dataesr/scientific-paragraphs-categorization huggingface dataset:
Statistical analysis Continuous variables are expressed as mean + SD and categorical variables as frequency and percentage. Use of antithrombotic therapy at baseline was analysed by CHA 2 DS 2 -VASc and 'modified' HAS-BLED (excluding fluctuations in the international normalized ratio) scores, calculated retrospectively from the data collected. Patients with missing values were not removed from the study. Occurrence of major clinical outcomes is described using the number of events, the proportion of patients with the event divided by the population at risk at the beginning of the follow-up period, person-time event rate (per 100 person-years), and 95% confidence interval (CI). We estimated person-year rates using a Poisson model, with the number of events as the dependent variable and the log of time as an offset, i.
e. a covariate with a known coefficient of 1. Only the first occurrence of each event was taken into account. The 4-monthly event rates were compared with the overall rates using the ratio between the observed and expected numbers of events (applying the overall rate to assess expected rates for that period). The Poisson trend statistic was used to assess the trends over time. Hazard ratios (HRs) were estimated using a proportional hazards Cox model after multiple imputation by the Multiple Imputation by Chained Equations (MICE) algorithm. 7, 8 We used the MICE algorithm to fill in missing values, creating five complete datasets. Data analysis was performed at the TRI with SAS version 9. 4 (SAS Institute Inc. , Cary, NC, USA) and Stata Statistical Software: Release 13 (StataCorp, College Station, TX, USA).
Discussion Analyses of event rates from the GARFIELD-AF registry have identified that death was the most frequent major adverse clinical event over 2 years of follow-up in patients with NVAF. The rate of death was three-fold higher than the rate of stroke/SE and more than five-fold higher than the rate of major bleeding. The highest frequency of events (for each major outcome measure) occurred during the first 4 months of follow-up. The early risks of death and major bleeding (but not stroke/SE) were higher with new (newly diagnosed/new onset) NVAF than with the other patterns of NVAF. These data suggest that incident NVAF may occur as a complication of a chronic or acute cardiovascular or non-cardiovascular underlying disease that impairs early evolution. 10 -13 In addition, fluctuations in AC control, which are commonly observed after the initiation of VKA therapy, may explain, at least in part, the early excess of  Includes patients with unknown types of stroke and those with both primary ischaemic and primary intracerebral haemorrhagic strokes.
Study strengths Several surveys, registries, and regional or national healthcare databases have reported outcomes for patients with NVAF but most studies had a limited duration of follow-up. 30 -37 Prior studies vary in terms of inclusion criteria, duration of follow-up, and care settings, and in the characterization of outcome events. In contrast, the design of the GARFIELD-AF registry is unique; it has a global reach and extended follow-up and incorporates patients with newly diagnosed NVAF from all care settings, making it representative of real-life management of NVAF worldwide. In addition, GARFIELD-AF audit and quality assurances exceed the standards of most large-scale registries and even some randomized trials. 5.
Acknowledgements We thank the physicians, nurses, and patients involved in the GARFIELD-AF registry,  Martin van Eickels  ( Bayer HealthCare Pharmaceuticals, Berlin, Germany ) for his contribution to the study design, and  Karen Chiswell  and  Karen S. Pieper  ( Duke Clinical Research Institute, Durham, NC, USA ) for their statistical expertise. Editorial support was provided by  Claire Aukim-Hastie ,  Emily Chu ,  Rae Hobbs , and  Jane Tricker  (TRI). SAS programming support was provided by  Jagan Allu (TRI).
If HV <70 ms Based on literature data in patients with bundle branch block associated with syncope in a non-TAVI context, this group is at low risk of high-grade conduction disturbances. A Biomonitor subcutaneous loop recorder (Biotronik, Berlin, Germany) will be implanted -in the left subclavian position for patients implanted with the first-generation Biomonitor (used at the start of the study), and thereafter in the left parasternal position for patients implanted with the second-generation Biomonitor, which will be used starting at the end of 2015. The parameters will be programmed in a homogeneous manner: bradycardia alert when the heart rate is <40 beats/min and the occurrence of a pause >2 s.
