dataesr/scientific-paragraphs-categorization huggingface dataset:
One dimensional diffraction patterns were obtained in the 2θ range 0 • -43 • by integrating the two dimensional images with the program Fit2D  [103]. Some patterns were collected upon pressure release (labelled (rev) in Tables  and Figures). Unit cell parameters determination through Rietveld refinements was possible for all the ramps (Table  S1 ). The Rietveld structural refinements were performed on the ZL/0. 5FL, ZL/1FL composites at 2. 09 and 2. 01 GPa, respectively (from now on will be both labelled 2 GPa (i. e. , the highest pressures at which the quality of the diffraction patterns allowed the structural refinement) and upon complete decompression (P amb (rev)). All the structural refinements were carried out in the space group P6/mmm starting from the atomic coordinates reported by Gigli et al.
Equations of motion were integrated with the Car Parrinello Lagrangean  [98, 141]  adopting a time step of 0. 121 fs. The starting configuration for the P amb simulation corresponded to the minimum energy structure determined in  [56]. An equilibration trajectory of 5 ps was followed by 12 ps of production run. The final configuration obtained at P amb conditions was used as starting configuration for the 1. 95 GPa compression simulation. Also in this case, data were gathered from a 12 ps trajectory after a 5 ps equilibration run. In all cases, temperature was controlled via Nose-Hoover thermostats set at 300 K. In all the simulations, performed with the CPMD code  [142] , no constraints was imposed to the systems except for the experimentally determined cell parameters.
The final configuration obtained at Pamb conditions was used as starting configuration for the 1. 95 GPa compression simulation. Also in this case, data were gathered from a 12 ps trajectory after a 5 ps equilibration run. In all cases, temperature was controlled via Nose-Hoover thermostats set at 300 K. In all the simulations, performed with the CPMD code  [142] , no constraints was imposed to the systems except for the experimentally determined cell parameters.
Acknowledgments: BM01 beamline and the  European Synchrotron Radiation Facility  are acknowledged for the allocation of experimental beamtime. This work was supported by the  Italian MIUR , within the frame of the following projects:  PRIN2015  "ZAPPING" High-pressure nano-confinement in Zeolites: the Mineral Science know-how APPlied to engineerING of innovative materials for technological and environmental applications (2015HK93L7),  ImPACT  ( FIRB RBFR12CLQD ), and  University of Insubria Far 2016.
Statistical analyses The variables studied were analyzed with the PROC MIXED option in SAS software (version 9. 4), adopting 0. 05 as the criti cal level of probability for type I error, according to the following model: Y ijk = μ+T i +a j +p k +ε ijk Where, Yijk is the dependent variable measured in animal j that was subject to the i treatment in period k; μ is the gen eral mean; T i is the fixed effect of treatment i; a j is the random effect of animal j; p k is the random effect of period k; and ε ijk is the unobserved random error assuming normal. After analysis of variance, the significance of the linear and quadratic effects of the replacement of the total of wheat bran in the basal diet by cactus cladodes was evaluated. Rumen pH and NH 3 N were considered the effect of sampling time as repeated measures in time.
Follow-up Follow-up and mortality data were mainly gathered from clinical notes. Patients were evaluated at return visits every 3 mo during the first 2 years after treatment, every 6 mo for the following 3 years, and annually thereafter according to hospital policy. At each visit, physical examination, endoscopic examination, and CT scan of the cervix, chest and abdomen were performed. Suspicious recurrences were biopsied. Confirmation of recurrence required imaging or pathological evaluation. Information about tumor recurrence was updated every time the patient came for a follow-up visit. For those patients who did not come for a follow-up visit, data were gathered by phone calls, and/or mail contact with patients or their next of kin. The patients were followed for a median of 72 mo and a maximum period of 263 mo.
Background: Chikungunya epidemic is a public health problem in South-East Asian countries. There was an epidemic of chikungunyain the year 2016 in New Delhi. Therefore, this present study was planned to understand the epidemiological profile of Chikungunya cases attending fever clinic in a tertiary care hospital in New Delhi. Objective: To studyepidemiological and clinical profile of Chikungunya cases attending fever clinic in Safdarjung Hospital. Methods: A total of 200 patients with fever of up to 7days duration were enrolled at fever clinic of VMMC and Safdarjung Hospital, New Delhi from May 2016 to October 2016. Total number of 47874 fevercases were reported in fever clinic from May 2016 to October 2016. A preformed semi-structured, interviewer administeredquestionnairewas used for data collection.
