dataesr/scientific-paragraphs-categorization huggingface dataset:
Acknowledgement The authors acknowledge Patricia Horcajada and Christian Serre at the Lavoisier Institute (UMR 8180 CNRS-UVSQ) for their technical assistance and helpful advice concerning the synthesis of MIL-100 (Fe). We would also like to thank Mrs Laila MAHFOUDHI, Major Professor of English in the Sfax Faculty of Sciences (University of Sfax Tunisia) for proofreading and editing the language of the manuscript.
Statistical Analyses Each pen was considered to be an experimental unit. Growth performance data and carcass traits were analyzed using the analysis of variance model to determine the treatment effects. An orthogonal contrast was set up to compare the BD to the supplemented ones. In addition, a 2-way analysis of variance model was performed only on the supplemented treatments to determine the effect of the methionine sources and doses. Differences between means were considered to be statistically different for P < 0. 05. A Tukey test was performed a posteriori to determine the difference between means. The antioxidant markers and amino acid compositions of the feathers were analyzed by using the Kruskal-Wallis test due to the heterogeneity of the variances between treatments. A multi-comparison posthoc test was then performed to determine the difference between means  (Dunn, 1961).
4  In current tions were sent on 5 June 2017 to 25,776 EAPCI and 6,117 CVIT email recipients. Reminders were issued on 12 and 29 June, and the survey closed on 8 July 2017. Results are reported as numbers (percentages) and were compared using Chi-squared tests. Results were stratified for subgroups of interest including region or country of practice and level of interventional experience. Two-sided P<0. 05 was considered statistically significant. Analyses were performed using SPSS version 17. 0 (SPSS Inc. , Chicago, IL, USA).
Fourth, we cannot exclude the possibility that perceptions regarding the use of IVI for bioresorbable scaffold implantation may have changed following the withdrawal of the ABSORB scaffold (after the present survey had been completed). We recorded institutional PCI volume but not individual operator volume. The number of cardiologists across countries was not recorded. We did not capture data on IVI in specific settings (e. g. , imaging for atherectomy devices). Finally, although participants from a large number of countries worldwide were included in the survey, the present findings are less representative for regions underrepresented in the survey sample.
Conflict of Interest M. N. reports receiving honoraria from Terumo, Volcano, and Abbott. L. R. reports receiving research grants (awarded to the institution) from Abbott. R. C. reports receiving a fellowship stipendium from The Irish Board for Training in Cardiovascular Medicine supported by MSD. W. W. reports receiving grants from St Jude -Abbott, Terumo, grants and personal fees from MicroPort, and grants and personal fees from Biotronik, and is a cofounder of Argonauts and a past non-executive board member of Genae and Celyad. M. V. reports receiving grants from Astra Zeneca and personal fees from Abbott, Amgen, and Beyer. G. G. reports receiving grants and personal fees from St Jude and research grants from Boston Scientific. S. W. reports receiving grants from Biotronik, Boston Scientific, Bracco Pharmaceutical, Edwards Lifesciences, Medtronic, Terumo Inc.
Systematic review of the literature 0] [11]  This review is reported according to the PRISMA statement. 12 he MEDLINE (via the PubMed interface) electronic database from inception until 29 January 2015 was searched. The search strategy was built using the combination of four main search term concepts: (i) antibiotics; (ii) quantity/utilization; (iii) measurement unit; and (iv) inpatient (a detailed list of search terms is provided in Table  S1 , available as Supplementary data at JAC Online). In addition, the reference lists of included articles identified by the literature search were hand-searched to identify any additional relevant studies.
Screening process, data collection and analysis Special systematic review software (DistillerSR V R , Evidence Partners, Ottawa, Ontario, Canada) was used for literature screening based on defined inclusion and exclusion criteria. Two reviewers (M. S. B. , R. M. ) independently screened the titles and abstracts of the records retrieved by the initial search. Discrepancies between the reviewers were resolved through a discussion with a third reviewer (V. V. -P. ). Three reviewers (M. S. B. , R. M. , V. V. -P. ) independently extracted relevant data from included articles. A random selection of 10 papers was used as a pilot test to clarify any ambiguities in the process of data extraction. From the eligible studies, the following data were retrieved: study objective; study design (cross-sectional, prospective, retrospective, literature review); the type of quantitative metric (e.