This sample size (n=200) is deemed sufficient to address the objective of determining the prognostic factors of high-grade conduction disturbances in the event of de novo LBBB  14  with satisfactory statistical power. No particular consideration will be given to sample size estimation associated with the safety objective. Each patient presenting with an adverse event will be investigated by the Data Monitoring Safety Committee who will decide (1) the accountability of the device or treatment and (2) whether the study should be continued.
Statistical analysis Statistical analysis will be performed with Stata software. The tests will be two-sided, with a type I error set at α=0. 05. The epidemiological, clinical and biological characteristics as well as treatment will be analysed as follows: quantitative variables will be presented as mean (SD) or median (IQR) according to the statistical distribution (assumption of normality will be assessed using the Shapiro-Wilk test). To evaluate time to occurrence of high-grade conduction disturbances, censored data analyses will be considered. Time intervals will not be determined by observed dates of events but by fixed intervals. The estimation of time to occurrence of high-grade conduction disturbances will be performed by an actuarial method. The safety analysis will be primarily descriptive.
Each patient presenting with an adverse event will be studied independently by the Data Monitoring Safety Committee. To determine prognostic factors of highgrade conduction disturbances, the following statistical analysis scheme is proposed. Univariate analysis will be performed using a log-rank test for categorical variables and a Cox proportional hazards model for quantitative outcomes. When appropriate, quantitative variables will be categorised according to clinical relevance and statistical distribution and after studying the receiver operating characteristic (ROC) curve and estimating several of the usual indices (Youden, Liu, efficiency and greyzone). In multivariate analysis, Cox regression models will be performed with covariates fixed according to univariate results and clinical relevance.
Finally, repeated longitudinally collected data (including EQ-5D scores) will be analysed using random-effects models taking into account within-and between-subject variability. As proposed by several statisticians, all individual p values will be reported without systematically performing a mathematical correction for distinct tests. 16 Particular focus will be given to the magnitude of difference and to clinical relevance. 17 A sensitivity analysis will be proposed in order to study the statistical nature of the missing data and to propose the most appropriate approach to imputation of missing data.
Data Monitoring Safety Committee A Data Monitoring Safety Committee (independent of the sponsor) will meet initially at the launch of the study and thereafter throughout the study, on its own initiative or at the request of the sponsor, and will discuss the results of the intermediate analyses. It will have a consultative role. It will provide a general opinion on the progress of the study. It may assist in the making of difficult decisions during the course of the study for which an independent judgement is desirable. The Data Monitoring Safety Committee will decide on possible early termination in the light of data transmitted by the adjudication committee, the role of which will be defined by the Data Monitoring Safety Committee. Auditing will be performed using eCRF Cleansight independently of investigator and sponsor intervention.
Ethics and dissemination The LBBB-TAVI Study has been in an active recruiting phase since September 2015 (21 patients already included). Local ethics committee (CPP Sud Est VI, AU1181) and ANSM (Agence Nationale de sécurité du medicament et des produits de santé, 2015-A00271-48) authorisation was obtained in May 2015. The study completion date is estimated to be September 2018. This multicentre, randomised, parallel-group trial is registered at http://www. clinicaltrials. gov under the registration number NCT02482844. We will publish findings from this clinical study in a peer-reviewed scientific journal and present results at national and international conferences.
Acknowledgements We thank  Mr Pierre Pothier  for editing this manuscript and  Miss Elodie Chazot  for daily coordination of the  NICD-CRT study. Contributors GM, FJ, GS,  BP  and RE contributed to the conception of the study. All authors contributed to the study design. The manuscript protocol was drafted by GM, BP, PB and RE. Screening of studies for inclusion will be undertaken by all authors (clinician) except BP (methodologist). Data extraction will be undertaken by GM,  BP  and RE. All authors approved the publication of the protocol.
aphidicola cells). Endosymbiont suspensions were then analyzed by flow cytometry, using an adapted sequential gating procedure. To discriminate endosymbiont cells from electronic background noise and debris, we selected the events positively labeled with the SYTO9 green fluorescent nucleic acid stain (Fig. 1a ), after confirming that the buffer used to resuspend cells did not generate any misleading signals. The SYTO9 dye, frequently used for bacterial viability analyses, was shown to be well suited for flow cytometry applications in prokaryotic organisms  [32] [33] [34] [35] [36]. It has the advantage of permeating viable cells without requiring repeated washing steps, which result in considerable loss of cells and often interfere with data repeatability and reliability. The SYTO9-positive population, representing 99.
