dataesr/scientific-paragraphs-categorization huggingface dataset:
These are a sharp contrast to the neat solutions of T a space. As we previously mentioned in section 3, such a behaviour is the expected consequence of the system being underconstrained by the T R parameters, and affirms that the results obtained using this parametrisation cannot meaningfully be presented as a set of parameter values with associated uncertainties. Furthermore, flat regions in the fit-parameter space may induce larger uncertainties in cases less ideal than those constituted by Asimov datasets. From the perspective of a fit, c φ and s φ are no different from the other parameters of the functional form; as such, we have allowed them to vary beyond their physical ranges, c   The toy corresponds to the m X = 700 GeV, Γ X X = 5%, and set 1 input parameters. Twodimensional profile likelihood plots are presented, with 1σ and 2σ boundaries outlined in white.
input) PM parameter values can be recovered. We begin by using the MultiNest (see eq. (5. 2)) sampling outputs to the T a and T R fits to construct "results" histograms using their respective functional forms. Such histograms are defined over an invariant mass range equal to the fitted invariant mass window (in this case, 660-740 GeV), with the same binning as that of the fitted dataset  (2 GeV). The points in parameter space satisfying χ 2 point -χ 2 bf ≤ Q χ 2 ν (p = 0. 68) , (5. 5) were extracted from the MultiNest files, where ν = 5 for the T a parameters (Q χ 2 5 (0. 68) ≈ 5. 86) and ν = 7 for the T R ones (Q χ 2 7 (0. 68) ≈ 8. 14). These are the points that lie within the 1σ confidence region of the respective ν-dimensional parameter spaces. For a given histogram bin, the range of functional form values prescribed by these points can thus be interpreted as the 1σ confidence interval of the bin.
The q 0 statistic is thus a measure that compares the likelihoods of the null (background-only) and alternative (i. e. including a signal) hypotheses; given a particular dataset and the observed value, q 0,obs , one can calculate the p-value, p 0 = ∞ q 0 ,obs f (q 0 |0) dq 0 , (5. 8) that subsequent data will exhibit an incompatibility with the background-only hypothesis to an equal or greater degree. Here, f (q 0 |0) represents the probability distribution function for q 0 conditional on the null hypothesis being true, and as such is always non-negative; a larger value of q 0,obs thus yields a smaller p 0 , and indicates a greater disagreement with the background-only hypothesis. An alternative metric that quantifies the statistical incompatibility of the backgroundonly assumption against the observed dataset is the local significance: Z 0 = Q G (1 -p 0 ) , (5.
To prevent an underestimation of the local significance, one should define sufficiently large prior volumes for the parameters during a fit, so as to give them the freedom needed to compensate for the lack of higher-order terms. We demonstrate the procedure using an Asimov dataset generated from the physics model, with the input parameters as we have adopted in the previous sections (m X = 700 GeV, Γ X /m X = 5%, and set 1 parameter values). The functional form of eq. (5. 1) was used as the model alternative to the null hypothesis, and was fitted over the full (100-1600 GeV) invariant mass range of the toy. We note that since parameter estimation is not of import, one can choose to do this using either the T a or T R parameters; in the interest of computational efficiency, we recommend the T a parameter set be employed, as a fit of its parameters typically converges more quickly in comparison to the T R one.
Acknowledgements The authors thank  Fabio Maltoni  and  Yee Chinn Yap  for their helpful comments and contributions during the early stages of the work. SF thanks the  CERN TH division  for hospitality during the course of this work. LR and MW are partly supported by the  Australian Research Council (ARC)   Discovery Project  grant  DP180102209. ET is supported by an  Australian government Research Training Program scholarship. AGW is supported by the  ARC Centre of Excellence for Particle Physics at the Terascale (CoEPP)  ( CE110001104 ) and the  Centre for the Subatomic Structure of Matter (CSSM). TikZ-Feynman [22] and pippi [23] were used to produce plots presented in this paper.
Incorporation of detector effects in template formsThe results presented thus far have been obtained under the assumption of statistically perfect datasets, whilst also neglecting event reconstruction effects stemming from the limitations of particle detectors, which will affect the events observed in any physical experiment. To account for these effects, one can choose one of two approaches. The first option is to obtain an approximation of truth-level data using unfolding algorithms, to which the procedure, as summarised in section 5. 6, can then be applied. The alternative approach is to incorporate a parametrisation of the detector reconstruction effects within the template descriptions, so that they can be fitted directly to reconstructed data. In this section, we study the latter approach.
