dataesr/scientific-paragraphs-categorization huggingface dataset:
We did, on the other hand, adjust for gestational age and for the administration of antenatal corticosteroid therapy, two factors closely associated with neonatal outcome. Gestational age is one of the principal prognostic factors for late preterm births  [9] [10] [11] [12]. The effectiveness of antenatal corticosteroid therapy administered before 34 weeks in reducing the risk of respiratory distress in infants born from 34 to less than 37 weeks has previously been reported  37. The strength of our study was to have included a large number of patients, very few with missing data (n=14, 1. 25%). Our classification of preterm birth was established based on data recorded prenatally, collected in the medical file, and very detailed about the course of the pregnancy and decisions in advance of birth.
Study population Data used in the analyses were collected as part of two clinical trials. The first was carried out in 1995À1996 in the Lekie division (Centre Region) of Cameroon, to determine the incidence of post-IVM SAEs in a loiasis-endemic area, and the L loa MFD threshold above which SAEs can occur  [1]  This study included 17 877 subjects aged 5 years living in 106 villages, including 5550 IVM-naïve subjects aged 15 years whose pre-treatment L loa MFD was measured. The second trial was carried out in 2005 in the Lom-et-Djerem and Haut-Nyong divisions (East Region) of Cameroon to evaluate whether coinfection with Plasmodium sp. is a risk cofactor for Loa-related post-IVM SAE  [6]. This study included 4956 IVM-naïve subjects aged 13 years living in 74 villages. Both studies were approved by the Cameroon National Ethics Committee for Research in Human Health  [1, 6].
Discussion This paper presents the first approach ever developed to estimate the probability of a post-IVM SAE in a subject with a given L loa MFD. Our results corroborate previously published estimates of the relative risk of SAEs across groups with different MFD levels  [1, 6] , but represent a significant extension allowing the quantification of individual risk. In doing so, they provide a framework enabling a direct assessment of the risks associated with IVM mass administration and of the benefits of alternative onchocerciasis control strategies such as TNT. The models developed in this study were based on data from the only two population-level studies where post-IVM adverse events were monitored actively in subjects with known L loa MFD. For obvious ethical reasons, further studies of this type could not be conducted.
L'effet des différentes covariables a été estime ́ a ̀ l'aide du risque relatif de la sous-distribution (RRs) et de son intervalle de confiance a ̀ 95 % (IC95%). Quant à l'analyse de survie globale, un modèle de Cox a été utilisé considérant l'EO comme une variable dépendante du temps. Les variables prises en compte dans ces analyses multivariées étaient celles associées a ̀ une p-value inférieure a ̀ 10 % en analyse univariée. Ces analyses ont été réalisées pour l'ensemble des patients et en fonction de la présence d'un EO dès le diagnostic. Les analyses ont été réalisées au seuil de risque alpha global fixe ́ a ̀ 0,05 et a ̀ l'aide du logiciel SAS 9. 3 (SAS Institute Inc. , Cary, NC). La valeur du p considérée comme significative était fixée à <0,05.
Finally, the policeman was killed. Data were gathered from all firefighters to better elucidate the impact of exposure level on PTSD symptomatology in association with the subject's position (rank and status) in the fire service centre. The study was approved by the Health and Safety and Working Conditions Committee ( Comité d'Hygiène et de Sécurité et des Conditions de Travail), responsible for promoting actions aimed at preserving the physical and mental health of employees. Furthermore, we respected the ethics code of the American Psychological Association  [15]  and the ethics code of French psychologists  [16]. The consent has been organized by the firefighter department hierarchy (co-author). The recruitment into the study was based on voluntary participation.
Procedure Following the terrorist attacks, the PCL-S was sent to firefighters involved in the rescue operation. The questionnaires were sent in paper form and were also available online. The free return of the questionnaires was offered via an internal system of the firefighters' departments. In Nice, the data were mainly obtained approximately 6 months, with some late responses through 21 months, after the terrorist attack (N = 117). In Carcassonne (N = 69), these measures were taken 3 months after the attack. Most of the responses were collected at 3 and 6 months.
Results First, the PTSD prevalence was calculated. Of the Nice respondents, 39 (33. 33%) out of 117 respondents indicated a global score above 34, meeting the screening threshold  [20]. Of these, 20 (17. 9%) presented a score above 44, meeting the diagnostic value proposed by Paul et al. [20]. Of the Carcassonne respondents, 3 (4. 35%) people out of 69 had total scores from 34 to 40, and no one scored above 44. The diversity of the PTSD structural models proposed in the literature expresses the complexity of trauma. We focused on eight models related to the DSM-IV that were tested via a CFA as specified in Table  2. The results showed poor fit with our data (Table  3 ), which led us to apply an EFA to the PCL-S. The EFAs (     showed that firefighters I/II presented higher scores on vigilance than did officers (t (153) = 2.