Data collection A preformed semi-structured, interviewer administered questionnaire was used for data collection. (Annexure-1). Several aspect of chikungunya was assessed by the questionnaire such as socio demographic characteristics of the respondents and clinical profile of patients (n=200) like signs and symptoms and their duration, examination and assessment of functioning of joints. Detailed examination of joints regarding number of joints involved, any swelling, tenderness and restriction of movements of joints was carried out on each patient.
This new version of VFSMOD was applied to two contrasted benchmark field studies in France (sandy-loam soil in a Mediterranean semicontinental climate, and silty clay in a temperate oceanic climate), where limited testing of the model with field data on one of the sites showed promising results. The application showed that for the conditions of the studies, VFS efficiency decreases markedly when the water table is 0 to 1. 5 m from the surface. In order to evaluate the relative importance of WT among other input factors controlling VFS efficiency, global sensitivity and uncertainty analysis (GSA) was applied on the benchmark studies. The most important factors found for VFS overland flow reduction were saturated hydraulic conductivity and WT depth, added to sediment characteristics and VFS dimensions for sediment and pesticide reductions.
2a ). Pesticide reduction and transport in the filter during the runoff event is calculated within the water quality-pollutant module (Fig. 1 ) based on a generalized regression-based approach developed from a large database of field studies by  Sabbagh et al. (2009)  and further tested by others  (Poletika et al. , 2009; Winchell et al. , 2011). The equation considers reduction of dissolved pesticides through infiltration, deposition of sediment-bound pesticides, and pesticide adsorption characteristics. The integration of the mechanistic (flow and sedimentation from VFSMOD) and empirical pesticide approaches allows for identification of important site-specific factors determining the efficiency of pesticide removal (or lack thereof) under realistic field conditions  (Muñoz-Carpena et al.
4b ). To our knowledge there are no VFS experimental studies with a shallow water table present that can be used for systematic model testing. While this paper focuses on coupling of the new infiltration algorithm with VFSMOD and the analysis of the important factors controlling VFS efficiency in the presence of WT, we used the single event with sufficient hydrological data at Morcille to get a preliminary assessment of whether the model responds in the same range as the measured field data. Uncalibrated or "cold" testing of the model (without initial calibration using field values) was performed and the 95 % confidence interval (gray area in Fig. 4a ) was obtained by varying only K s within measured field values (Table  2 ). The model performance was assessed against the measured data based on FitEval software  (Ritter and Muñoz-Carpena, 2013).
, 1999). For pesticide inputs, field measurements of the percentage of clay (PTC) and organic carbon (PCTOC) of the upper field followed a uniform PDF  (Lacas, 2005; Benoit et al. , 1998; Madrigal-Monarrez, 2004). The triangular distribution for KOC for the pesticides evaluated at each site is based on measurements in Jaillière for the base value and boundaries  (Benoit et al. , 1998; Souiller et al. , 2002)  and on Morcille for the base value  (Lacas, 2005)  but using boundaries from the PPDB database  (IUPAC, 2007). In all, for the two sites, two infiltration options (GAMPT, without shallow water table and with k = 18, and SWINGO, with shallow water table and with k = 20, Table  2 ) and two pesticides at each site, the total number of GSA simulations performed were 75 544 for eFAST (M = 497 ≈ 512) and 1600 for Morris.
Uncertainty in the pesticide reduction, driven by water or sediment reduction, also depends on the pesticide sorption properties (KOC). This work suffers from several limitations. Firstly, limited field experimental data is available for detailed studies of the response of a VFS under alternative conditions of deep and shallow water tables. Further laboratory and field research should address this limitation, where exhaustive experimental datasets must be compiled to reduce the uncertainty in the identification of sensitive input factors controlling the measured and simulated responses studied here. To address this limitation, a comprehensive laboratory testing of the updated model under mesoscale controlled shallow water conditions was just presented by  Fox et al. (2017) , with successful results.