Web site search The web sites of national and international organizations were also searched for data reporting antibiotic IQMs published until 29 January 2015. Two reviewers (M. S. B. and R. M. ) screened a selection of relevant web sites. These web sites were selected based on a discussion with all study authors. The list of searched web sites is presented in Table  S2. Data were extracted and all extracted IQMs from the included web sites were grouped into categories based on the numerator and presented to the stakeholders in the consensus procedure.
Systematic review of the literature and web sites The flow chart of the review process is shown in Figure  1. The initial search of the MEDLINE database identified 1152 articles. An additional 41 articles were identified through cross-referencing (n " 13) and searching of web sites (n " 28). By screening the abstracts, 968 articles and duplicates were excluded. An additional 57 articles were excluded for the following reasons: 29 did not have full text available and 28 did not meet the inclusion criteria. The complete search resulted in 168 articles (140 from MEDLINE and 28 from web sites). Table  S4  shows the articles and the following characteristics: author, year of publication, country, socioeconomic setting, study design, specific populations and objectives of the studies included in the review.
1] [42]  Both online surveys included a wide range of stakeholders from the medical community, from patients and global public health, from the pharmaceutical industry, and from payers, policy makers, government and regulators. One limitation is that the systematic review process was limited to only one database (MEDLINE), although it was accompanied by a citation-tracking search and the review of 26 relevant web sites. The web site search included the most relevant ones, but not all. One could interpret it as a limitation of this study, but the web site search should rather be seen as complementary to the systematic literature review. It was performed to make sure no metrics were missed in the literature. Initial arbitrary selection of stakeholders could be considered a limitation of this study, but all groups were well represented.
Funding This work was supported by the  Innovative Medicines Initiative (IMI) Joint Undertaking  (grant agreement no. 115618 -Driving re-investment in R&D and responsible antibiotic use-DRIVE-AB -www. drive-ab. eu). Resources are composed of financial contribution from the  European Union 's  Seventh Framework Programme  ( FP7/2007-2013 ) and  European Federation of Pharmaceutical Industries and Associations (EFPIA)  in-kind contribution.
Flow cytometry Cell suspensions were incubated with the antibody cocktail diluted in cold fluorescence-activated cell sorting (FACS) buffer (PBS, 2% FCS, and 2 mM EDTA) for 30 min at 4°C. For intracellular staining, cells were permeabilized with FIX & PERM Kit (BD Biosciences). Flow cytometry was conducted using the LSR 561 machine (BD Biosciences), and data were analyzed with FlowJo (Tree Star). The antibodies used are listed in tables S3 and S4. Confocal microscopy and PLA CAL-1 cells were harvested, centrifuged for 5 min at 4°C, then resuspended in prewarmed serum-free medium and dropped on a 12-mm coverslip, and covered with 1% alcian blue. The coverslips were then incubated for 20 min at 37°C and fixed with 3% paraformaldehyde. iPLAs were performed using the Duolink Kit (Sigma-Aldrich) according to the manufacturer's instruction.
Translation intensity measurement Puromycin labeling for measuring the intensity of translation was performed as previously described  (41). Puromycin (P8833; min 98% thin-layer chromatography, cell culture-tested, and diluted in PBS; Sigma-Aldrich) was added at 2. 5 mg/ml in the culture medium, and the cells were incubated for 15 min at 37°C and 5% CO 2. Cells were fixed and permeabilized with Cytofix/Cytoperm buffer (BD Biosciences), stained with the anti-puromycin antibody (12D10) directly coupled with Alexa Fluor 488, and diluted in Perm/Wash buffer (BD Biosciences). Flow cytometry was conducted using the LSR 561 machine (BD Biosciences), and data were analyzed with FlowJo (Tree Star).
