dataesr/scientific-paragraphs-categorization huggingface dataset:
We used ANOVA to test for differences at each timepoint, using the aov function followed with Tukey's post hoc test, coded as Phenotype = Group or Phenotype = Group + Diet + Group × Diet for F0 and F1 respectively. Effect size was reported as the proportion R2 of the variance in the phenotype of interest. The PCA function of the FactoMineR package was used in F0 dams. For olfactory scores, the distribution of the variance was heterogeneous, so nonparametric statistics were performed. N-ways ANOVAs were done using the aovp function of the Permutation Tests for Linear Models (lmperm) package, with factors: Groups × Diet in Figure  4a  and Group × Diet × fasting in Figure  4c , Group × Diet × Odorant in Figure  5  (discrimination) and Group × Diet × Odorant dilution in Figure  6 ; or the nonparametric analysis longitudinal data (nparLD) package  [44]  with Groups × Diet as whole plot factors in and Days in Figure  4b  or Odorant presentations in Figure  5  (habituation) as a subplot.
Post-hoc tests (coin package) followed by BH correction were performed: symmetry-test (Figure  4b ), Wilcoxon test (Figure  4b  and Figure  5 ) and the two-sample Fisher-Pitman permutation test for comparative analysis of two independent diet group (Figure  4 ), stratified by dose (Figure  6 ). A multiple factor analysis (MFA) was performed in F1 generation on a set of 18 variables regrouped in 3 variable categories (biochemisty, biometry and behaviour), using the FactoMineR package  [45]. "Biochemistry" grouped the last measure of fasting glycaemia, insulinaemia, cholesterolemia and leptinemia, and glycemic AUC in OGTT. "Biometry" grouped the organ to body weight ratio for BAT, Pr-WAT, Pg-WAT, Sc-WAT, Total-WAT, Liver, Heart and Kidney, and week-24. 5 body weight. "Behaviour" grouped the week-23 relative caloric intake, day-1 hidden-cookie test retrieving time, HFD filled hole preference ratio and EOG at dose 0.
Acknowledgments: We thank the members of the  Infectiologie Expérimentale des Rongeurs et Poissons Unit  ( UE 0907 ) of the  Institut National de la Recherche Agronomique (INRA) of Jouy-en-Josas  for their professionalism and help with animal experiments. We are grateful to  Adrien Acquistapace ,  Alexandr V. Baklanov ,  Pierre Caillol ,  Amandine Catonné ,  Soahary Jean-René ,  Régine Monnerie ,  Audrey Prézelin  and  Aurélien Raynaud  for their experimental help and to  Aurélia Bruneau  for sharing with us her expertise in OGTT experiments. We thank the Budget and Personnel management service of our research units.
Introduction: The health-related QoL is a patient-centered evaluation covering several aspects. This evaluation seems to be particularly important in patients submitted to radical cystectomy (RC) and urinary diversion with ileal conduit (IC) or a neobladder (NB). Objective: Review all recent data comparing QoL outcomes after radical cystectomy with NB and IC diversions. Evidence Acquisition: A systematic search in PubMed/Medline, Embase, and Cochrane databases was conducted according to the Preferred Reporting Items for Systematic Reviews and Meta-analyses (PRISMA) statement in December 2018. All articles published from January 01, 2012 to December 31, 2018, were included. A study was considered relevant if it compared QoL outcomes using validated questionnaires (EORTC QLQ C30, FACT-G, FACT-BL, FACT-VCI, and BCI).
Data collection process A systematic search in PubMed/Medline, Embase, and Cochrane Library databases was conducted independently by two authors on December 31, 2018. The electronic search strategy (Table-1) included the following Medical Subject Headings (MeSH) terms: "quality of life" OR "QoL" AND "urinary diversion" OR "ileal conduit" OR "neobladder" AND "cystectomy. " All full-length articles published from January 01 2012 to December 31, 2018, were included in the original search. References were also examined to identify additional relevant studies (Figure-1). Missing data were requested from study authors. Discrepancies were resolved through discussion with a third author when necessary.