Interestingly, icSARS-CoV-2-mNG and NiV-EGFP entered and disseminated in both lung and brain cultures (Fig. 2a ,b and Extended Data Fig. 1 ) whereas MeV IC323-EGFP-F L454W only infected the brainstem and the cerebellum (Fig. 2c  and Extended Data Fig. 1 ). Even at 4 dpi the hyperfusogenic MeV did not infect any cells in the lung cultures, suggesting that MeV entry in lung epithelial cells may require additional factors in this model (Fig. 2c  and Extended Data Fig. 1 ). SARS-CoV2 infection was then followed by genome quanti cation by RT-qPCR. The viral load was higher in lung than in brainstem and cerebellum (Fig. 2d ). This difference was already observed on the day of infection (Fig. 2d ). The greater susceptibility of lung cultures might arise either from the thickness of the slice (thicker than that of the brainstem and cerebellum cultures) or perhaps from a greater number of ACE2 expressing cells (as supported by the slightly higher ACE2 activity (Fig.
The qPCR step uses then a reverse primer against SARS-CoV-2 and a forward primer against NiV extension. For the GAPDH (Glyceraldehyde 3-phosphate dehydrogenase) and all other genes, 100ng of total RNA were reverse transcribed using the iScript cDNA Synthesis Kit (Bio-Rad). Obtained cDNAs were diluted 1∶10. Quantitative PCR was performed using Platinum SYBR Green qPCR SuperMix-UDG (Invitrogen) on a StepOnePlus Real-Time PCR System (Applied Biosystems). Primers were either designed using Beacon Designer (version 8) software or chosen after validation that their e cacy was close to 100% according to the MIQE checklist 66. All samples were run in duplicate and results were analyzed using StepOne version 2. 3 (Applied Biosystems). All results were normalized to the standard deviation (SD) for GAPDH mRNA, and the calculations were performed using the 2ΔΔCT model 67.
Heatmaps were generated using the R package pheatmap by calculating the log2fold change for infected samples relative to uninfected samples and taking the 50 with the largest absolute value, after eliminating those in which there were fewer than 5 normalized counts in the uninfected sample for lung, or 1 in brain. Genes for which the annotation did not include a formal gene symbol were manually searched in the Ensembl database for highly conserved rodent orthologues, which are included next to the Ensembl gene name in the heatmaps. Immuno uorescent stainings. Organotypic cultures from seven days-old hamsters were infected with 1,000 PFU of BetaCoV/France/IDF0571/2020 virus. 24 hours post infection the slices were xed during 1 hour in 4% paraformaldehyde (PFA), washed in 1× Dulbecco's phosphate-buffered saline (DPBS) and permeabilized and blocked in 1× DPBS-3% BSA-0.
3% Triton X-100 (perm and block solution) overnight at 4°C. Slices were incubated in the perm and block solution containing the primary antibodies overnight at 4°C. After 3 washes (5 min each) in 1× DPBS, slices were incubated in the perm and block solution containing the secondary antibodies for 1 h at RT; donkey anti-rabbit conjugated with Alexa 488 or 555, donkey anti-mouse conjugated with Alexa 488 or 555, and donkey anti-goat conjugated with Alexa 555 or 647 antibodies (1:500 each). After 3 washes in 1× DPBS, slices were mounted with Fuoromount-G® aqueous mounting medium (SouthernBiotech, catalog no. 0100-01) on epoxy slides (CEL-LINE, catalog no. 30-12A-BLACK-CE24) and coverslipped. Images were taken using an inverted microscope Zeiss Axio Observer. Z1 with confocal unit LSM 800 and analyzed using ImageJ software.