Statistical analysis Statistical analysis was performed with GraphPad Prism software. When several conditions were compared, performed a one-way analysis of variance (ANOVA), followed by a Tukey range test to assess the significance among pairs of conditions. When only two conditions were tested, we performed Student's t test or Welch's t test (according to the validity of the homoscedasticity hypothesis). Statistical analysis on survival curves was performed using log-rank test, followed by the Benjamini-Yekutieli correction when required. from hypertension and that guanabenz and related compounds could, thus, have dual benefits for these patients. such that TLR9 did not reach endosomes where it is fully activated. The authors note that many lupus patients suffer However, guanabenz did not inhibit TLR9 by affecting GADD34 activity, but rather by altering cholesterol metabolism erroneously recognized by the immune system, and guanabenz reduced symptom severity in a mouse model of lupus.
In addition, there were about 3 times more splayed hair bundles in the ush1ga b1342/b1342 mutants and 4 times more in ush1ga b1240/b1240 than in WT siblings (Figure  3J ). Analysis of the anterior macula also revealed significant decreases in the number of hair cells and hair bundles in ush1ga b1342/b1342 but no significant differences in ush1ga b1240/b1240 (Figures  S3K  and S3L ). This latter result could be due to the presence of a second transcript variant of ush1ga. Supporting this, Ensembl (Ensembl Release 92) predicts a second transcript with a start codon in exon 2  (Zerbino et al. , 2018) , downstream of the ush1ga b1240/ b1240 frameshift in exon 1. Together, our data show that grxcr1, ush1c, and ush1ga zebrafish mutants have very similar phenotypes with significantly thinner, fewer hair bundles and splayed stereocilia.
Variables In the present study, the outcome of interest was episiotomy, which was defined by one code in the CCMP (JMPA006). The quality of hospital discharge abstracts regarding episiotomy has been validated thanks to a French validation study  [18]. Unfortunately, to our knowledge, no validity studies have used national data to study episiotomy in non-operative vaginal deliveries. The explanatory variables concerned the characteristics of the women and the characteristics of birth environment. At the maternal level, we considered the known risks factors for episiotomy: maternal age, parity (primiparous women were women who gave birth for the first time), gestational age (available only since 2010), multiple pregnancy, epidural analgesia, non-reassuring fetal heart rate, breech vaginal delivery, newborn weight > 4000 g (for single pregnancies, linkage with the birth abstract reliable only since 2013).
Statistical analysis The characteristics are presented as means or proportions. Percentages were compared using Pearson's Chi 2 test or Fisher's exact test under the conditions of application. To evaluate trends in episiotomy rates between 2007 and 2014, we used the Cochran-Armitage test. Episiotomy rates in 2007 and 2014 are presented per department (97 departments, including overseas territories). A mixed model was used to assess associations with risk factors. As the independence of the observations could not be confirmed, hierarchical logistic regression, which took into account the hierarchical structure of data, was performed using the individual maternal variables as level 1 data, and the hospital as level 2 data. Multilevel analyses were performed using SAS 9. 4. Geographic Information System MapInfo 11.
Results We report general observations on the effects of information structure on the realization of accentual contrasts based on visual inspection of time-normalized averaged F0 curves pooled over all eight speakers, followed by statistical evaluation with analysis of variance for repeated measures (rmANOVA). A Praat script was used to carry out the measurements and to correct pitch errors resulting from creaky voice or octave jumps  (Boersma & Weenink 2014). F0 measurements for initial accent and final accent target items will be reported separately for each of the four parts of the corpus given in Table  2. Figures  2  and 3  show averaged contours on normalized time scales for the minimal pairs [tɒbeʃ/tɒbéʃ] and [dídan/didán] in the three focus conditions, while Figures  4  and 5  show the two factive conditions.
Acknowledgements We are grateful to two anonymous reviewers for helpful comments that greatly improved this paper; to  Sajjad Peyvasteh  and  Atefeh Moslehi  for help with the experiments; to  Joop Kerkhoff  and  Farbod Javanshab  for technical support; to  Francisco Torreira  for a Praat script and to our participants for their enthusiastic collaboration. We would like to thank  Nasir Asadi ,  Mahmood Bijankhan ,  Saeed Ghaniabadi ,  Mortaza Taheri-Ardali ,  Lei Wang  and participants at the 8 th  Speech Prosody conference in Boston  for their discussion and suggestions. This research was supported by the  Centre for Language Studies (CLS)  at the  Radboud University Nijmegen , through a travel grant to the first author.
