dataesr/scientific-paragraphs-categorization huggingface dataset:
Uncertainties in the background prediction The systematic uncertainty associated with the background estimation of the ABCD method was evaluated using data events passing the validation region selection. Events falling in each of the two bands of the ABCD plane that surround region A, and that are shown in Figure  10  for the 1MSVx+E miss T strategy in the barrel, were excluded and the expected background in the signal region was re-evaluated. The definition of region A was not modified in this procedure. The relative variation with respect to the observed events in region A was then evaluated. The size of the two bands is defined by the resolution of the two variables used to define the ABCD plane. The maximum value of the two results obtained by separately removing bands with widths of 1σ and 2σ was taken as the systematic uncertainty associated with the background estimation.
Summary of the baseline criteria used for the analysis presented in this paper. All selection criteria are also applied to signal MC events when determining the number of expected signal events in the dataset. Event passes Muon RoI Cluster triggerEvent has a PV with at least two tracks with p T > 400 MeV Event has at least one MS vertex MS vertex matched to triggering muon RoI cluster (∆R(vertex, cluster) < 0. 4). For 2MSVx strategy: in the case of 2 muon RoI clusters, the second vertex should be matched to the second cluster.
Acknowledgments We thank  CERN  for the very successful operation of the LHC, as well as the support staff from our institutions without whom ATLAS could not be operated efficiently. We acknowledge the support of  ANPCyT , Argentina; YerPhI, Armenia;  ARC, Australia ;  BMWFW  and  FWF , Austria; ANAS, Azerbaijan; SSTC, Belarus;  CNPq  and  FAPESP, Brazil ;  NSERC ,  NRC  and  CFI ,  Canada ; CERN; CONICYT, Chile; CAS,  MOST  and  NSFC, China ;  COLCIENCIAS, Colombia; MSMT CR, MPO CR  and  VSC CR, Czech Republic ;  DNRF  and  DNSRC, Denmark ;  IN2P3-CNRS ,  CEA-DRF/IRFU , France; SRNSFG, Georgia; BMBF,  HGF , and  MPG, Germany ;  GSRT, Greece; RGC, Hong Kong SAR, China ;  ISF and Benoziyo Center, Israel ;  INFN, Italy ;  MEXT  and  JSPS, Japan ; CNRST, Morocco; NWO, Netherlands; RCN, Norway;  MNiSW  and  NCN , Poland; FCT, Portugal; MNE/IFA, Romania;  MES of Russia  and  NRC KI , Russian Federation; JINR; MESTD, Serbia; MSSR, Slovakia; ARRS and MIZŠ, Slovenia; DST/NRF, South Africa; MINECO, Spain;  SRC and Wallenberg Foundation, Sweden ;  SERI ,  SNSF  and  Cantons of Bern and Geneva, Switzerland; MOST, Taiwan ;  TAEK, Turkey; STFC, United Kingdom ;  DOE  and  NSF ,  United States of America.
The 3D growth is associated with the formation of Mn-rich clusters that exhibit typical RHEED patterns of the α-MnSe phase. The Mn concentration was deduced from the combination of Rutherford backscattering spectroscopy (RBS), energy dispersive X-ray spectroscopy (EDX) and X-ray photoemission spectroscopy (XPS) measurements. We have also developed a transfer process of the centimeter-scale layers from mica to suitable substrates for further characterizations. Magnetic measurements of monolayers TMD are a challenging task owing to the substrate contribution and a small amount of magnetic matter to measure. The successful transfer allowed us to perform the magnetic measurements using highly sensitive magnetometer superconducting quantum interference device (SQUID). In this study, the magnetic data have shown that Mn dopants induce magnetic states in the doped layers which imply ferromagnetic ordering and paramagnetic states.
We first calibrated the atomic density of Mn in the 3-ML-thick MoSe 2 layers using RBS technique. An incident 4 He + beam is accelerated at an energy of 1. 9 MeV and the backscattered helium ions are detected at an angle of 160 • with respect to the incident beam. The beam current is about 25 nA on the analyzed area. Note that RBS allows quantifying the composition of the layers over millimeter-square regions. Figure  2a  shows typical RBS spectra of the doped layer with a nominal Mn concentration of 10% and the undoped layer in which we can point out the peaks corresponding to Mn, Mo and Se atoms. The quantitative analysis was then performed using a theoretical simulation with help of the commercial software SIMNRA. For the spectrum of doped layer, the simulation yields the Se/Mo atomic density ratio of 2.