Acknowledgments The Fig. 1a has been created with BioRender. com. We thank  Bruno Lina ,  Andres Pizzorno  and  Manuel Rosa-Calatrava  from the  CIRI, Centre International de Recherche en Infectiologie, LYON, France , for providing us with the BetaCoV/France/IDF0571/2020 virus. We acknowledge World Reference Center for Emerging Viruses and Arboviruses (WRCEVA) and UTMB investigator,  Dr. Pei Yong Shi  for kindly providing recombinant icSARS-CoV-2-mNG virus based on 2019-nCoV/USA_WA1/2020 isolate. We thank  Sonia Longhi  from  AFMB UMR 7257 ,  CNRS  and  Aix-Marseille University, France , and  Frédéric Carrière  from  BIP UMR 7281 ,  CNRS  and  Aix-Marseille University, France , for advice and help in proofreading of the manuscript. We acknowledge  Denis Gerlier  for helpful advices and critical reading of the manuscript.
We thank  Fabienne Archer  for providing us with anti-SP-C and anti-αTubulin antibodies and for her numerus precious advices. We thank  Géraldine Gourru-Lesimple  and  Claire Dumont  for assistance in lab management. This work was supported by  ANR-CoronaPepStop  ( ANR-20-COVI-000 ) and  Fondation de France  to BH and  ANRS-COV8-SARSRhinCell  to CM.
Individual heterogeneity can be introduced in the parameters associated with the covariates entering the observable part of the utility or in the variance of the errors. This leads respectively to the mixed effect models (MXL) and the scale heterogeneity model (S-MNL). All these models can be estimated with the mlogit package  (Croissant 2020b ) which provides a unified interface and is available from the Comprehensive R Archive Network (CRAN) at https://CRAN. R-project. org/package=mlogit. The first version of mlogit was posted in 2008 and it was the first R package allowing the estimation of random utility models. Since then, other package have emerged. 3 The following packages provide useful additions to mlogit: • mnlogit  (Hasan, Wang, and Mahani 2016)  enables efficient estimation of MNL for large data sets, • gmnl  (Sarrias and Daziano 2017)  estimates MXL and S-MNL, but also the so called generalized multinomial logit model G-MNL which nests them, • latent-class multinomial logit models (LC-MNL), for which the heterogeneity is due to the fact that individuals belong to different classes and mixed-mixed models (MM-MNL) which are a mixture of LC-MNL and MXL can also be estimated using the gmnl package, • Bayesian estimators for multinomial models are provided by packages bayesm  (Rossi 2019) , MNP  (Imai and van Dyk 2017)  and RSGHB  (Dumont and Keller 2019).
Data sets can have two different shapes: a "wide" shape (one row for each choice situation) or a "long" shape (one row for each alternative and, therefore, as many rows as there are alternatives for each choice situation). Package mlogit deals with both formats by relying on the dfidx function from the dfidx package  (Croissant 2020a) , which takes as first argument a data. frame and returns an object of class 'dfidx', which in "long" format is a data. frame with a special column which contains the corresponding indexes.
Testing As for all models estimated by maximum likelihood, three testing procedures may be applied to test hypotheses about models fitted using mlogit. The set of hypotheses tested defines two models: the unconstrained model that does not take these hypotheses into account and the constrained model which imposes these hypotheses. This in turn defines three principles of tests: the Wald test, based only on the unconstrained model, the Lagrange multiplier test (or score test), based only on the constrained model and the likelihood ratio test, based on the comparison of both models. Two of these tests are implemented in the lmtest package  (Zeileis and Hothorn 2002) : waldtest and lrtest. The Wald test is also implemented as linearHypothesis in package car  (Fox and Weisberg 2019) , with a fairly different syntax.
ModeCanada We first use the ModeCanada data set, which was already coerced to a 'dfidx' object (called MC) in the previous section. The same model can then be estimated using as data argument this 'dfidx' object: R> ml. MC1 <-mlogit(choice ~cost + freq + ovt | income | ivt, MC) or a data. frame. In the latter case, further arguments that will be subsequently passed to dfidx should be indicated: R> ml. MC1b <-mlogit(choice ~cost + freq + ovt | income | ivt, ModeCanada, + subset = noalt == 4, idx = c("case", "alt")) mlogit provides two further useful arguments: • reflevel indicates which alternative is the "reference" alternative, i. e. , the one for which the coefficients of choice situation specific covariates are set to zero, • alt. subset indicates a subset of alternatives on which the estimation has to be performed; in this case, only the lines that correspond to the selected alternatives are used and all the choice situations where not selected alternatives have been chosen are removed.