It should be emphasized that the absorption at 450 nm is related to the presence of MNPs and not of the copolymer. Cryo-TEM images were obtained using a Tecnai F20 X TWIN microscope (FEI Company, Hillsboro, OR, USA) equipped with a field emission gun, operating at an acceleration voltage of 200 kV. Images were recorded on the Gatan Rio 16 CMOS 4 k camera (Gatan Inc. , Pleasanton, CA, USA) and processed with Gatan Microscopy Suite (GMS) software (Gatan Inc. , Pleasanton, CA, USA). Specimen preparation was done by vitrification of the aqueous solutions on grids with holey carbon film (Quantifoil R 2/2; Quantifoil Micro Tools GmbH, Großlöbichau, Germany). Prior to use, the grids were activated for 15 s in oxygen plasma using a Femto plasma cleaner (Diener Electronic, Ebhausen, Germany). Cryo-samples were prepared by applying a droplet (3 µL) of the suspension to the grid, blotting with filter paper and immediate freezing in liquid ethane using a fully automated blotting device Vitrobot Mark IV (Thermo Fisher Scientific, Waltham, MA, USA).
The spectral lines from all pixels are then combined (after weighting by the limb-darkening function). We use the synthetic solar optical spectra used in the SAFIR software  (Galland et al. 2005)  from  Kurucz (1993) , and use only a single line here for simplification, at 5300 Å, i. e. in approximately the middle of the HARPS spectrograph wavelength coverage. We then compute the bisector of this line after integration over the disc to check whether meridional flows leave a signature in the line shape. To estimate the variation of the bisector shape, we compute the variable BIS at each time step, which is the difference between two quantities, λ 1 and λ 2 , after conversion to a velocity. These quantities are computed as follows. We use I to denote the intensity at the line core and I ′ the line depth (1-I).
Values of λ 1 and λ 2 are then the wavelengths of the middle of the line profile for intensities between I and I+0. 2I ′ and between I+0. 7I ′ and I+0. 9I ′ respectively. Finally, the time series will be compared to two activity indicators: the spot number from SIDC (Solar Influences Data analysis Center) and the S-index from the Sacramento Peak Observatory. The objective is to compare the phase of the different series during the cycle.
Acknowledgements. We thank  S. Brun  and  A. Strugarek  for usefull discussions about this work. This work has been funded by the  ANR GIPSE   ANR-14-CE33-0018. This work was supported by the  "Programme National de Physique Stellaire" (PNPS)  of  CNRS/INSU  co-funded by  CEA  and  CNES. This work was supported by the  Programme National de Planétologie (PNP)  of  CNRS/INSU , co-funded by  CNES. The monthly sunspot number has been provided by the SIDC-team, World Data Center for the  Sunspot Index, Royal Observatory of Belgium  (http://www. sidc. be/sunspot-data/). This work made use of the Ca K index provided by the  Sacramento Peak Observatory of the U. S. Air Force Phillips Laboratory.
Statistical Analysis Categorical variables were expressed as numbers (percentage). Continuous variables were expressed as means (±standard deviation, SD) or medians (range). Comparisons in patient characteristics between the two study groups (with mPM or without mPM) were completed using Student's t-tests for continuous variables and the Mann-Whitney test for non-continuous variables. Statistical testing was completed at the two-tailed α level of 0. 05. Data were managed with an Excel database (Microsoft Corporation, Redmond, WA, USA) and analyzed using R 3. 5. 1 software, available online (https://cran. r-project. org/).
Ethics The research protocol was approved by a national Ethics Committee (PPC Sud Est II, ID-RCB 2017-03431-52; Date of approval: 16/05/2018) and registered on clinicaltrials. gov (NCT03754569). The collection of patient data was declared to the French "Commission Nationale Informatique et Liberté" (CNIL-Q9d2264273M). Each patient signed a written informed consent after receiving clear and detailed information about the research protocol. In the absence of preliminary data and given the possibility of not detecting mPM at the end of the complete CRS, it did not seem legitimate to subject many patients to an additional surgical procedure. We therefore made the arbitrary choice of conducting an initial exploratory prospective pilot study based on a cohort of consecutive patients over one year.