Acknowledgements. The authors wish to thank  Nadia Carluer  for the field testing dataset and selection of the study sites, as well as her review of the paper. Marilisa Letey  helped with the literature review for this paper. Axel Ritter  helped in the FitEval evaluation of the experimental data. Claire Lauvernet acknowledges TOPPS-PROWADIS for partial project funding. The second author received support from the  UF Research Foundation Professorship, UF Water Institute Fellowship , and  USDA NIFA  Award no. 2016-67019-26855. The authors also thank the  University of Florida Research Computing  (https://www. rc. ufl. edu) for providing high-performance computational resources and support that have contributed to the research results reported in this publication. Edited by:  Nunzio Romano Reviewed  by:  Stefan Reichenberger ,  Marnik Vanclooster , and one anonymous referee.
Background: General anaesthesia (GA) during endovascular thrombectomy has been associated with worse patient outcomes in observational studies. We examined the association between GA and functional outcome in ischaemic stroke patients with large vessel anterior circulation occlusion undergoing endovascular thrombectomy versus standard care in pooled data from available trials. Methods: Patient-level data were pooled from randomised trials listed in Pubmed 1/Jan/2010-31/May/2017 comparing endovascular thrombectomy performed using predominantly stent-retrievers with standard care in anterior circulation ischaemic stroke patients (HERMES Collaboration). The primary outcome was ordinal analysis of the modified Rankin scale (mRS) at 90 days in the GA and non-GA subgroups of endovascular-treated patients and patients randomised to standard care, adjusted for baseline prognostic variables.
common odds ratio (cOR) 1•52, 95%CI 1•09-2•11, p=0•014) and non-GA (adjusted cOR 2•33, 95%CI 1•75-3•10, p<0•001) patients. However, outcomes were significantly better for those treated under non-GA versus GA (covariate-adjusted cOR 1•53, 95%CI 1•14-2•04, p=0•004; propensitystratified cOR 1•44 95%CI 1•08-1•92, p=0•012). The risk of bias and variability among studies was assessed to be low. Interpretation: Worse outcomes after endovascular thrombectomy were associated with GA, after adjustment for baseline prognostic variables. These data support avoidance of GA whenever possible. The procedure did, however, remain effective versus standard care in patients treated under GA, indicating that treatment should not be withheld in those who require anaesthesia for medical reasons.
Introduction: Multiple observational studies have suggested that patients treated with endovascular thrombectomy under general anaesthesia (GA) have poorer outcomes than those treated without GA. 1  However, patients with more severe stroke or comorbidities may be more likely to be treated under GA, leading to the potential for confounding by indication. In MR CLEAN, sites specified their anaesthetic strategy prospectively and analysis of that trial found that the beneficial treatment effect of thrombectomy became nonsignificant in patients treated under GA. 2  These results could lead to a reluctance to convert from an awake procedure to GA in cases where patient agitation or challenging vascular anatomy are preventing optimal revascularization. 4] [5]  We analysed the pooled individual patient data from available randomised trials to assess whether a treatment benefit was preserved in patients treated under GA in broader contemporary practice.
This may be plausible if reduced patient movement allows more efficient roadmap techniques. However, the three centres that performed the randomised trials of GA achieved exceptionally fast anaesthetic induction that may not be common practice at most institutions. The main limitation of this study is that the choice to use GA versus non-GA was not randomised and the differentiation between medically required GA versus elective GA was not recorded in the trial databases. The important prognostic variables of age and time from stroke onset to randomisation favoured the GA group. We used two different methods of adjustment for baseline imbalances (multivariate regression and propensity-score stratification) which gave consistent results. Nonetheless, for both methods the possibility of unmeasured confounding remains.
The anaesthetic practices in the HERMES trials were not pre-specified by protocol nor recorded in detail but are likely to have been substantially more variable than the recent single centre randomised trials comparing GA versus no GA. However, this also represents a strength of our study as results are likely to be generalizable to current clinical practice. The risk of bias in component trials was overall assessed to be low. In conclusion, the HERMES data suggest that GA for endovascular thrombectomy, as practiced in contemporary clinical care across a wide range of expert centres during the randomised trials, is associated with worse outcome compared to avoiding GA, independent of patient co-morbidities. Patients still benefited from thrombectomy compared to standard care when treated under GA.