Flow cytometry measurements were run at low flow rate (12 μ l/min) and the core stream was allowed to stabilize for 30 sec prior to the 2 min acquisition. Cellular data were collected and processed using FACSDiva software (version 6. 1. 2, BD Biosciences). The analyses were performed using logarithmic gains and specific detector settings, adjusted on non-stained samples to eliminate the endosymbiont autofluorescence. To eliminate debris, from the analysis, the cells were first gated on SYTO9 fluorescence signals. Then, the endosymbiont population was identified by screening samples on FSC-W vs. FSC-H and SSC-W vs. SSC-H dot plots. SYTO9-stained symbionts were mounted onto slides and analyzed with an inverted epifluorescent IX81 Olympus microscope (Olympus Corporation, Tokyo, Japan) equipped with a specific emission filter, HQ535/50, for green signals.
Microscopy images were captured at 160X magnification using an F-view camera linked to the CellF software (Soft Imaging 197 System). Counting and size determination of aphid bacteriocytes. For bacteriocyte counting, aphids were analyzed one by one. Bacteriocytes were surgically isolated from the abdomen of each individual aphid in ice-cold buffer A and counted at 25X-40X magnification with a MDG-17 stereomicroscope. To avoid counting several times the same cell, the bacteriocytes were eliminated one by one, after counting, with a Pasteur pipette attached to a vacuum pump. For each developmental stage, a total number of 20 aphids was analyzed. To determine their size, bacteriocytes were collected with a micropipette and mounted on glass slides, using spacers cut from coverslips to avoid crushing cells.
Bacteriocyte images were acquired with an IX81 Olympus microscope at 16X magnification. As previously described  56  , bacteriocytes appeared as irregular spherical cells. To obtain an estimate for cell volume, each bacteriocyte was thus treated as a sphere. The bacteriocyte area (A) was determined using the CellF software, and the bacteriocyte volume value (V) was calculated applying the standard formula: = π V A 4 3.
Tissue sections of 3 μ m were cut using a LKB Historange microtome (LKB Instruments, Bromma, Sweden), placed on polylysine coated slides, dried overnight at 37 °C, and conserved at 4 °C until staining. Paraffin sections were de-waxed in methylcyclohexane, rinsed in absolute ethanol, and rehydrated through an ethanol series to PBS. Staining was performed using RAL products (REACTIFS RAL Martillac, France), according to the manufacturer's instructions and sections were mounted in Mountex mounting medium (Histolab, Gothenburg, Sweden). Observations were performed under transmitted light, using an IX81 Olympus microscope at 10X-50X magnification. Statistics. All statistical analyses were carried out using the R software R v3. 1. 1, with values of P < 0. 05 considered significant. As data did not meet the requirement of normality and homogeneity of variances (Shapiro-Wilk and the Bartlett tests), a log-transformation was performed.
Acknowledgements This work was supported by  INRA ,  INSA-Lyon , the  French   ANR-13-BSV7-0016-01  ( IMetSym) program  grant, and the  French Ministry of Research  that awarded a PhD fellowship to P. S. The authors would like to thank  Séverine Balmand  for her help at the beginning of the project,  Nicolas Parisot  for graphical representation support,  Alain Clavel  for plant production,  Catherine Garcia  and  Lionel Razy  for logistical support, and  Elyane Chassignol  and  Heidi Eppe  for secretarial assistance. We are grateful to  Patrick Callaerts  for the critical reading of the manuscript and useful feedback. We thank  Valérie James  for the English language editing of the manuscript.
MATERIALS AND METHODS All procedures were performed in accordance with the OECD Guideline for Testing of Chemicals, 421, Reproduction/Developmental Toxicity Screening Test (Adopted: July Test substance and dose preparation. EHA (CAS No. : 626-86-8) was purchased from Sigma-Aldrich (MO, USA) EHA is a white solid, and its melting point, density, and molecular weight are 28~29 o C, 0. 98 g/mL (at 25 o C), and 174. 19  (5). The EHA (Lot No. : S09682V) used in this study was 97. 4% pure and was maintained at room temperature. It was suspended in corn oil (Sigma-Aldrich), and the dosing formulations were prepared daily without analyses for homogeneity and stability. Experimental animals and housing conditions. Specific pathogen-free Sprague-Dawley (Crl:CD (SD)) rats were used in this study. SD rats are commonly used in general and reproductive toxicity studies and have a large historical control database.