The effects of ranolazine were mimicked by decreasing the maximal conductance of peak INa. Data analyses: Optical mapping data were analyzed using custom software (SCROLL, Dr. Sergey Mironov) as previously. 8, 18, 19 Analyses included maximal DF, SP density, rotor core trajectory area and lifespan (mean time of rotor existence), as well as AF cycle length (AFCL). For these analyses a rotor was defined as completion of at least one full rotation. Statistical analysis: Statistical analyses were performed using GraphPad Prism 7. Continuous variables with normal distributions were expressed as mean±SEM. Normality of each data set was assessed by a Shapiro-Wilk test and QQ plot, and equality of variance was assessed by Ftest. For non-normal data, the nonparametric Wilcoxon signed-rank test was performed for comparison of means.
University of Michigan Health System and Peking University Health Sciences Center Joint Institute for Translational and Clinical Research (J. J. );  Ministerio de Economía y Competitividad  and  Fondo Europeo de Desarrollo Regional (FEDER)  (J. J. ); the  JHRS fellowship program  from  Medtronic Japan ,  Uehara Memorial Foundation  (Y. T. );  American Heart Association postdoctoral fellowship  (Y. T. ); research grants from  Gilead Sciences Inc  (J. J. , S. V. P. ); and research support and assistance with implantable devices from  St. Jude Medical and Medtronic Inc  (J. J. , O. B. ).
Inhabitants of coastal areas are constantly confronted with minor or major events such as storms, erosion or flooding. This article investigates the predictors of coping willingness among citizens exposed to coastal flooding. Coping can be defined as a set of cognitive and behavioral efforts to master, reduce or tolerate a given risk and these strategies are generally regrouped into two different categories: active coping strategies oriented toward the risk to reduce or master it, and passive coping strategies focused on the reduction of internal tensions such as anxiety or fear. In this paper, we focus especially on how place identity, perceived self-efficacy, anxiety-state and coastal flooding risk perception shape both active and passive coping willingness. Data were obtained from different areas at risk of coastal flooding located in France.
Sample and Procedure Data were obtained from different areas at risk of coastal flooding located in France. The sample is composed of 315 adult participants (mean age = 47; SD = 15). The large proportion of seniors in our sample is representative of the over-representation of elderly people in the coastal areas in France  (Vinet et al. , 2012). Details related to the composition of the sample are presented in Table  1. Participants were asked for their postal code and whether they lived in the area at risk. All participants were living in areas at risk of coastal flooding, located in the western coastal region of France. Site selection was based on coastal risk prevention plans published by the French state. All sites were at equal risk. These plans represent areas exposed to a coastal flood phenomenon.
Data Analysis Because they were no model that clearly established how risk perception, place identity and coping willingness are tied together, we chose to develop and to compare two different models that would enlighten these relations in the context of coastal flooding risk. The first model integrates place identity as a moderator between anxiety and passive coping while the second does not integrate place identity. Descriptive analysis and analysis of variance were performed using SPSS 22 (IBM Corporation, 2013b). Path analysis was performed using AMOS 22 (IBM Corporation, 2013a). There were no missing data. Descriptive statistics are provided in Table  2  and the correlation matrix between the different variables in Table  3. Before the  analysis, the data were checked for normality. Two steps lead the analysis.
The EB population densities (in cfu/g FW) varied depending on the plant species and tissue (Table  1 ). Similar findings were published elsewhere  (Hallmann et al. , 2002; Quadt-Hallman et al. , 1997; Sturz and Nowak, 2000). In the present study, the highest EB densities were found in the leaves of all species tested except for G. biloba. The EB density in its fruit was 33 times higher than that in its leaves (Table  1 ). Based on the relative diameters of the inhibition zones they formed on Xcc plates, 18 EB isolates exhibited varying degrees of positive antibacterial activity (Table  2 ). In addition, solvent extracts of these isolates were evaluated for their antagonistic activity against XccW1 (data not shown). Based on the screening data using the EB and the extracts, the endophytes TbL-22 and TbL-26 were selected for their antibacterial activities against all Xcc strains (Table  3 , Fig.
In contrast to conventional pelvic overview X-rays, which are taken with the patient in a supine position, biplanar EOS images are taken with the patient in an upright standing position of the entire lower limbs from pelvis to feet  [15]. As such, from the EOS images 3D radiological parameters of the whole leg can be calculated to verify the fit of the prosthesis as well as to document changes in radiological leg parameters after THR. In hip OA patients, an increased sacral slope and an increased femoral mechanical angle have been found compared to healthy subjects  [16]. These differences might be due to degenerative changes over time due to OA or inherent differences between individuals. To eliminate these influencing factors also data of healthy controls will be included in this study. The goal of this study was to determine which changes in radiological leg alignment parameters (Hip-Knee-Shaft-Angle, femoral offset, Neck-Shaft-Angle and varus/valgus alignment) occur due to THR and which of these parameters can explain abnormal joint loads during gait.