As a soft lepton is only present in a relatively small fraction of heavy-flavour jets, the soft lepton taggers are not always able to discriminate heavy-flavour jets from other jets. Therefore they are not used standalone, but rather as input for a combined tagger. The combined tagger, cMVAv2, uses six b jet identification discriminators as input variables, namely the two variants of the JP algorithm, the SE and SM algorithms, and the two variants of the CSVv2 algorithm. The training is performed using the open source SCIKIT-LEARN package  [42]  and the variables are combined using a gradient boosting classifier (GBC) as BDT. Prior to the training, the jet p T and η distributions are reweighted to obtain a similar distribution for all jet flavours. Although the correlation between the two CSVv2 discriminator values is close to 100%, a small improvement is seen in the case where the vertex finding algorithms reconstruct different secondary vertices.
Two trainings are performed: one for discriminating c jets from light-flavour jets (CvsL) and another one for discriminating c jets from b jets (CvsB). The training of the two discriminators was performed with the SCIKIT-LEARN package  [42]  using a GBC as implementation of the BDT. The GBC settings were optimized by varying them over a wide range of values, to ensure the optimal setting was contained within the scanned range. Both the CvsL and CvsB trainings were optimized by scanning a range of the parameters and comparing the final performance curves. The best performance was achieved with the number of boosting stages set to 500, the learning rate to 0. 05, the minimum number of samples required to split an internal node to 0. 6% and a maximum depth of the individual regression estimators of 15  (8)  for the CvsL (CvsB) training.
When refitting the primary vertex using the reconstructed tracks, the resolution on its position along the beam line further improves to less than 30 µm, as shown in Fig. 27. The reconstructed tracks and the refitted primary vertex are then used to reconstruct secondary vertices with the IVF vertex reconstruction algorithm. These vertices and tracks are then used as input for the CSVv2 algorithm described in Section 5. No dedicated training of the CSVv2 algorithm is used at the HLT, as studies have not shown any improvement in performance. The processing time of regional tracking used for b tagging with up to eight leading jets with p T > 30 GeV is on average 87 ms, not including the jet reconstruction time. The processing time was evaluated using data with the highest number of pileup interactions observed in 2016 (49 pileup interactions on average) and selecting events using a trigger threshold of 250 GeV on the scalar sum of the calorimeter jet transverse momenta.
In this event sample we expect an enrichment in b jets from top quark decays. There is also a small contribution from jets from pileup interactions due to the relatively low threshold on jet p T. • Single-lepton tt sample: Events are selected at trigger level by requiring the pres- ence of at least one isolated electron or muon  [9, 10]. Offline, exactly one isolated electron or muon is required, satisfying tight identification criteria. The electron (muon) is required to have a p T > 40  (30)  GeV and |η| < 2. 4. Events are further considered if they contain at least four jets with p T > 25 GeV. In this event sample a higher fraction of c jets is expected in comparison with the other samples. These c jets arise from the decay of the W boson to quarks. The distributions of all input variables and output discriminators in the four aforementioned event topologies are monitored to assess the agreement between data and simulation.
LifeTime method The muon jet sample used in the LT method is the same as for the PtRel method, except that the away jet is not required to be tagged. Also the strategy is similar to the PtRel method, but the fit is performed on the JP discriminator distribution. The track probabilities are calibrated using templates with negative impact parameter tracks in multijet events. The calibration is done separately on data and simulation to take into account a potential difference in the impact parameter resolution between both samples. The fraction of b jets is fitted including all shape systematic uncertainties via a correlation matrix. The tagging efficiency is then obtained as the ratio of the number of b jets obtained from the fit after and before applying the algorithm working point ε b = C b N tagged b N b.
