dataesr/scientific-paragraphs-categorization huggingface dataset:
Discussion This study shows that the QoLEB, in its Spanish version, is a valid and reliable scale which makes it possible to measure the quality of life of persons who suffer from EB in Spain. The internal consistency of the QoLEB in Spanish is high, α = 0. 91, a result similar to that obtained in the validation of both the original (α = 0. 931) and Dutch questionnaires (α = 0. 905). Convergent validity is high, since the chi-squared test and factor loadings indicate that there is a high proportion of variance in common. Discriminant validity between the SF-36 and Spanish-version QoLEB questionnaires is high, HTMT = 0. 681 (heterotrait-monotrait ratio of correlations), with the result being less than 0. 85. In general, the average scores obtained in the Spanish version of the QoLEB were higher than those recorded in the Dutch questionnaire, as was also the case in the scores reported for the original English questionnaire and in data collected on EB-affected adults in Brazil.
This open-label, multicenter, single-arm, phase 2 study assessed the safety and efficacy of blinatumomab consolidation therapy in adult patients with newly diagnosed, high-risk diffuse large B-cell lymphoma (DLBCL; International Prognostic Index 3-5 and/or double-/triple-hit or double MYC/BCL-2 expressors) who achieved complete response (CR), partial response (PR), or stable disease (SD) following run-in with 6 cycles of R-chemotherapy (NCT03023878). Of the 47 patients enrolled, 28 received blinatumomab. Five patients (17. 9%) experienced grade 4 treatment-emergent adverse events of interest (neutropenia, n ¼ 4; infection, n ¼ 1). Two deaths reported at the end of the study were unrelated to treatment with blinatumomab (disease progression, n ¼ 1; infection, n ¼ 1). 3/4 patients with PR and 4/4 patients with SD after R-chemotherapy achieved CR following blinatumomab.
Study design and treatment This open-label, multicenter, single-arm, phase 2 study was conducted at 24 centers across North America and Europe (ClinicalTrials. gov, NCT03023878) and was designed to investigate the safety and efficacy of treatment with blinatumomab following induction with Rchemotherapy in patients with newly diagnosed, highrisk DLBCL. The study protocol was approved by the ethics committee or the institutional review board at each clinical site. Enrolled patients were required to complete a run-in period, wherein patients were administered six cycles of R-chemotherapy (Figure  1(A) ). Patients who demonstrated complete response (CR), partial response (PR), or stable disease by positron emission tomography/computed tomography (PET/CT) done 3 weeks (±3 days) after six cycles of R-chemotherapy and assessed by a central radiology reviewer per Lugano classification and size of the target lesions went on to receive treatment with blinatumomab  [15].
Acknowledgments The authors thank all the site investigators and patients who participated in this study. Swapnil Kher, PhD , of  Cactus Life Sciences  (part of  Cactus Communications ) and  Ben Scott, PhD  ( Scott Medical Communications, LLC ) provided medical writing assistance funded by  Amgen Inc. Graphics support was provided by  Robert Dawson  of  Cactus Communications  and funded by  Amgen Inc. This study was funded by  Amgen Inc  and  Astellas Pharma Inc. The funders contributed to study design, data collection, data analysis, and data interpretation, and funded a professional medical writer to assist with writing the report. Disclosure of interest D. A. K. received honoraria from and fees for consulting or advisory role and speakers' bureau from  AbbVie and Stemline. M. P. C. received fees for consulting from  Teva Pharmaceuticals.
C. T. received fees for consulting or advisory role from  Amgen ,  Celgene ,  Jazz Pharmaceuticals, Kite/Gilead ,  Novartis ,  Servier , and  Roche  and received research funding from  Roche ,  Celgene , and  Hospira. N. J. M. received fees and honoraria from  Kite/Gilead ,  Janssen , and  Amgen Inc. A. V. received honoraria from and fees for consulting or advisory role and speakers' bureau from  Amgen ,  Roche ,  Kite/Gilead , and  Novartis. A. M. G. -S. received honoraria from and fees for consulting or advisory role and speakers' bureau from  Celgene ,  Servier ,  Gilead ,  EUSA Pharma ,  MorphoSys ,  Kyowa Kirin , iQone, and  Roche ; research grant from  Celgene  and  Janssen ; and non-financial support/travel fees from  Celgene ,  Janssen ,  Servier ,  Roche , and  Celltrion. G. R. -G.