NOx The second example is a data set used by Fowlie (2010), called NOx. She analyzed the effect of an emissions trading program (the NOx budget program which seeks to reduce the emission of nitrogen oxides) on the behavior of producers. More precisely, coal electricity plant managers may adopt one out of fifteen different technologies in order to comply with the emissions defined by the program. Some of them require high investment (the capital cost is kcost) and are very efficient to reduce emissions, some other require much less investment but are less efficient and the operating cost (denoted vcost) is then higher, especially because pollution permits must be purchased to offset emissions exceeding their allocation. The focus of the paper is on the effects of the regulatory environment on the manager's behavior.
pub <-mlogit(choice ~post + cm + lnb + vcost + kcost + kcost:age | + -1, subset = available & env == "public", data = NOxml) R> ml. reg <-update(ml. pub, subset = available & env == "regulated") R> ml. dereg <-update(ml. pub, subset = available & env == "deregulated") R> ml. pool <-mlogit(choice ~post + cm + lnb + vcost + kcost + kcost:age + + kdereg | -1 | 0 | env, subset = available == 1, data = NOxml, + method = "bhhh") R> library("texreg") R> texreg(list(Public = ml. pub, Deregulated = ml. dereg, Regulated = ml. reg, + Pooled = ml. pool), caption = "Environmental compliance choices. ", + omit. coef = "(post)|(cm)|(lnb)", float. pos = "t!", label = "tab:nox", + dcolumn = TRUE) Results are presented in Table  1 , using the texreg package  (Leifeld 2013). Coefficients are very different on the sub-samples defined by the regulatory environment.
The inclusive values link the two models. It is then straightforward to show that IIA applies within nests, but not for two alternatives in different nests. A consistent but inefficient way of estimating the nested logit model is to estimate separately its two components. The coefficients of the lower model are first estimated, which enables the computation of the inclusive values I l. The coefficients of the upper model are then estimated, using I l as covariates. Maximizing directly the likelihood function of the nested model leads to a more efficient estimator. Bhat (1995)  estimated the heteroscedastic logit model on the ModeCanada data set. Using package mlogit, the heteroscedastic logit model is obtained by setting the heterosc argument to TRUE:.
R> sc. heter <-scoretest(ml. MC, heterosc = TRUE) R> sapply(list(wald = wd. heter, lh = lh. heter, score = sc. heter, + lr = lr. heter), statpval) wald lh score lr stat  25. 196 25. 196  9. 488 6. 888 p-value 0. 000 0. 000 0. 009 0. 032 The homoscedasticity hypothesis is strongly rejected using the Wald test, but only at the 1% and 5% level for, respectively, the score and the likelihood ratio tests. JapaneseFDI  Head and Mayer (2004)  analyzed the choice of one of the 57 European regions belonging to 9 countries by Japanese firms to implement a new production unit. R> data("JapaneseFDI", package = "mlogit") R> jfdi <-dfidx(JapaneseFDI, idx = list("firm", c("region", "country")), + idnames = c("chid", "alt"), drop. index = FALSE) Note that the argument idx is a list of two elements, where the second element contains the names of the column containing the regions and the countries, indicating the nestedness of regions within countries and where region is a grouping variable, feature used later to easily define the nests.
There are two sets of covariates: the wage rate wage, the unemployment rate unemp, a dummy indicating whether the region is eligible to European funds elig and the area area are observed at the regional level and are therefore relevant for the estimation of the lower model, whereas the social charges rate scrate and the corporate tax rate ctaxrate are observed at the country level and are therefore suitable for the upper model. We first estimate a multinomial logit model: R> ml. fdi <-mlogit(choice ~log(wage) + unemp + elig + log(area) + scrate + + ctaxrate | 0, data = jfdi) Note that, as the covariates are only alternative specific, the intercepts are not identified and therefore have been removed. We next estimate the lower model, which analyzes the choice of a region within a given country.
Therefore, for each choice situation, we estimate the choice of a region on the subset of regions of the country which has been chosen. Moreover, observations concerning Portugal and Ireland are removed as these two countries are mono-regions. R> lm. fdi <-mlogit(choice ~log(wage) + unemp + elig + log(area) | 0, + data = jfdi, subset = country == choice. c & !country %in% c("PT", "IE")) We next use the fitted lower model in order to compute the inclusive value at the country level: iv ig = ln j∈Bg e β x ij , where B g is the set of regions for country g. When a grouping variable is provided in the dfidx function, inclusive values are by default computed for every group g (global inclusive values are obtained by setting the type argument to "global"). By default, output is set to "chid" and the result is a vector (if type = "global") or a matrix (if type = "region") with row number equal to the number of choice situations.