Mathematical Analysis Of the 26 patients, each associated with 13 biopsies (after data completion as described above), one patient had seven biopsies with mPM, two had two biopsies with mPM and four had one biopsy with mPM. For the remaining 19 patients, mPM was not detected in any of the 13 biopsies. As stated in the first part of the model, these results were displayed as a relative histogram (Figure  2 ). From this histogram, results were found to be properly described by a Poisson distribution. An optimization was therefore performed using the Matlab software to determine the Poisson distribution, which best fits.
Mathematical Analysis Of the 26 patients, each associated with 13 biopsies (after data completion as described above), one patient had seven biopsies with mPM, two had two biopsies with mPM and four had one biopsy with mPM. For the remaining 19 patients, mPM was not detected in any of the 13 biopsies. As stated in the first part of the model, these results were displayed as a relative histogram (Figure  2 ). From this histogram, results were found to be properly described by a Poisson distribution. An optimization was therefore performed using the Matlab software to determine the Poisson distribution, which best fits the relative histogram. The Poisson distribution obtained by fitting (orange diamonds in Figure  2 ) was used to assign the probabilities that 0, 1, 2,. , or all the 13 biopsies have mPM.
2   II. To check the validity of the parameters found, the T resonator was simulated in the ADS with the relative permittivity, effective permittivity of the plate and tangent loss shown in Table  II. Fig. 3  shows the simulated and measured parameter  12 for the FR4 plate, in which it is possible to note that up to 7 GHz the behaviour of the measured and simulated curve are very close. Thereafter, there is a large dispersion between the measured and simulated graphs, proving that the FR4 material is not suitable for high frequencies. After the characterization of the dielectric, the optimization process was performed for the five topologies presented in Fig. 1. This process was performed in the Advanced Design System (ADS) software using the Genetic Algorithm. This algorithm is based on the mechanisms of natural selection and genetics, as Holland proposed in  [15].
Measurements relating to the retrieved organisms The data retrieved from the sampling included the abundances of 840 taxa found at the 98 sample points, each representing 0. 2m². Among the recorded taxa, 723 species were identified to level of species (86% of the taxa); consequently, the geographical patterns of these 723 species could be been documented according to the available literature. The species names were validatedby use of the WoRMS database (http://www. marinespecies. org; accessed on 4 December 2018). The distribution of the 723 identified species was also categorized in terms of the distinct biogeographical regions of the Mediterranean adopted by  Coll et al. (2010)  A hierarchical cluster analysis (HCA) was used based on Sorensen's coefficient for Presence/Absence of the species in the 13 biogeographical regions defined above, and a dendogram was constructed using the group-average algorithm from the PRIMER V6 software  (Clarke and Gorley, 2006).
Acknowledgements The authors would like to thank the crew of the oceanographic vessel, the M. S. Benyahia for their help during the sampling campaigns. The authors also wish to acknowledge the contribution received from  S. Alizier ,  T. Ruellet  and  S. Andres  with respect to setting up the database, data analyses and preparation of the figures. Finally, the authors are grateful to  Michel Carpenter  for his correction of the original English manuscript and  Colin Burton  for his correction on the last version of the text.
Simulation Procedure The CFD simulation has been developed by the finite volume method performed by ANSYS ® v2019 R3 fluent  [26]. Firstly, the geometry of the collector was defined in the software and meshed optimally. Secondly, from the experimental results, the specific setup, variable and solution method were defined. Finally, the results of the model were analyzed and then compared with experimental results. The simulation model solved the continuity, energy and momentum equations inside the collector. Flow field, heat transfer, temperature gradient inside the receiver, thermal and electrical yield, and radiation field were obtained from these set of simulations.
Funding: This research was partly supported with funding from the  European Union 's  Horizon 2020 research and innovation program  under grant agreement No. 814865  ( RES4BUILD ). The authors are also grateful for the support provided by the  STINT mobility program  and are thankful for the fruitful cooperation with the project partners. The outputs reflect only the author's view and the  European Union  cannot be held responsible for any use that may be made of the information contained therein.