Process of data collection for the study A total of 13 caregivers from various care professions were interviewed: two speech therapists (both female), two family medicine practitioners (one female, one male), one dentist (male), one physiotherapist (female), three psychotherapists (two females, one male), four nurses (with various specializations, three females, one male). All participants were native French speakers. The interviews took place in the interviewee's workplace or in a meeting room located in one of the authors' research institutions. No strict control was enforced for variables such as the interviewee's gender or the match or mismatch between the interviewer and interviewee's genders. This study follows the Helsinki Declaration (World Medical Association, 2013). The primary objective of our research was to generate new knowledge on care, without prevailing over the health, well-being, and rights of our participants.
Their transcriptions, with added information about time and numbered interventions assigned to the interviewer or the interviewee, contained a total of 117,142 words, with a mean number of 11,714 words per transcription and a standard deviation of 3,286 words. Transcriptions are available upon request to the corresponding author. Information on the educational and training background, the number of years of practice and the professional context of intervention (private/public practice, patients etc. ) was also collected to provide a number of meta-data for later analysis. Upon carefully reading the 11 transcriptions, 7 were considered for further analysis.
These sexual differences in Sr/Ca values could also reflect physiological differences between males and females specific to this species of Hexanchus. 3 ). The latter ratios in H. griseus females show a Sr/Ca ratio of 5. 93 (n = 5) significantly higher than that of males (2. 68, n = 6) (Wilcoxon P value = 0. 004). Even if the process remains unclear, it could result from physiological as well as spatial differences, and could allow us to determine a posteriori the sex of undocumented material in historical collections using Sr/Ca ratios. Considering this, among the specimens that do not display sex information in our dataset we speculate that these specimens represent one female and four males. In this paper, Sr/Ca and Mg/Ca ratios are reported to be significantly higher in H. griseus than in I.
This hypothesis is supported by a lack of difference in sexual variations in other shark species, including our whole dataset of Isurus and Carcharodon as well as the previously published dataset of Akhtar et al. (2020) (e. g. , Carcharhinus, Galeocerdo, Sphyrna, Lamna, Carcharias, Hemipristis, Negaprion, Prionace, Somniosus) (Akhtar et al. , 2020), which all fall within the Sr/Ca range of Hexanchus males. It is noticeable that specimens from H. griseus whom sex is unknown and whom Sr/Ca was analysed (n = 5), present Sr/Ca values consistent with the two groups based on sex information (Figure.
ACKNOWLEDGEMENTS We thank  Henri Cappetta  for providing the osteological specimens of sharks that are presented in this analysis. We also acknowledge  Hakan Kabasakal  for his valuable help in obtaining enamel samples. We are grateful to  Vincent Balter  for discussions and encouragement as well as  Emmanuelle Albalat  for help in the clean laboratory and  Philippe Telouk  for his support with the instruments. We thank  CNRS  ( INSU INTERRVIE ) and  ENS de Lyon  facilities, which permitted the geochemical analyses. We thank the anonymous reviewers for their help in improving the manuscript.
Data Collection The material for analysis was gathered through semi-structured interviews, using an interview guide with phenomenologically oriented questions centered on the participant's lived experiences (Appendix. 1). To stay as close as possible to the experience the in-person face to face interviews were conducted between one-and three-weeks post intervention. The interviewer made sure to create an atmosphere of con dence so that responses would be spontaneous. The interviews were recorded, anonymized, and verbatim transcribed. We used purposive sampling  (Patton, 2001)  to obtain a diversity of medical students' experiences across various characteristics such as age, sex, university and academic level. We applied the principle of data saturation without pre-de ning the number of interviews.
Acknowledgments All authors would acknowledge support from the  École Polytechnique and its Laboratore de Mécanique des Solides (LMS). The work was initiated in part by grants from  École Polytechnique  and the C. N. R. S. ( Centre National de Recherche Scientifique ) during the AY 2017-2018, while TJH was a Distinguished Visiting Professor and SSP a visiting doctoral student. RSE acknowledges several visits to LMS during this period supported by the  LMS. The work of  SSP  was also supported in part by the  National Science Foundation (NSF)  through grant  DMS-1613753. TJH also acknowledges partial support from that grant and from  NSF  grant  DMS-2006586. The work of RSE was also partially supported by the  NSF  grant  CMMI-1462826 , and he acknowledges the  Minnesota Supercomputing Institute (MSI)  at the  University of Minnesota  for providing resources that contributed to the research results reported within this work.