c) to a logical for the chosen country. R> JapaneseFDI. c <-subset(JapaneseFDI, + select = c("firm", "country", "choice. c", "scrate", "ctaxrate", "iv")) R> JapaneseFDI. c <-unique(JapaneseFDI. c) R> JapaneseFDI. c$choice. c <-with(JapaneseFDI. c, choice. c == country) Finally, we estimate the upper model, using the previously computed inclusive value as a covariate. R> jfdi. c <-dfidx(JapaneseFDI. c, choice = "choice. c", + idnames = c("chid", "alt")) R> um. fdi <-mlogit(choice. c ~scrate + ctaxrate + iv | 0, data = jfdi. c) If one wants to obtain different iv coefficients for different countries, the iv covariate should be introduced in the third part of the formula and the coefficients for the two mono-region countries (Ireland and Portugal) should be set to one using the constPar argument.
Dans notre article, nous traçons les grandes lignes du modèle de la langue initié par Zellig S. Harris et complété par Maurice Gross. Ce dernier définit ce modèle (ou théorie) comme étant l'association de la grammaire (en tant que système de règles) et du lexique (en tant que définition extensionnelle du système de règles), d'où la notion de lexique-grammaire. La question est pour nous de savoir quel est le type de lexicographie qui convient au modèle du lexique-grammaire : nous montrons que dans ce cadre, les dictionnaires sont nécessairement des bases de données informatisées et que la lexicographie est par conséquent plus qu'une méthodologie de recherche ; elle est aussi la réalisation la plus aboutie du modèle de la langue. Nous nous intéressons aux dictionnaires informatisés de Maurice Gross, de Gaston Gross et de Jean Dubois & Françoise Dubois-Charlier, que nous présentons comme des jalons importants dans l'entreprise de modélisation de la langue française.
Le choix de corréler le lexique à la grammaire implique la conception d'un nouveau type de dictionnaires, à savoir des bases de données informatisées structurées en tables qui mettent en relation les lexèmes avec leurs propriétés linguistiques caractéristiques, ce qui les rend disponibles pour le Traitement Automatique du Langage (TAL). A première vue, ce type de lexicographie est beaucoup plus qu'une méthodologie de recherche, puisque les dictionnaires obtenus, en tant que représentations du lexique, sont surtout là pour révéler et expliciter l'une des deux composantes du modèle de la langue. Il n'en reste pas moins que la méthodologie qui consiste à mettre en regard les propositions de la grammaire avec le plus grand nombre possible de faits expérimentaux remplit ses fonctions traditionnelles de vérification et de perfectionnement du modèle théorique.
, Le Pesant (1994), Mathieu-Colas (1998), et Le Pesant & Mathieu-Colas (1998). Revenons au Dictionnaire Electronique des Mots (DEM). Il s'agit d'une base de données lexicales à laquelle Jean Dubois et Françoise Dubois-Charlier ont travaillé jusque peu de temps avant leur mort, intervenue respectivement en 2015 et 2016. C'est une entreprise colossale, puisque la base de données compte près de 150. 000 entrées, mais elle est.
, Le Pesant (1994), Mathieu-Colas (1998), et Le Pesant & Mathieu-Colas (1998). Revenons au Dictionnaire Electronique des Mots (DEM). Il s'agit d'une base de données lexicales à laquelle Jean Dubois et Françoise Dubois-Charlier ont travaillé jusque peu de temps avant leur mort, intervenue respectivement en 2015 et 2016. C'est une entreprise colossale, puisque la base de données compte près de 150. 000 entrées, mais elle est largement inachevée. Elle n'en constitue pas moins une « matière première » exceptionnelle pour l'élaboration de ressources lexicales nouvelles plus spécifiques (cf. sur ce point l'article de (Lapalme et Le Pesant, 2020)). Le DEM présente les quatre caractéristiques suivantes : 1. contrairement aux dictionnaires du LADL, il incorpore les mots non prédicatifs, notamment les noms concrets ; 2.
Measurement of ERK activity ERK dynamics were measured using the mean nuclear intensity of miniCic. Whenever For the measurement of miniCic in neighbours combined with apical area (Figure  3 ), cell contours were tracked using E-cad-GFP (Packing analyser), while nuclei were manually tracked on Matlab using His3-mIFP. For each dying cell, the nuclear miniCic intensity and apical area were averaged for all the neighbours (first row and second row of cells). The final curves are averaged of each of these curves after alignment at the termination of cell extrusion (apical area=0). Note that the "n" used for s. e. m. calculation is not the total number of neighbours, but the number of cell clusters.