Statistical analysis Gaussian distribution was verified (D'Agostino-Pearson normality test), and meanstandard deviation was calculated. Two-way ANOVA was chosen for statistical significance testing of RBCs, and unpaired t-test for plasma and platelets (RBCs: N = 16, plasma: N = 16, platelets: N = 8 per study arm), with Holm-Sidak's correction for multiple comparisons. For contingency test of 2,3-DPG at d21, Fisher's exact test was used to compare AS and plasticizers, respectively. GraphPad Prism v. 8. 2 for Windows (GraphPad Software Inc. , La Jolla, CA, USA) was used for computation of all statistics.
Minor effects on RBC membrane and metabolism Haemolysis, RMV and K + were analysed to assess the effects of plasticizer and AS on cell membrane degradation. Haemolysis was higher in DEHT than in DEHP from d14 onwards (P < 0Á001). From day 35, AS also affected haemolysis, with lower haemolysis levels in PAGGSM for both DEHT and DEHP (P < 0Á05 within plasticizers, P < 0Á001 for all other combinations). However, at d49, DEHT/SAGM, highest of the study arms (0Á39%), still barely reached half of the European limit 0Á8% [23] (Fig. 2a  and b , Table  1 , Supporting Information 3)). RMV count is an indicator of membrane integrity loss. Reflecting the haemolysis results, the count was higher in DEHT than in DEHP and in SAGM than in PAGGSM (Fig. 2c , Table  1 ). We also noticed a similar highest-tolowest order of glycophorin A expression decrease throughout storage (data not shown).
Acknowledgements We want to acknowledge  Dr Hans Gulliksson  for invaluable mentorship, Macopharma for material and financial support,  Blenda Westeson ,  Jenny Eriksson ,  Alexandra Sabo ,  Erik Dahl ,  Andreas Eriksson ,  Sandra Valencia  and  Hanna-Stina Ahlz  en as helpful members of blood collection and production,  Ase Tolf  at  Macopharma Nordic  for practical support, and all volunteer blood donors that contributed to this study.
METHOD Setting design and participants The CACAO study was a French nationwide multicentre prospective cohort of consecutive ambulatory patients receiving an oral anticoagulant in general practice who were recruited between April and October 2014 (see Supplementary Table  S1  for details of patient characteristics). The study's 463 GP investigators were located in 290 different rural and urban areas, and in 47 different counties throughout France. The study had two phases: an initial crosssectional phase that examined safety data from medical records at inclusion, followed by a standard, 12-month longitudinal phase during which the efficacy and safety of VKAs versus DOACs were assessed. 13 The CACAO study's main inclusion criteria were age ≥18 years, prescription of a VKA or a DOAC, and a consultation (for whatever reason) with a GP investigator during the study period.
Data collection General assessment. For the purposes of the present study, only baseline data were considered. Using an electronic case report form, GPs collected data anonymously on demographics, personal medical history, current medications (from the French National Medicines Agency's list),  14  items from CHA 2 DS 2 -VASc and HAS-BLED (scores were calculated subsequently),  15, 16  and laboratory tests (renal and hepatic function tests, and coagulation assays). No biological samples were collected specifically for this study. Outcomes. ] [19]  These situations involved inappropriate dose prescription (under-dosing or over-dosing); prescriptions that were contraindicated or not recommended (because of a comorbidity or a concomitant medication); nonindication (a CHA 2 DS 2 -VASc <1); an at-risk interaction (antiplatelets or other reasons); and non-compliance with the precautions for use (concomitant treatments or comorbidities), that is, clinician prescribed the DOAC against the precautions for use.
A logistic model was used, because no effect of GPs was observed in an empty multilevel model. Adjusted ORs (95% confidence intervals) were estimated using multinomial logistic or exact logistic regression models. The reference category was the appropriate DOAC dose. Rivaroxaban was chosen as the reference category for the 'DOAC molecule' factor because it was the most prescribed drug and thus facilitated the interpretation of ORs. Goodness of fit was assessed using the Akaïke and Bayesian information criteria (lowest value = best fit). All tests were two-sided, and the threshold for statistical significance was set to P≤0. 05. Analyses were performed with Stata software (version 15).