That was also evidenced by optical microscopy and by mapping Raman peaks which are as intense as the ones of the before-transferred samples. We performed the magnetic measurements with a SQUID magnetometer. Probing the magnetic state of doped 2D layers is an intriguing issue that requires a great attention in terms of sample handling and data analysis. We were also aware of the high sensitivity of SQUID which makes the data interpretation complicated because of a large substrate volume as compared to the one of the 2D layers. Many magnetic measurements using a SQUID or vibrating-sample magnetometer (VSM) on the 2D TMD layers have been done with thick substrates which presumably exhibit a high susceptibility  [18, 25] , leading to a strong substrate contribution to the final magnetic signal.
Acknowledgments The authors thank  Vincent Mareau ,  Laurent Gonon  and  João Paulo Cosas Fernandes  for their assistance and discussions with Raman spectroscopy. The authors acknowledge  Yann Almadori  and  Benjamin Grévin  for AFM characterizations;  Nicolas Mollard  for preparation of TEM samples. This work is supported by  Agence Nationale de Recherche  within the ANR contracts (MoS2ValleyControl and MAGICVALLEY). The  French state funds LANEF  ( ANR-10-LABX-51-01 ) and  Equipex  ( ANR-11-EQPX-0010 ) are also acknowledged for their support with mutualized infrastructure. Minh Tuan Dau acknowledges the support from.
Gaussian distance In Section 2. 4. 2 we showed that the Gaussian distance can be estimated numerically by sampling over (in this case) semidefinite programs (SDP) according to (58) and (60). When empirically averaging these results according to  (17)  one obtains an estimate of the statistical dimension and therefore the phase transition point for successful convex recovery. For the case of sparse and low-rank matrices with the weighted sum of nuclear norm and 1 -norm as regularizer the distance (58) becomes G -cone ∂ • λ,sum (X 0 ) 2 = min τ ≥0,X1,X2 G -X 1 -X 2 2 : X 1 + X 2 , X 0 = τ λ, X 0 1 X 0 1 , X 1 ∞ X 2 ∞ ≤ τ λ. (87) A similar SDP can be obtained for the case of the maximum of these two regularizers. We solve both SDPs using the CVX toolbox in MATLAB (with SDPT3 as solver) for many realization of a Gaussian matrix G and then average those results.
Convex recovery We numerically find the phase transition for the convex recovery of complex sparse and low-rank matrices using the sum and maximum of optimally weighted 1 and nuclear norm. We also compare to the results obtained by convex recovery using only either the 1 -norm or the nuclear norm as reguralizer and, exemplary, also to a non-convex algorithm. The dimension of the matrices are n = n 1 = n 2 = 30, the sparsity range is s = s 1 = s 2 = 5,. , 20 and the rank is r = 1. For each parameter setup a matrix X 0 = uv † is drawn using a uniform distribution for supports of u and v of size s and iid. standard complex-normal distributed entries on those support. The measurement map itself also consists also of iid. complex-normal distributed entries. The reconstructed vector X is obtained using again the CVX toolbox in MATLAB with the SDPT3 solver and an reconstruction is marked to be successful exactly if X -X 0 2 / X 2 ≤ 10 -5 (88) holds.
Acknowledgments We thank  Micha l Horodecki ,  Omer Sakarya ,  David Gross ,  Ingo Roth ,  Dominik Stoeger , and  Željka Stojanak  for fruitful discussions. The work of MK was funded by the  National Science Centre, Poland  within the project  Polonez  ( 2015/19/P/ST2/03001 ) which has received funding from the  European Union 's  Horizon 2020 research and innovation programme  under the  Marie Sk lodowska-Curie  grant agreement No  665778. The work of SJS was partially supported by the grant  DMS-1600124  from the  National Science Foundation (USA). PJ has been supported by  DFG  grant  JU 2795/3.