Acknowledgment nil  A. Demchuk  reports personal fees from  Covidien (Medtronic). S. Bracard: Has  nothing to disclose. P. White reports grants from  National Institutes for Health Research, Stroke Association, Medtronic (Covidien)  and  Codman  and has consulted for Microvention Terumo and  Codman. A. Dávalos  reports lecture fees, consultancy and advisory board fees from  Medtronic Neurovascular (Steering Committee STAR)  and unrestricted grant for the REVASCAT trial from  Medtronic  (paid to institution). C. B. L. Majoie reports an unrestricted grant from  Stryker  (paid to institution). A. V. D. Lugt reports honoraria from  Stryker  (paid to institution). G. A. Ford reports grants and personal fees from  Medtronic , personal fees from  Pfizer ,  Athersys ,  AstraZeneca ,  Lundbeck ,  Cerevast ,  Daiichi Sankyo  personal fees and non-financial support from  Boehringer Ingelheim , grants from  Pulse Therapeutics.
STATISTICAL DISTRIBUTIONS OF G, G AND L θ The distributions of the features are studied by using a Kernel smoothing function f w which is defined as follows  (Rosenblatt, 1956; Parzen, 1962) : f w (x) = 1 nw n ∑ i=1 K( x -x i w ) , (28) Table  2. Using AR-based method for PSD estimation in polar coordinates (Fig. 4  & 5), statistics of distance (Eq. 23), distance variation (Eq. 24) and tangential length (Eq. 27) features of the detected lobe of catalyst image databases (Cat 1 and Cat 2 ). where n is the sample size, {x i } i=1,. ,n are the set of considered samples, x ∈ R, K(•) is the kernel smoothing function and w is the bandwidth. For these catalysts, the inter-distance between two neighboring white/black fringes G is known to be close to 0. 615 nm (see  Geantet and Sorbier (2012) ). In Table  2 , G has almost same value for Cat 1 and Cat 2 (0.
KOLMOGOROV-SMIRNOV TEST FOR CATALYST DISCRIMINATION In this section, we propose Kolmogorov-Smirnov (KS) test for comparing Cat 1 and Cat 2 ARFBF morphology characterizations. The KS measure is given by (see  (Peacock, 1983)  for details) K = max x (| f1 (x) -f2 (x)|), (29) where f1 , f2 are the empirical cumulative distribution functions of catalyst datasets indexed by '1' and '2'. Function f is hereafter the kernel distribution for one of the three features: G, ∆ G and L θ. A threshold, based on asymptotic of K , is used to derive a decision between alternative hypotheses: null hypothesis (H = 0) is that the two samples are drawn from the same catalyst or H = 1 means that the test rejects the null hypothesis at 5% significance level. First, Table  4  highlights that Kolmogorov-Smirnov test makes a clear discrimination between the two catalysts effective when considering parameters G and L θ.
Our observations in Africans confirm those made in a Chinese population, in which 64% of patients with HBV-MN also had PLA2R antigen in immune deposits. 18 The mechanisms whereby HBV may trigger autoimmunity may involve molecular mimicry, alterations of regulatory T-cells (Treg), or Bcell activation. 23, 24 HBV scanning of protein databases has revealed regional similarities between HBV proteins and antigenic targets of nuclear and smooth muscle antibodies. 25 Alignment of the immunodominant peptide of PLA2R against a database of microbial proteins identified a small sequence shared by a cell wall enzyme, D-alanyl-D alanine carboxypeptidase, common in several bacterial strains, including Clostridia species, but no mimicry of HBV viral antigens. 26 No direct link between Treg number and/or function and HBVrelated immunopathological manifestations has been reported.