The GPs' records may not have included all the factors that influence decisions about DOAC dosing, including patient preferences and values, and plans for imminent cardioversions. The HAS-BLED and CHA 2 DS 2 -VASc scores were assessed a posteriori. Therefore, it was not possible to tell whether prescribers knew of these scores and took them into account when prescribing DOACs. Other confounders were also included, such as a personal history of haemorrhage requiring hospitalisation (Supplementary Table  S1 ). Although the concomitant prescription of DOAC and aspirin is not recommended, rivaroxaban and low-dose aspirin can be given concurrently in acute coronary syndrome and AF. However, the dose of aspirin prescribed was not recorded in the study database. Finally, the absence of longitudinal data on inappropriate prescriptions constitutes a limitation for the present analysis, but this was not the main objective of the CACAO cohort study.
8 × 3. 8 mm field, manually centered on the crack tip, at minimum and maximum load during selected cycles (with an interval of 3 000 to 10 000 cycles). The spatial resolution of these images was approximately 1 µm/pixel. The other side was just polished, and a fixed 32. 5 × 28 mm area was monitored by a 2448 × 2046 pixels camera fitted with a Tokina macro 100 F2. 8 D objective. The resolution of the images was 13 µm/pixel. The Vic2D software was used for DIC, with a subset size between 80 and 120 pixels, and a step between 25 and 50 pixels (25 to 50 µm), depending on the local density of the speckle painting. To determine the stress intensity factors, the amplitude of the relative opening and sliding displacements between 2 rows of virtual extensometers, 100 to 150 µm apart, above and below the crack (denoted by COD and CSD, respectively) were plotted as a function of the square root distance to the crack tip.
The conclusion from the data plotted in Figure  11  is that the clamping devices devices are not infinitely stiff compared to the sample as the SIF range measured from the actual displacement by Teams 4 and 6 (direct estimates from higher resolution DIC measurements) appear to be in between those predicted by type 1 and 2 boundary conditions tested by Team 11. For investigating this boundary condition issue, the displacement amplitude measured by DIC (Team 4) is analyzed in order to estimate the displacement amplitude applied along the top edge of the domain of interest (as if the displacement amplitude of the bottom edge was fixed). This displacement amplitude is plotted in Figure  12  for different crack tip positions and for the two levels of maximum load. It is evidenced that the rotation of the boundary of the domain of interest is not zero.
The scatter is less pronounced for low load level for     Crack growth rate [µm/cycle] Team 1 Team 4 Team 6 Team 9, front Team 9, back Team 11, Type 1 Team 11, Type 2 Team 12, Tada Team 12, DIC (b) F F which the monotonic plasticity remains constrained and the actual loading conditions are closer to the ideal ones. To allow the fatigue community to test numerical prediction of fatigue crack growth and path, the rich database obtained during this benchmark will be made available online at the following DOI: 10. 5281/zenodo. 3891441.
Acknowledgments: The authors would like to dedicate this review to our dear colleague  Elke Bräuer-Krisch  who was an integral part of MRT research and a proponent for its clinical application. The authors would also like to acknowledge  Nahoko Shintani  for her assistance during the experiments and staining of the samples,  Adolfo Odriozola  for his support with electron microscopy. The authors' thanks also to  John Hopewell  and  Jennifer Fazzari  for editing this manuscript.
In all patients, diagnosis of COVID-19 was confirmed by RT-PCR on respiratory samples. Briefly, viral RNA was extracted using the NucleoSpin 1 RNA Virus kit (Macherey-Nagel) according to the manufacturer's instructions, and amplified by RT-PCR protocols developed by the Charité (E gene)  (Corman et al. , 2020)  and the Institut Pasteur (RdRp gene)  (Bernard Stoecklin et al. , 2020)  on LightCycler 480 1 (Roche). We collected the following data from the medical files of patients in both groups: demographic characteristics, comorbidities and outcome. To increase statistical power, we chose a combined primary endpoint (mortality and/or IMV requirement) to compare the two groups. Continuous variables were expressed as mean and standard deviation (SD) and compared with ANOVA test. Categorical variables were expressed as number (%) and compared by χ 2 test or Fisher's exact test between the two groups.
Acknowledgements The authors thank especially  Emmanuel Siess ,  Azzedine Rahmani ,  Charlotte Bourgoin ,  Elodie Bouvier ,  Julien Lorenne  and  Frederic Deuze  for their strong implication in the present work. They also thank the management team of the  Hospital Nord Franche-Comté  for having made available Tocilizumab outside its approved indication and each member of the  HNF Hospital Tocilizumab multidisciplinary team. Special acknowledgements to all the physicians, caregivers (nurses and orderlies) and patients.