The tagged C3P3-G1 enzyme was imaged by indirect immunofluorescence. CHO-K1 cells were transfected with the pCMV-FLAGx3-NP868R-(G 4 S) 2 -K1ERNAP(R551S), which encodes for the NP868R-(G 4 S) 2 -K1ERNAP(R551S) C3P3 enzyme fused in-frame to the C-terminus of the FLAGx3 tag  (12). CHO-K1 cells were then stained as above, using a primary polyclonal F7425 rabbit IgG anti-FLAGx3 antibody (1:250; Sigma) (13) followed by secondary Alexa Fluor 568-conjugated goat anti-rabbit (1:800; Life Technologies). Cells transfected with FLAG-RLuc plasmid and cells stained only with secondary antibodies were used as controls. Slides were imaged on a Leica SP8 confocal microscope equipped with the appropriate laser excitation filters under oil immersion (i. e. ×40 lens) with image magnification and processed with Leica LAS-AF and ImageJ analysis software.
ASFV NP868R increases protein expression when coupled with various prokaryotic RNAPs, especially the R551Soptimized K1E phage RNAP Having found that NP868R can boost protein expression when coupled to T7RNAP, we asked if NP868R could function with other bacteriophage RNAPs. We selected 54 complete bacteriophage genome sequences, which were analyzed for candidate phage-promoter sequences using the PHIRE software  (55). Twenty-nine RNAPs with wellcharacterized promoters were then subjected to BLAST+ analysis  (56) , and clustered into 12 subgroups having <80% amino-acid identity (Supplementary Figure  S9 ). One member of each subgroup was randomly selected and fused to the carboxyl-end of NP868R via (G 4 S) 4 linker (Supplementary Table  S5 ). For each RNAP, the putative phage promoter from the major capsid protein was inserted upstream of the luciferase gene and co-transfected with the corresponding C3P3-G1 enzyme plasmids (Supplementary Table  S5 ).
ACKNOWLEDGEMENTS We thank the  French Ministry of Research and Innovation and BpiFrance  for their encouragements and financial support. We also thank  Christiaan Levelt  at the  Netherlands Institute for Neuroscience (Amsterdam, The Netherlands ) and  Samira Benadda  at  INSERM (Paris, France ) for their help in immunofluorescence imaging. We are grateful to  Daniel Metzger  ( Institut de Génétique et de Biologie Moléculaire et Cellulaire, Strasbourg ) for reviewing the manuscript and very helpful comments.
Initial study PREMAG was a prospective multicenter randomized controlled trial that took place in 13 French perinatal centers. Between July 1997 and July 2003, women pregnant at a gestational age younger than 33 WG were eligible if birth was expected or planned within 24 h. Women received 4 g magnesium sulfate solution or isotonic 0. 9% saline. The study included 564 women who gave birth to 688 infants. A parent of each child provided written informed consent. The Clinical Trials. gov Identifier was NCT00120588  [4, 5].
School-age study Between December 2009 and April 2012, we contacted the families of all surviving children. A mail questionnaire was sent to the parents, who remained blinded to the treatment group in the perinatal period. This second protocol was approved by the Comité consultatif sur le traitement de l'information en matière de recherche dans la Santé (CCTIRS) of the French Ministry of Health (17 December 2009) and the Commission Nationale de l'Informatique et des Libertés (CNIL) (19 April 2010). All questionnaires were collected and analyzed at the Neonatal Intensive Care Unit at Rouen University Hospital, with secure computers used for data entry and storage  [3]. Parents gave informed consent to the research and to publication of the results.
We calculated sensitivity, specificity, positive and negative predictive values, positive and negative likelihood ratios, and pre-test and post-test probabilities. For test performance indexes, delayed DAMT was considered a positive test and normal or advanced DAMT was considered a negative test. Odds ratios (OR) and corresponding 95% confidence intervals were estimated. Statistical significance was defined as p<0. 05. These analyses were performed using SAS software, version 9. 2 (SAS Institute, Cary, NC, USA).
6% versus 88. 6%, p=0. 001). No children died between the ages of 2 and school age. Overall, 301 children drew a human figure, 152 in the magnesium sulfate group and 149 in the placebo group. Seventy-two questionnaires were collected by phone and 58 children did not answer the HFD question. The experimenters did not include 20 HFDs because they did not match the DAMT criteria. Finally, 281 HFDs (64. 5% of the school-age cohort) were eligible for analysis (Figure  1 ). Between respondents and nonrespondents to the HFD question, no differences were identified for the main characteristics (age, sex, gestational age, single or multiple pregnancy, magnesium sulfate exposure), except for behavioral problem and prosocial scales of SDQ, and for cognitive deficits, which were more frequently abnormal among the children who did not respond (data not shown).