Participants The Cognitive Bias Questionnaire for Psychosis (CBQp)  [49]  was administered to the control group (N = 663) either in paper format to several undergraduate classes at the University of Montreal or online through a survey website that was shared across several social media networks. Data from 84 participants were excluded due to too many missing answers. Therefore, 579 control participants were retained for statistical analysis. In addition to the controls, 62 participants with either a psychotic disorder (N = 30) or mood disorder (depression; N = 32) responded to the paper version. These participants were recruited through other ongoing studies in Quebec and France. Participants with a psychotic disorder were receiving services at a clinic for psychotic disorders and did not present with substance-induced psychosis.
Finally, cluster analyses were conducted to investigate cognitive biases across diagnostic groups (without the healthy controls). The variables used for the cluster analyses were the score for the five cognitive biases (Catastrophising, Dichotomous Thinking, Emotional Reasoning, Intentionalising and Jumping to Conclusions). Scores were standardized prior to the cluster analysis. We conducted a Clustering ensemble to ensure a more rigorous approach to cluster analyses  [71, 72] , which includes three methods (Hclust: Hierarchical clustering in R, with Ward Linkage  [73] ; the DB scan  [74]  and the K-means Clustering  [75] ). The data was then clustered using the number of times each pair of subjects had been classified together in the same group as a proximity value. The solution based on this last clustering was our final solution.
The nitrocefin-based test (Nitrocefin SR112, Oxoid microbiology Products, USA) for beta-lactamase production was negative. The treatment with ceftriaxone (4 g/day) was therefore switched to amoxicillin (8 g/day) for 4 weeks. The evolution of infectious process was favorable and the patient remained apyretic throughout his stay. The aortic insufficiency was treated using a mechanical prosthesis after 4 days of medical antibiotic treatment. The culture of the native valve remained sterile and molecular typing with 16 S rRNA gene sequencing confirming Cardiobacterium hominis identification (accession number LR134365. 1) based on a 100% identity, using the NCBI database.
Antivirals as therapeutics to treat NDs As aberrant deposition of Aβ is believed to initiate the detrimental cascade of Tau aggregation and neuronal death  [57] , current clinical trials for AD mainly target Aβ, albeit with limited therapeutic outcome  [58]. Antivirals might thus represent interesting alternative drug candidates for the treatment of NDs. In cell culture, antivirals were able to lower HSV-1-induced Aβ production and phosphorylated Tau  [59]  or influenza-A-mediated α-Synuclein aggregation  [45]. Analyses of large medico-administrative databases support this and suggest that antiherpetic therapy could decrease the risk of developing AD  [60]. However, a Phase II pilot trial with a high dose oral administration of antiherpetic drug valacyclovir for 4 weeks failed to show changes in ND markers in patients with early-stage AD  [61].
Studies were excluded if: (i) they exclusively included paediatric patients, drug users or blood donors; (ii) patient recruitment started before 2000; (iii) they were not written in French or English; or (iv) they did not present original results. Article titles and abstracts were screened by two independent investigators (M. C. and P. H. ) using the Covidence review tool. 14 Fulltext articles were then retrieved and assessed for their eligibility by the same two authors. Any conflict in articles screening or full-text assessment were resolved by a third senior researcher (K. J. or L. T. ). For each study, the following data were extracted by P. H. : total number of patients; patient type; study design; and measures of association and sample size of the exposed/non-exposed groups. Any doubt concerning data extraction was resolved by a senior researcher (K.
Data analysis The procedures were categorised into 10 groups and validated by medical experts (L. B. L. N. and Y. S. ) (Table  1 ; Table  S10 , Text S2). Risk of blood-borne infection was supposed to be the same within these groups. Measures associated with the same procedure but reported across different populations (e. g. by gender) were considered independently in the meta-analysis. We performed random-effect meta-analyses to pool ORs for an association between each procedure group and the risk of HCV infection using the R 'meta' package. 15 When two or more distinct procedures were classified in the same procedure group within the same study population, a three-level model  16  was used to account for the dependence between the measures of association. I 2 statistics were used to assess the heterogeneity across the studies.
