another weakness is that the total protein and energy intake, including intake from oral nutrition, was not recorded; therefore, the reported data underestimate the total nutritional intake. In addition, it should be taken into account that the plasma amino acids found at day 5 were somewhat influenced by protein intake from oral and parenteral nutrition.
We recently demonstrated in a randomized clinical study (http://ClinicalTrials. gov NCT01771588) that this new human milk fortifier (nHMF) is safe, well tolerated, and improves the weight gain of preterm infants, when compared to a control fat-free fortifier (cHMF)  [9]. As part of this study, we conducted secondary experiments in a subset of infants to determine the baseline fatty acid composition of unfortified human milk and to compare the effects of nHMF and cHMF on fatty acid metabolism in preterm infants.
Plasma and RBC FAME Preparation and Analysis Fatty acids in plasma TAG and PL were transesterified according to the method described by Morrison and Smith  [13]. FAMEs were analysed by GC on a BPX 70 capillary column (60 m long, 0. 25 µm film, 0. 25 mm ID, SGE, Milton Keynes, UK). Hydrogen was used as carrier gas with a constant 120 kPa pressure and flow of 20 mL/min. The GC system consisted of a Focus GS (Thermofinnigan, Courtaboeuf, France) equipped with a split injector (1:80 ratio) heated to 250  C/min), and held at 235 • C for 20 min. ChromQuest software (Thermofinnigan, Courtaboeuf, France) was used for data acquisition and handling. A pure FAME mixture (Sigma, St Louis, MO, USA) of known composition was used as the standard for column calibration. The variation in peak area between injections was below 2%.
Statistical Analysis Levels of fatty acids were measured at Day 1 and Day 21 of full HM fortification, in plasma PL, plasma TAG, RBC-PC and RBC-PE. Summary statistics for each fatty acid and for each compartment were calculated at each visit. Data distribution was close to log-normal; geometric mean and geometric standard deviation are provided in the present paper instead of arithmetic mean and standard deviation. Relative fatty acid concentrations were analysed at Day 21 (log-transformation) using a mixed-effect ANCOVA model adjusted for postmenstrual age at Day 1, weight at Day 1, fatty acid concentration at Day 1, sex, centre and treatment group (with centre considered as a random effect). Estimations of the treatment effect nHMF/cHMF (log of the ratio of the geometric estimates) and the two-sided p-value are given in for each fatty acid analysed in the different lipid compartments.
Discussion The lipid composition of the nHMF is intended to provide significant quantities of dietary MCFA 8:0 and 10:0, ALA and DHA, as a complement to HM innate lipid content (Table  2 ). In the present study, a subset of HM samples was fortified with nHMF to validate both its addition rate and composition in accordance to the current recommendations (Table  3 ). It is important to note that large inter-individual variation of ARA and DHA content in HM has been observed mainly due to the influence of maternal diet  [7]. In the present study, comparison of the fatty acid profile of erythrocyte and plasma lipids in infants fed HM fortified with nHMF or cHMF provides valuable insight into the fatty acid metabolism of preterm infants. Based on the full dataset, Figure  1  gives a comprehensive representation of the changes in fatty acid levels when preterm infants are fed HM fortified with the nHMF compared to preterm infants fed HM fortified with cHMF.
Acknowledgments: The authors thank the families of the infants who participated in the study, as well as the research staff at each participating institution. We also thank  Christelle Perdrieu  and  Samir Dahbane  from the  Clinical Development Unit at the Nestlé Research Center  for assistance with trial management and Christele Closse/COPEDA who provided medical writing services on behalf of Nestlé Nutrition. Portions of these data were presented in abstract form at the  World Congress of Pediatric Gastroenterology, Hepatology, and Nutrition, Montreal ,  Canada ,  5-8 October 2016.