Once the jets are assigned to the quarks, a tag-and-probe (TnP) technique is applied to determine the b tagging efficiency from data. As a tagging requirement, the medium working point of the CSVv2 algorithm is applied to either the b jet on the hadronic or leptonic side while the b jet from the other side is used as probe. The event is rejected if the tagging requirement is not satisfied. The probe jets are used to determine the b tagging efficiency of a given working point for each tagger under consideration. To achieve that, the distributions oflog(λ) and p miss T for probe jets passing and failing the tagging requirement are fitted with their expected templates to determine their number in data for the correctly-reconstructed tt events. During the fit, the normalization of the template for the non-tt background is naturally constrained by the p miss T distribution during the simultaneous fit.
Comparison of data with simulation The data are compared to the simulation using jets in boosted topologies. Jets are selected from events satisfying the following description: • Muon-enriched boosted subjets sample: A sample of muon-enriched multijet events is obtained using a combination of single-jet (AK4 and AK8) triggers requiring a muon in the jet. The data are compared to the simulation for soft-drop subjets (Section 6) of AK8 jets with p T > 350 GeV and within the tracker acceptance. The subjets are required to contain at least one muon with p T > 7 GeV and ∆R < 0. 4. In addition, to reduce the contribution from prompt muons, the ratio of the p T of the muon to that of the jet is required to be smaller than 0. 5. The subjet p T distribution in simulation is reweighted to match the observed distribution.
Measurement of the b tagging efficiency The data-to-simulation scale factors for subjets originating from b quarks are measured on subjets of AK8 jets using the selection requirements described in Section 9. 1. The LifeTime LT method presented in Section 8. 4. 1. 2 is applied to measure the scale factors for the loose and medium working points of the CSVv2 algorithm. The templates of the JP distribution for the various flavours obtained from simulation are fitted to the distribution observed in the data before and after applying the tagging requirement. An example of the fitted JP distribution for subjets with 240 < p T < 450 GeV is shown in Fig. 57  for all subjets and for subjets passing the medium working point of the CSVv2 algorithm. The systematic uncertainties associ-JP discriminator ated with the scale factor measurements are the same as evaluated for AK4 jets discussed in Section 8.
4. 1. 4. Compared to the measurements in Section 8. 4. 1. 2, the calibration of the track probabilities used in the resolution function of the JP algorithm (Section 5. 1. 1) is performed differently. In particular, for the nominal scale factor values considered here, the calibration of the track probabilities is derived from simulation and applied to both data and simulation. The systematic effect is evaluated from the difference between the nominal scale factor and that obtained by applying to the data the calibration of the track probabilities derived from the data. The uncertainty due to jets without a JP discriminator value is found to be negligible because of the higher jet p T. The measured data-to-simulation scale factors for the loose and medium working points of the CSVv2 tagger are presented as function of the subjet p T in Fig.
Indeed, after the selection, the distributions of the doubleb tagger discriminator values and its input variables were compared for simulated g → bb and H → bb jets. Since a different shape was observed for the discriminator distribution, the g → bb events were reweighted using the distribution of the z variable and the secondary vertex energy ratio, which are the variable distributions with the largest shape difference. The data-to-simulation scale factors were then computed using either the reweighted g → bb simu-lation or the original g → bb simulation. Both scale factors were found to be compatible, which confirms that the g → bb events allow for an unbiased measurement of the efficiency. The efficiency and the corresponding data-to-simulation scale factor SF double-b is measured using data for the working points of the double-b tagger defined in Section 6.
Similarly, N bkg,MC bb-tagged and N bkg,MC are the simulated number of background events with a tagged AK8 jet and the number of simulated background events before applying the working point of the double-b tagger, respectively. The data-tosimulation scale factors are measured both inclusively and in bins of the AK8 jet p T. The main systematic effect arises from the normalization of the background processes. An uncertainty of 30% is assigned to the cross section of each background contribution. An additional systematic uncertainty is related to the reweighting of the top quark p T spectrum. The shape of the p T distribution for top quarks in data is observed to be softer than in the simulation  [77, 78]. For the nominal scale factor measurements, a reweighting procedure is applied to correct for the observed difference.