17 Procedure-specific pooled ORs were stratified by country for the two most represented procedure groups. In addition, subgroup analyses were performed to compare estimates between cohort and non-cohort studies. Third, the pooled OR for blood transfusion based on transfusions performed with either recent dated or an unspecified date of realisation was compared to the one based on transfusions performed before 1998, which is the latest cut-off date used within selected articles. Indeed, we assumed cut-off dates found in the studies selected to reflect local implementation of mandatory HCV screening in blood donors. Finally, meta-regressions were performed to investigate the potential effect modifier of: (i) the HCV prevalence level (as a continuous variable), and (ii) the Healthcare Access and Quality (HAQ) index, a 0-100 score quantifying the strength of healthcare quality and access based on amenable mortality data in each country (Table  S9 ).
A central tool for the proofs in this last section is an adaptation of the proof of the one-jump lemma from  [ , Appendix B]  to the diagonal convergence of the perimeter processes (Appendix A). No. ), as well as the ERC Advanced Grant (QFPROBA). The second author also acknowledges support from the Icelandic Research Fund (Grant Number: -) as well as from the LABEX MILYON (ANR--LABX-) of Université de Lyon, within the program « Investissements d'Avenir » (ANR--IDEX-) operated by the French National Research Agency (ANR).
Acknowledgements. The authors would like to thank  M. Albenque ,  J. Bouttier ,  S. Charbonnier ,  K. Izyurov ,  M. Khristoforov ,  A. Kupiainen  and  L. Ménard  for enlightening discussions. Both authors have been primarily supported by the  Academy of Finland  via the Centre of Excellence in Analysis and  Dynamics Research  (project.
KaiC WT , KaiC S258A , KaiC F247A , KaiC Q361E , KaiC N390A , KaiC F470Y , and KaiC DE were concentrated up to 15. 0, 12. 3, 14. 6, 14. 3, 16. 9, 8. 5, and 9. 7 mg/mL, respectively. Each 1-mL sample was placed in a double-cylindrical aluminum cell with a sample thickness of 0. 5 mm and sealed tightly with indium wire. QENS experiments. QENS data were recorded using the near-backscattering spectrometer installed at beamline BL02 (DNA) in the Material and Life Science Experimental Facility of Japan Proton Accelerator Research Complex (MLF/J-PARC), Tokai, Ibaraki, Japan  30. QENS spectra were recorded over an energy transfer range from -0. 5 to 1. 5 meV with energy resolution (12 μeV) enabling us to access motions faster than ~55 ps. QENS data were collected at 283, 293, 302, 310, 313, and 317 K with exposure times of 6-10 h for each condition (520-615 kW).
The obtained S(Q,E) were corrected for detector efficiency using a vanadium standard, and intensities were normalized as relative intensities using the standard after subtracting the contributions of the empty cell. The background spectrum of the D2-buffer was subtracted from each sample spectrum on the basis of scaling factors calculated from neutron scattering cross-sections, as reported previously  35, 36. The temperature was controlled by an LS350 (Lakeshore) with He conductance gas through a GM refrigerator and heat transfer from a cartridge heater installed in a copper block at the top of a sample cell, while monitoring the temperature at the bottom of the cell. Estimation of the Q10 values. Datasets with more than two temperature points were subjected to Arrhenius plot analysis, and the resulted activation energy (E a ) was converted to the Q10 value at 303 K using exp{(E a /R)(10/T/(T + 10))}, where T and R represent temperature and the gas constant, respectively  65.
Acknowledgements We thank  Dr. K. Shibata  for his kind support for the trial QENS experiment, and  Dr. M. Kataoka  and  Dr. H. Kamikubo  for their discussions and critical comments on the manuscript. This study was partly supported by  Grants-in-Aid for Scientific Research  ( 17H06165  to S. A. ). The QENS experiments using BL02 (DNA) at the  Materials and Life Science Experimental Facility  of the J-PARC were performed under user programs (Proposal No. 2017B0123 ,  2018B0244 ,  2019A0308 , and  2020B0073 ).
Acknowledgments: The authors would like to thank the anonymous referee for numerous comments on the manuscript which led to several clarifications and an important improvement of the manuscript. S. R. is on leave of absence from Univ. Lyon, Université Claude Bernard Lyon 1, CNRS UMR 5208, Institut Camille Jordan, 43 blvd. du 11 Novembre 1918, F-69622 Villeurbanne CEDEX, France.