Patients and healthy controls Twenty-seven symptomatic unilateral hip OA patients (10 male, 17 female), who were scheduled for THR were included in the study. Exclusion criteria were the inability to walk without walking aids, body mass index (BMI) > 30 kgm -2 , inflammatory arthritis, orthopaedic surgeries within the past 6 months and previous joint replacement in the lower extremities. Healthy control subjects were included if they had no history of orthopaedic surgeries or chronic and neuromuscular diseases. All patients and healthy subjects gave informed consent prior to participation. Our institution's medical ethics committee approved the study under the number 497/15. Patient gait data were compared to gait data of 15 healthy controls (9 male, 6 female) with a similar age distribution (Table  1 ).
Gait analysis Patients and healthy controls walked barefoot at a self-selected speed in the gait laboratory. Kinematic data were collected using an 8-camera Vicon MX T10 motion capture system (VICON Motion Systems, Oxford, UK) operating at 200 Hz, while two AMTI force plates (Advanced Mechanical Technology, Inc. , Watertown, MA, USA) were used to synchronously collect kinetic data at 1000 Hz. The marker protocol used for this study was a modified version of the Plug-in-gait model  [20]. After the measurement, 3D marker trajectories were reconstructed, missing frames were filled and data was smoothed with a Woltring filter with MSE 10 using the Vicon Nexus software (version 2. 5, VICON Motion Systems, Oxford, UK). In five trials with a clear foot-forceplate-contact, events were set to identify gait cycles.
Kinematic and kinetic variables were obtained using inverse dynamics equations in which the center of the hip joint was calculated with a standardized geometrical prediction method  [21]. For the healthy controls, data of the left leg was processed, since no significant differences were found in the discrete variables of interest between the left and right side. Data were exported to Matlab (version R2016b, The Mathworks Inc. , Ismaning, Germany) and patterns, which were normalized over the gait cycle, were calculated. To represent the knee and hip joint load, the maximum external knee and hip adduction moment during the first (KAM_1 and HAM_1) and second (KAM_2 and HAM_2) phase of stance were determined for each trial and averaged over the trials. All joint moments were normalized to body mass and expressed in Nmkg -1.
Statistical analysis All data were analysed using IBM SPSS Statistics (version 25, IBM Deutschland GmbH, Ehningen, Germany). Shapiro-Wilk tests revealed normally distributed data. The radiological leg alignment parameters were investigated for differences between patients and controls via independent-samples Students' t-tests and for differences between the affected/operated and non-affected/non-operated side in the patient group using paired-samples Students' t-tests. For the nonoperated leg, Cronbach's α and mean differences between the preoperative and postoperative parameters were calculated to give information on the reliability of the measurement. Walking speed was considered as a covariate to eliminate the effect of speed on the dependent kinematic and kinetic variables (ANCOVA: univariate analyses of variance with walking speed as a covariate and group as a fixed factor (operated leg or nonoperated leg vs.
Patients and healthy controls Of the 27 patients, data of three patients could not be included: for one patient the preoperative EOS image could not be reconstructed, one EOS dataset was not valid due to movement artefacts and one gait analysis could not be used. Of the remaining 24 patients, two patients dropped out as they missed out on the postoperative gait analysis. 22 patients (9 male, 13 female) were included and apart from a significantly higher BMI (P = 0. 002), the patients showed no significant differences to the data of 15 gait controls (Table  1 ). Patients walked significantly faster 1 year after surgery, however still significantly slower compared to the healthy controls (1. 15 vs. 1. 26 ms -1 , P = 0. 009). For the comparison of the leg alignment parameters, the group of 53 controls was significantly younger (P < 0.
For each cell type mean ± SE of three independent experiments (each done in quadruplicate) is shown (3 biological replicates each includes 4 technical replicates). g Ratio of NADPH/NADP + in C and R cells (mean ± SE of four biological replicates). h Levels of ATP in C and R cells (mean ± SE of four biological replicates). For panels d, g, h, p values were below 0. 001 (Student's t-test) for the comparison of R and C cells (detailed statistical analysis for these panels is shown in Supplementary Figs. 4  and 6-8 ). i Proliferation rate of C and R cells measured in real-time (xCelligence); samples with three densities of cells were monitored for each cell type. In each case, experiments were done in duplicate with automated averaging of data points. j PCA for metabolites (475 total) measured in C and R cells (n = 4; samples are biological replicates) Comparison of our patient's fibroblasts with fibroblasts derived from parents Fibroblast cultures generated from both parents (mother, M, heterozygous for the intronic mutation; father, F, heterozygous for the mutation causing a premature stop codon) showed ALDH1L2 protein expression though its levels were noticeably higher in father's cells (Fig.