ACKNOWLEDGEMENTS This study was funded by grants from the  European Research Council   ERC-2012-ADG_20120314 (Grant Agreement 322947 ) and from the  7th Framework Programme  of the European Community Contract  2012-305608  ( European Consortium for High-Throughput Research in Rare Kidney Diseases ). LB was supported by a grant from the  Swiss National Foundation  ( P2GEP3_162179 ).
| Phylogeny Based on a previous Palaemonidae phylogenetic study  (Kou et al. , 2013) , we used four genes to construct a focused community phylogeny; partial fragments of the 16S ribosomal RNA (rRNA) gene (~368 bp), and partial fragments of three nuclear genes; enolase (~405 bp), PEPCK (~521 bp), and NaK (~620 bp). Nineteen of the twenty species from the metacommunity were represented by at least two genes in the consensus phylogeny (see Table  S2 ). Only Exoclimenella maldevensis was not included in the consensus phylogeny as we were only able to amplify the 16S gene for this species. As this species was rare in the community, occurring only once, it was excluded from further analysis. An additional 26 species were included in the phylogeny (from Chagos samples and available specimens on GenBank) to provide more information on the evolutionary relationships between species in the metacommunity.
Phylogenetic trees were constructed under Bayesian Inference (BI) analysis in MrBayes v. 3. 2  (Ronquist et al. , 2012)  (see Table  S3  for models of evolution used), on the online CIPRES Science Gateway  (Miller & Schwartz, 2010)  for the consensus alignment and for each gene tree separately. A composite metacommunity phylogeny was produced in APE using the phylogeny (Figure  2 ;  Paradis, Claude, & Strimmer, 2004). All sequences were catalogued on GenBank. See Appendix S1 for a detailed methodology.
However, four gravid females were excluded from the analysis as a result of damage to the egg sac and/or suspected shedding of eggs during collection. The longest and shortest diameter of ten randomly selected eggs from each female were measured to the nearest 4 μm. Total egg number per female was also counted. To establish a measure of fecundity, linear regression and ANOVA were used to evaluate the relationship between egg number with egg size and with female body size. The relationships were plotted and a generalized additive model (gam) used to obtain a line of best-fit. Egg number was then adjusted to take account of egg size as a measure of fecundity (see Appendix S2). Fecundity data were also interpolated, with respect to body size, for all species. The trait diversity analysis was then preformed on both the original fecundity data and the interpolated data to identify potential error caused by the small sample size of fecundity data (see Appendix S2).
| Community phylogenetic analysis To test for phylogenetic signal in the quantitative traits, we used the K-statistic  (Blomberg, Garland, & Ives, 2003) , using the R package "phyltools"  (Revell, 2012). This was preformed twice; once incorporating sampling error following  Ives, Midford, and Garland (2007) , as our data have within-species variation which is not accounted for in other methods to the best of our knowledge, and for a second time without taking within species variation into account. Phylogenetic signal in the nominal trait of habitat association was tested using  Maddison and Slatkin (1991)  method which compares the minimum number of trait changes to the distribution of trait changes drawn from a null model. We used function "phylo. signal. disc" in R environment, developed by Enrico Rezende (Universidad Autònoma de Barcelona) (http://grokbase.
com/k-for-discrete-unordered-traits). To investigate functional (trait) diversity and phylogenetic patterns in trait diversity across distinct spatial scales, we used the third proposition of  Pavoine, Marcon, Ricotta, and Kembel (2016)  to divide Rao's measure of diversity, named quadratic entropy (QE),  (Rao, 1982)  across spatial scale, using the R package "adiv"  (Pavoine, 2017). This partitioning of diversity is adapted to unbalanced sampling design. Quadratic entropy is also relatively robust to samplingeffects because this method is an extension of the Simpson index for functional and phylogenetic data, which gives high weight to common species  (Lande, 1996). Therefore, rare species perhaps not identified by under-sampling are unlikely to impact the index even if they are functionally or phylogenetically distinct from others.
The QE index of diversity uses the phylogenetic tree, distributions of relative abundances of species in a community, and a matrix of trait distances among species obtained by Gower distance  (Gower, 1971) , to assess whether there is any phylogenetic and/or trait clustering in the metacommunities and local communities  (Pavoine et al. , 2010). Phylogenetic and/or trait clustering are measured using the beta diversity standardized effect size (SES), which calculates the observed beta diversity minus the mean of simulated beta diversities, divided by the standard deviation of simulated beta diversities. The trait-based apportionment of quadratic entropy across spatial scales will be referred to as the trait quadratic entropy test  (TQE)  and that based on phylogenetic data as the phylogenetic quadratic entropy test (PQE).