We identified 12,111 quasiindependent GWS SNPs, including 9,920 (82%) primary signals with a GWS marginal effect and 2,191 secondary signals that only reached GWS in a joint regression model (Suppl. Table 10). Of the GWS SNPs obtained from the non-EUR meta-analyses above that were conditionally independent of the EUR GWS SNPs, 0/2 in SAS, 5/19 in AFR, 27/49 in EAS, and 39/143 in HIS remained statistically significant in our METAFE (Suppl. Table  9 ), meaning that a small number of additional signals were only identified in the ancestry-specific analyses. We next sought replication of the 12,111 METAFE signals using GWAS data from 49,160 participants of the Estonian Biobank (EBB). We first re-assessed the consistency of allele frequencies between our METAFE and the EBB set. We found a correlation of allele frequencies of ~0.
98 between the two datasets and a mean FST across SNPs of ~0. 005, similar to estimates obtained between populations from the same continent. Of the 12,111 GWS SNPs identified through our COJO analysis, 11,847 were available in the EBB dataset, 97% of which (11,529) have MAF>1% (Suppl. Table 10). Given the large difference in sample size between our discovery and replication samples, direct statistical replication of individual associations at GWS is not achievable for most SNPs identified (Suppl. Fig. 10a ). Instead, we assessed the correlation of SNP effects between our discovery and replication GWAS as an overall metric of replicability. 1, 13 Over the 11,529/11,847 SNPs with a MAF>1% in the EBB, we found a correlation of marginal SNP effects of   =0. 93 (jackknife standard error; S. E.
Genomic distribution of height-associated SNPs To examine signal density among the 12,111 GWS SNPs detected in our METAFE, we defined a measure of local density of association signals for each GWS SNP based on the number of additional independent associations within 100 kb (Suppl. Fig. 12 ). We observed that 69% of GWS SNPs shared their location with another associated, conditionally independent, GWS SNP (Fig. 1 ). The mean signal density across the entire genome is 2. 0 (LOCO-S. E. = 0. 14), consistent with a nonrandom genomic distribution of GWS SNPs. Next we evaluated signal density around 462 autosomal genes curated from the Online Mendelian Inheritance in Man (OMIM) database  14  as harbouring pathogenic mutations causing syndromes of abnormal skeletal growth ("OMIM genes"; Suppl. Methods; Suppl.
SC measurement. The same NHSOPS-F questionnaire was administered to the two groups prior to the implementation of the training package (January 2016), and again around 18 months later (September 2017). It was important that the NH took ownership of the support system over time. The methodology for the distribution and collection of questionnaires has been extensively described in an earlier article  [21]. To summarize, in each NH the two contact points were responsible for: distributing the questionnaire to each professional working in the NH; promoting and following-up the survey; centralizing the completed questionnaires; and returning them to the research team  [21]. The survey was conducted over a sixweek period. Each completed questionnaire was given a number to ensure anonymity. Responses were recorded by an external technician, and data capture was blind, in duplicate, with cross-checking.
• Template operating charter for the RM steering group. • Template procedure for reporting AEACs. • Template AEAC report form. Technical Session 3 • Train members of the RM steering group in the monitoring and analysis of • Computerized database for recording AEACs. and monitoring AEACs. Session 4 • Provide support during the first analysis. AEAC: adverse events associated with care RM: Risk Management https://doi. org/10. 1371/journal. pone. 0277121. t001 Dimension 7 (Feedback and communication about incidents) explores how potential or actual incidents are dealt with, and solutions are shared.
Acknowledgments We thank  B. Ananthanarayan ,  Pawel Caputa ,  Shouvik Datta  and  Chethan Krishnan  for comments on the draft. XC would like to thank  Daniel Parker ,  Thomas Scaffidi  and  Tianrui Xu  for discussions and collaborations in related topics. PN thanks  Aranya Bhattacharya ,  Arpan Bhattacharyya ,  Pawel Caputa ,  Pingal Pratyush Nath  and  Aninda Sinha  for useful discussions and ongoing collaborations. BB is supported by the  Ministry of Human Resource Development (MHRD), Government of India  through the  Prime Ministers' Research Fellowship. PN is supported by the  University Grants Commission (UGC), Government of India.