Metabolomic analysis Cells were cultured in 15 cm dishes, grown to 70-80% confluency, harvested, and subsequently flash frozen. Sample preparation for analysis was carried out at Metabolon Inc. , as described. 54 Briefly, individual samples were subjected to methanol extraction then split into aliquots for analysis by ultrahigh performance liquid chromatography/mass spectrometry (UHPLC/MS). The global biochemical profiling analysis comprised of four unique arms consisting of reverse phase chromatography positive ionization methods optimized for hydrophilic compounds (LC/MS Pos Polar) and hydrophobic compounds (LC/MS Pos Lipid), reverse phase chromatography with negative ionization conditions (LC/MS Neg), as well as a HILIC chromatography method coupled to negative (LC/MS Polar). 55 ll of the methods alternated between full scan MS and data dependent MS n scans.
Statistical analysis Two types of statistical analyses were performed: (1) significance tests and (2) classification analysis. Standard statistical analyses were performed in ArrayStudio on log-transformed data. For analyses not standard in ArrayStudio, the R program (http://cran. r-project. org/) was used. Following log transformation and imputation of missing values, if any, with the minimum observed value for each compound, Welch's two sample t-test was used as significance test to identify biochemicals that differed significantly (p < 0. 05) between experimental groups. An estimate of the false discovery rate (q-value) was calculated to take into account the multiple comparisons that normally occur in metabolomic-based studies. Classification analyses used included principal components analysis (PCA), hierarchical clustering, and OPLS-DA.
2. ALDH1L2 was detected using in-house ALDH1L2-specific polyclonal antibody (1:2000). 12 ALDH3A2 (ab113111), VDAC (ab154856), and GAPDH (ab8245) antibodies were from Abcam. Actin antibody (sc-47778) was purchased from Santa Cruz. All commercial antibodies were used at the dilution of 1:1000. All blots derived from the same experiment were processed in parallel. Band intensities were quantified using ImageJ software, NIH (https://imagej. nih. gov/ij/). Uncropped blot images are shown in Supplementary Fig. 12.
Analysis of mitochondrial mass and membrane potential Cells (1. 5 × 10 5 ) were seeded onto 6 cm plates and left to attach overnight. Cells were harvested, resuspended in 5 ml of fresh medium and stained with 250 nM TMRM and then with 100 nM MitoTracker Green (both from Molecular Probes) to determine mitochondrial polarization and mitochondrial mass respectively. Intensity of each dye was determined using CytoFLEX flow cytometer (Beckman Coulter, Indianapolis, IN, USA). Quantitative analysis was completed using CytoFLEX software.
, Buffalo Grove, IL). Ultrathin sections were collected on 200 mesh copper grids and stained with 4% aqueous uranyl acetate for 12 min, followed by Reynolds' lead citrate for 8 min. Samples were observed with a JEOL JEM-1230 transmission electron microscope operating at 80 kV (JEOL USA, Peabody, MA) and digital images acquired using a Gatan Orius SC1000 CCD camera and Gatan Microscopy Suite 3. 0 software (Gatan, Inc. , Pleasanton, CA). Magnification for each image set includes 5000×, 10,000×, and 20,000×.
ACKNOWLEDGEMENTS The authors thank  Mélanie Rigal ,  Catherine Vaurs-Barrière ,  Patricia Combes , and  Geneviève Giraud  ( Clermont-Ferrand );  Dr. Ting Li  and  Dr. David Horita  ( Nutrition Research Institute, UNC Chapel Hill ). S. A. K. is supported by the  National Institutes of Health  grant  R01 DK117854. The  Microscopy Services Laboratory, Department of Pathology and Laboratory Medicine, UNC , is supported in part by  P30 CA016086   Cancer Center   Core Support Grant  to the  UNC Lineberger Comprehensive Cancer Center.