DAMT results were statistically associated with behavioral and cognitive deficit but other deficits could affect the DAMT score such as motor dysfunction (even minor), visual deficit, attention disability, dysexecutive syndrome, dyspraxia, or dysgraphia. Other factors such as creativity, drawing experience, and personal interest for drawing may interfere with DAMT  [9, 10]. DAMT scores are based on the number of details in the drawing and the accuracy of the placement of each body part. These criteria may not be appropriate for assessing child development. In addition, DAMT may not be relevant for detecting behavioral and/or cognitive disabilities. Recently, Tükel et al. categorized the developmental stages of HFD (1, scribble; 2, pre-tadpole; 3, tadpole; 4, transitional; 5, conventional-I; and 6, conventional-II), analyzed the drawing order (1, top-down; 2, center-periphery; and 3, bottom-up), and objective and quantitative criteria (size, symmetry, proportion, and circularity) using an image-processing computer program (ImageJ)  [11].
The results are presented in terms of the distribution size in the volume base because for calorimetric measurements it is the energy involved during freezing/melting depending on the mass, which is recorded. The mean droplet size is characterized by D 43 = N i D 4 i N i D 3 i (1) where N i is the number of droplets in size range i and D i is the middle diameter of size range i. Optical Microscopy, the morphology of the sample was observed using optical microscope NIKON Labophot-2. The sample object was observed under high power of 100× and the microscope image captured was copied by software IrfanView 64 bit version (Nikon, Tokyo, Japan).
It is reassuring, as we did not consider buckling, which would make long linear chains fold on themselves and produce more complex clusters, and may bias the linear chain distribution for very large lengths. It should also be noted that with fixed division time, not only the distribution is bumpy, as chains comprising a power of two number of bacteria are more frequent than others, but the distribution is also narrower. We analyzed experimental data on clusters of S. Typhimurium in the cecum of vaccinated mice. The experimental chain length distribution is in line with the model of fixed replication time, which is indeed more realistic. There is however somewhat less large chains than expected. More data would be necessary to asses this more reliably. This could be because of possible bias in the data.
Around seven million patients undergo endoarterial interventional radiology procedures (EAIRP) annually worldwide. These procedures have become part of the standard repertoire of vascular surgery. However, the healthcare-associated infections related to these procedures are relatively unknown. Prevalence and adverse outcome of infectious complication (IC) post-EAIRP may be underestimated. We aim to provide national trend estimation of EAIRP incidence and outcome in France. Methods and analysis From the French Common Classification of Medical Acts, we will define four categories of EAIRP. We will collect procedures via the French nationwide hospital discharge database, called Programme de Médicalisation des Systèmes d'Information (PMSI) and derived from the Diagnosis Related Group system. Various combinations to identify the numerator will be employed according to a pre-established algorithm.
Technical data wrangling tools facilitating the use of PMSI will be developed to obtain a clean and well-structured database ready for statistical analysis. This protocol will require competences in medicine, epidemiology, statistics, data processing and techniques through various stages of the study. The cohort will contain the denominator (the first act of the first stay of each patient) and the corresponding numerator (the IC which will occur during the first stay). Ethics and dissemination No nominative, sensitive or personal data on patients have been collected. The study of the MOrtality and infectious complications of therapeutic EndoVAscular interventional radiology (MOEVA) study does not involve humans, and falls within the scope of the French Reference Methodology MR-004 according to 2016-41 law dated 26 January 2016 on the modernisation of the French health system.
7 rengths and limitations of this study ► The large sample size of Programme de Médicalisation des Systèmes d'Information (PMSI) enables analyses of rare conditions, uncommon treatments and special patient populations spanning several years of recruitment. ► The PMSI's database is immediately available and systematically collected over time. ► The chosen French Common Classification of Medical Acts' codes reflect homogeneous population selected for endoarterial interventional radiology procedure treatment evaluation. ► Infectious diseases coding is heterogeneous across clinicians within the PMSI's framework because they are more often secondary than principal diagnoses during a single stay.