Dose administration. An individual dose was calculated for each animal on the basis of the most recently recorded body weight data at a dose volume of 5 mL/kg. Rats were dosed once daily by gastric intubation with EHA at a dose of 0, 200, 400, or 800 mg/kg/day. Control rats were administered corn oil. The treatment dose was determined based on a previous 1-week repeated oral toxicity study. The body weight gain and food consumption of males administered 1,000 mg/kg/day EHA decreased during the 1-week treatment period (data not shown). Males were dosed once daily for 42 days from 2 weeks before mating to 2 weeks after mating. Females were dosed once daily from 2 weeks before mating to 4 days after delivery. Further, females showing no evidence of copulation or those in which mating was confirmed, but no signs of pregnancy were noted, were dosed once daily up to 26 days after the last day of the mating period.
Statistical analysis. The data were statistically analyzed using SAS program (Version 9. 3; SAS Institute Inc. , Cary, NC, USA). Body weights, food consumption, mating period, gestation period, pre-and post-implantation loss rates, live birth index, viability index on postpartum days 0 and 4, and organ weight data were analyzed using Bartlett test for homogeneity of variance (significance level: 0. 05). One-way analysis of variance (ANOVA) test was used for homogeneity; if the values were significant (significance level: 0. 05), Dunnett's t-test was applied for multiple comparisons (significance level: 0. 05 and 0. 01, two-tailed). Kruskal-Wallis test was used for heterogeneous data; if these data were significant (significance level: 0. 05), Steel's test was applied for multiple comparisons (significance level: 0.
Hence, Basel II should lead to an increase in the market valuation of IRB banks' DLLPs. We draw on a sample of 103 listed banks from 24 European countries for the years 2006-2011 and use a difference-indifference (DiD) research design to test our hypotheses. Because many of the variables necessary to study the impact of Basel II on the valuation of DLLPs are not available from public databases, such as BVD Bankscope, we hand-collect much of our data. This results in a unique data set that allows us to test our hypotheses using empirical models that to date have been used only for U. S. samples, for which data are more readily available than in Europe. To investigate whether the adoption of Basel II has affected the market valuation of IRB banks' DLLPs, we perform the following three tests.
Data description We test our hypotheses for a broad sample of listed banks in the European Union. We choose listed banks in the EU because they had to apply Basel II in 2008. These banks provide us with a common adoption point to test the impact of Basel II. Second, because all listed banks in the EU had to adopt IFRS in 2005, we also have a homogeneous pre-Basel II adoption sample (from 2005 onwards). This homogeneous setting provides a unique opportunity to study the effect of Basel II relative to the previous banking regulations. The core financial data stems from the BVD Bankscope database. Given the large number of missing observations, similar to Gebhardt and Novotny-Farkas (2011), we complete the data with hand-collected loan loss provisions (LLPs), non-performing loans (NPL), net charge-offs (NCO), net income, total assets, EBPT, and Tier 1 from banks' annual reports published on their websites.
We start from an initial sample of 284 listed banks in the EU, as available from Bankscope. After eliminating banks with missing financial data that could not be manually collected with reasonable efforts, we further exclude banks that underwent mergers or that are subsidiaries of other banks. Finally, we are left with 103 listed banks from 24 EU countries. This process results in 618 bank-year observations. Nonetheless, we lose 80 observations given missing values for Net Charge-Offs (NCO), the most difficult variable to collect. In contrast to  Kim and Kross (1998) , we do not need to exclude voluntary adopters to avoid biasing our findings, because, to the best of our knowledge, no bank in the sample adopted the IRB approach of Basel II earlier than 2008. We further obtain stock returns and the market value of equity data from Datastream.