ACKNOWLEDGMENTS The authors thank  David Montero  and the  Institut des Matériaux de Paris Center (IMPC)  for the SEM-FEG characterization, the staff of the MPBT (physical properties -low temperature) platform of  Sorbonne University  for their support in SQUID measurements,  Laurent Lisnard  for his helping hand in XRPD and  Pierre Gouzerh  for his helping hand in IR spectroscopy and his as always precious advice.
Final models include all variables with a p value less than 0. 10 in multivariate analyses. Hazard ratios (HR) were presented with their 95% CI. Correlations between variables eligible for the multivariate models were tested. Time to local free recurrence was analyzed using univariate Cox model. Patients without local free recurrence and patients who died were censored at the date of last follow up. Due to the low number of events (n=10), multivariate analyzes were not performed. all tests were 2-sided. The significance level was set at 5%. All analyses were performed using SAS 9. 4.
Epidemiological data and tumor characteristics 65 men (57. 5%) and 48 women (42. 5%) were included. Median age at diagnostic was 63 years [min=20 -max=91]. 73 (64. 6%) tumors were located in the lower limb, 25 (22. 1%) in the trunk and 15 (13. 3%) in the upper limb. Tumor size, histological type, grade and depth were presented in Table  1.
Acknowledgments The authors wish to thank the following for their participation:  Pr Guy Leverger ,  Armand Trousseau  (Paris),  Pr Simon Tabassome, Saint-Antoine (Paris) , and  Dr Anne Auvrignon ,  Armand Trousseau  (Paris). We thank all participants in the ELAM02 protocol, as well as the medical centers that included children. We especially thank  Dr Marlène Pasquet ,  Dr Thierry Leblanc ,  Pr Virginie Gandemer ,  Pr Yves Bertrand ,  Dr Stéphane Ducassou ,  Pr Gérard Michel ,  Dr Brigitte Nelken ,  Pr Arnaud Petit , and  Pr André Baruchel. The ELAM02 protocol was a study under the aegis of the " Société Française de lutte contre les Cancers et les leucémies de l'Enfant et de l 'adolescent (SFCE) » and the  Belgian Society for Pediatric Hematology and Oncology (BSPHO). Pr Hélène Lapillonne, Armand Trousseau (Paris) , centralized the molecular biology analysis at diagnosis and during treatment.
The AE monitoring is conducted by means of multiple sensors using a PCI-2 data acquisition system (Mistras Group, Sucy en Brie, France). In order to study the sensors' effects, tensile tests are conducted with two types of sensors (nano30 and picoHF sensors) placed at the same position on each face of the specimen 40 mm apart (Figure  2 ). These two sensors show a good sensitivity in the frequency range of 200 to 400 kHz for nano30 sensor and 500-1850 kHz for picoHF sensor (Mistras Group data). Thus, by using both of them for tensile testing it is interesting to investigate, from an experimental point of view, the effect of the sensor on AE descriptors. In all tests, the coupling agent is medium viscosity vacuum grease. Each sensor is linked to a preamplifier (gain 40 dB, type 20 H). Each waveform is digitized and recorded.
We set the sampling rate to 2 MSPS or 5 MSPS in order to make a compromise between the respective peak frequencies of the sensors, the digitization capabilities of our system and the volume of data to be stored. The value of the acquisition threshold is equal to 32 dB, depending on the background noise and the acquisition parameters are set to 25 µs, 50 µs and 1000 µs for the peak definition time (PDT), the hit definition time (HDT) and the hit lockout time (HLT). All signals are filtered in the bandwidth 20-1200 kHz. Since two sensors are used, only the located signals along the gauge length are used. The AE wave velocities are measured with pencil lead breaks. The velocity is equal to 1750 m/s with nano30 sensors and to 1500 m/s with the picoHF sensors.
Fiber Break Model In this study, we perform all FEM simulations using the ABAQUS software (Dassault Systèmes Simulia Corp. , Providence, RI, USA) with dynamic calculations. We model the full geometry of the sample. Figure  3  shows the boundary conditions. Clamping jaws are taken into account as boundary conditions. The geometry is meshed using tetrahedral elements (C3D4), the element size varies between 0. 01 mm and 0. 2 mm and the calculation step time is 0. 1 µs. The resolution of the finite mesh is gradually refined from 0. 2 mm down to 0. 01 mm close to the model source. The element size determines the frequency range that can be modelled: smaller elements are required to capture higher frequencies. A total duration of 170 µs was calculated. Sensitivity studies are conducted on mesh refinement and for the size of the time step.