11 AIRP, as a surgical activity, is susceptible to risk of infection, which varies according to the state of the patient and whether a established medical device is used or not. 5 Its practical implementation depends on individual and collective behaviours, organisation,  12  general constraints of hygiene  13  of image-guided of IR equipment and radiation protection. 14 The complexity and multiplicity of the procedures, the severity of the patient's disease and the need for optimal result are reasons for monitoring  15  and evaluation of all steps of the interventions. 5 16 Today, we have limited insights into the underlying infectious complication (IC) mechanisms post-EAIRP,  17 18  so we hypothesised that the prevalence and death from IC post-EAIRP are underestimated because previous estimations were not based on global databases, such as national databases.
Surveillance of healthcare-associated infections (HAIs) is now key to prevention and an effective element in the fight against HAIs. 19 Because monitoring is often time-consuming and labour-intensive,  20  only some studies estimated the prevalence of HAIs post-EAIRP. Malavaud et al have estimated the risk as 0. 64% for coronary angioplasty and 4. 9% for all arterial and venous angioplasties. 15 21 Other studies have reported the occurrence of prosthetic vascular graft infection with a cumulative incidence varying from 0. 5% to 5%  22 23  and from 0% to 3. 1%. 24 Data were heterogeneous  25  and associated with a low level of evidence. 26 Most studies were monocentric  27  and provided information on a particular microbial ecology and cannot be extrapolated to another centre. 6 he Programme de Médicalisation des Systèmes d'Information (PMSI) database,  28  which collects hospital discharge data (HDD), represents an important potential for epidemiology, with a positive cost/quality ratio since the data were already recorded.
Henceforth, surveillance and measurement of healthcare are increasingly based on risk-adjusted outcomes derived from administrative databases. 29 This is why researchers and policy makers use HDD to identify, track and analyse national trends in healthcare utilisation, access, charges, quality and outcomes. 30  France, the PMSI is an annual database of hospital inpatient stay. It is the largest, publicly available, all-payer inpatient care database. On mandatory use,  31  it generates 25 million stays per year. 32 In 1996 the PMSI was adapted from the Diagnosis Related Group (DRG) of the USA. The PMSI is used to create billing data submitted by hospitals to the state. DRG includes information on clinical and resource use mainly available from discharge abstracts. 33 RG is designed to deliberately classify groups of stays according to medical similarity and cost.
34 In most hospitals, the processing of information on medical records, which is then entered into databases for later analysis, follows a typical sequence. The medical activity reported by the PMSI is entered by coding the summary discharge of hospitals, which contains alphanumeric codes for (1) diagnoses according to the International Classification of Diseases, Tenth Revision (ICD-10) in its French version and (2) the French Common Classification of Medical Acts (FCCMA). 35 Thus, the FCCMA allows billing of hospital activity relative to payment of fees. The use of PMSI databases with specific architecture in an epidemiological context puts researchers and engineer face the complexity of handling these data. This complexity largely exceeds the number of individuals and variables. To decipher them, these data require structuring, cleaning, enrichment, pairing, concatenation, merge, recoding, analysis and validation across special software application before interpretation of findings.
Even if research in the field is developing, it remains discrete, and exploitation of national medicoeconomic databases for studies of the French PMSI is insufficient. To date, these preliminary treatments and protocols for PMSI exploitation are not standardised. They are reiterated in each study and involve a time-consuming implementation. To help develop improved methods to increasingly use PMSI data, we created a methodologiy for design of a PMSI cohort lends to the analysis. Our research question is the following: 'What is the incidence of the IC of EAIRP?' objectives The primary objective is to determine the epidemiology of IC secondary to EAIRP within 30 days of the procedure. The secondary objectives are (1) to identify the denominator, numerator and all records relating to the same individual using record linkage, (2) to assess clinical outcomes across four therapeutic approaches in different study populations (children and adults), and (3) to compare the characteristics of the patients who underwent EAIRP and developed IC with the same population without IC.
Open access study design MOrtality and infectious complications of therapeutic EndoVAscular interventional radiology (MOEVA) is an observational study of the longitudinal national cohort of all patients hospitalised in French public and private hospitals and assessed in the PMSI database. Patients will be selected by the presence in the hospital discharge data set, from 1 January 2009 through 31 December 2014, of at least one EAIRP according to the FCCMA. In accordance with the French national regulations, due to the absence of direct involvement of patients and the retrospective nature of the study design, informed consent is not required. The PMSI's tables will be linked using the unique encrypted ANOnymous (ANO) possible since 2001. 36 Each pathway patient will be studied for 24 months (figure  1 ).