Data Preprocessing All the raw data were processed as one batch using the SIEVE R software (Thermo Fisher Scientific) for the peak alignment and framing. This process results in a table of time-aligned detected features, with their retention time, m/z ratio and intensity in each sample (peak area). As the SIEVE R framing algorithm typically considers all areas higher than a cut-off value as a potential peak and we used a low cut of intensity value for sensitivity considerations, all the frames (peaks) were manually analyzed by checking the peak shape. Frames that were not associated to a classical peak shape were eliminated from the peak table. We normalized each peak area to the total peak areas of each chromatogram and further performed statistical analysis on non-normalized and normalized data (each peak area to the total peak areas of each chromatogram).
Thus, the metabolome profile may be informative in detecting atypical phenotypes. Pregnant women were included but we did not detect a specific profile of these subjects. Although some studies showed modification in global metabolism during pregnancy  [37] , few studies focused on the EBC of these subjects. Some authors highlighted a higher EBC pH in healthy pregnant women than that from healthy non-pregnant women  [38]. These findings may have an impact on metabolic profile and need to be fully explored. We have to take into account that OPLS-DA provides optimistic results and building robust models to perform prediction requires a specific methodology. Importantly, external validation may be the most important criteria for considering a molecule as a true biomarker. The analysis on two sets of data (i.
One current experimental challenge is to observe the B-modes of polarisation of the CMB caused by primordial gravitational waves produced by inflation. Their detection by the BICEP2 experiment was announced in early 2014. However, more accurate modelling of the signal over the next few months, which allowed the observation to be explained by polarised dust emission in our Galaxy, decreased the statistical confidence of the initial result  [222]. This was confirmed by Planck data in 2016  [223]. Upcoming large-scale structure surveys, such as the Euclid satellite mission, or 21-cm radiation surveys such as the Square Kilometre Array, may measure the power spectrum with greater precision than current CMB probes, and could provide further evidence in favour of the inflationary paradigm  [224] [225] [226].
Experimental Progress There has been rapid progress in constraining cosmological parameters and models over the last two decades, with a multitude of experiments observing the CMB, large-scale structure, galaxies and supernovae. We will just provide a summary of the most recent data sets. The first are anisotropies in the CMB, where the main statistic is the angular power spectrum of fluctuations C , and polarisation of the CMB. The most recent and current are: WMAP (http://map. gsfc. nasa. gov), Planck (http://www. cosmos. esa. int/web/planck), Atacama Cosmology Telescope (ACT) (http://act. princeton. edu), South Pole Telescope (SPT) (https://pole. uchicago. edu), Atacama Cosmology Telescope polarisation-sensitive receiver (ACTPol)  [529] , SPTPol, Spider (http://spider. princeton. edu), Polarbear (http://bolo.
berkeley. edu/polarbear), Background Imaging of Cosmic Extragalactic Polarization (BICEP2) (http://bicepkeck. org,https://www. cfa. harvard. edu/ CMB/bicep2), Keck Array (http://bicepkeck. org,https://www. cfa. harvard. edu/CMB/keckarray). The second source of data are surveys cataloguing the angular positions and redshifts of individual galaxies, leading to the power spectrum of fluctuations P(k, z), or the two-point correlation function ξ(r). The recent and current experiments are: Baryon Oscillation Spectroscopic Survey (BOSS) using Sloan Digital Sky Survey (SDSS) data (http://www. sdss3. org/surveys/boss. php), Dark Energy Survey (DES) (https://www. darkenergysurvey. org), Weave (http://www. ing. iac. es/weave/ science. html), Hobby-Eberly Telescope Dark Energy Experiment (HETDEX) (http://www.
hetdex. org), Extended Baryon Oscillation Spectroscopic Survey (eBOSS) (https://www. sdss3. org/future/eboss. php), Mid-Scale Dark Energy Spectroscopic Instrument (MS-DESI) (https://www. skatelescope. org), Canadian Hydrogen Intensity Mapping Experiment (CHIME) (http://chime. phas. ubc. ca), Baobab, MeerKAT (http://www. ska. ac. za/science-engineering/meerkat), and ASKAP (http://www. atnf. csiro. au/projects/askap/index. html). The third source of data are weak lensing, which use the fact that images of distant galaxies are distorted and correlated by intervening gravitational potential wells to produce statistics such as the convergence power spectrum C κ  [530, 531]. Some current experiments are: Dark Energy Survey (DES) (https://www. darkenergysurvey. org), Red Cluster Sequence Lensing Survey (RCSLens) (http://www.