dataesr/scientific-paragraphs-categorization huggingface dataset:
This provides further evidence that the stylized fact we detect is not an artifact of some correlation between isolated capitals and generally low state capacity that is unrelated to the kind of forces our theory underscores. We now turn to the question of whether we can shed direct light on the power sharing mechanism highlighted by the theory, by looking at the Polity IV data set. We have used the aggregate Polity measure to parse the sample between democracies and autocracies, but the data contain more information that can be used to study more subtle distinctions. In particular, the Polity measure aggregates the content of several other measures -and the extent to which they can be interpreted as relating to the degree of power sharing varies considerably. Out of the four variables aggregated into the Polity IV index of Democracy, two are described as pertaining to either the realm of "independence of executive authority" (ExecutiveConstraints) or to that of "political competition and opposition" (P articipationCompetitiveness).
comments and conversations. We also thank the  Taubman Center for State and Local Government at the Harvard Kennedy School (Campante) , the  French National Research Agency's (ANR)  grants  ANR-11-LABX-0091  ( LIEPP ) and  ANR-11-IDEX-0005-02 , and the  PRES Sorbonne Paris Cité (Do)  for generous financial support. Jean-Louis Keene  and  Nicolò Dalvit  provided excellent research assistance. A previous version of the paper has circulated under the title " Isolated Capital Cities and Misgovernance: Theory and Evidence ".
21 Diabetes mellitus, use of antihypertensive drugs, and smoking of cigarettes, cigars/cigarillos, or pipes were self-reported. History of CVD was identified from documentation (ie, population-based coronary event or stroke registers, person's medical records, a hospital discharge register, or other health information system) or self-reported history of myocardial infarction or stroke, including angina pectoris when the data collected did not permit its separation from myocardial infarction.
Statistical Analysis Anthropometric measures were categorized into 6 groups based on sex-specific sample means and SDs of all available data (<-1 SD below the mean, -1 to <-0. 5 SDs below the mean, ≥-0. 5-≤0. 5 SDs from the mean, >0. 5-1 SD above the mean, >1-2 SDs above the mean, and >2 SDs above the mean). The ranges of values for the categories are shown in Table  S1. Associations between the categorical anthropometric measures and the risk of all-cause and cardiovascular death were estimated separately for men and women using Cox proportional-hazards models, stratified by cohort, with age as the time scale, after partial and further adjustment. These associations were estimated in models including each individual anthropometric measure or a model including both WC and HC. Partially adjusted models included age at baseline (<50, 50-<55, 55-<60, 60-<65, 65-<70, and 70-<75 years).
Acknowledgments Drs Cameron ,  Romaniuk, Orellana , and Söderberg were responsible for the conception and design of the work. Drs Cameron ,  Romaniuk , and Orellana were responsible for analysis of the data and initial drafting of the manuscript. All authors other than  Drs Cameron ,  Romaniuk , and Orellana were responsible for acquisition of data. All authors were involved in revisions of the manuscript and interpretation of data and have approved the submitted version.
Sources of Funding This work was supported by the  Medical Research Council London  (grant  G0601463 [80983])  and  European Union   FP7  project  BiomarCaRE  (grant  HEALTH-F2-2011-278913 ), which supported the  Monica Risk, Genetics, Archiving, and Monograph (MORGAM) Project. The activities of the MORGAM Data Centre have been sustained also by recent funding from  European Union   FP7  project  Consortium on Health and Ageing: Network of Cohorts in Europe and the United States  ( HEALTH-F3-2010-242244 ).
Search strategies will be developed and peer-reviewed by medical information specialists. The search strategy for the updated review on e-cigarettes will be developed using that of the candidate systematic review. The MEDLINE®, PsycINFO, Embase, and the Cochrane Library electronic databases will be searched as of 2008 for the overview of reviews and from the last search date of the selected review for the updated review. Organizational websites and trial registries will be searched for unpublished or ongoing reviews/studies. Two reviewers will independently screen the title and abstracts of citations using the liberal accelerated method. Full-text screening will be performed independently by two reviewers. Extracted data will be verified by a second reviewer. Disagreements regarding full-text screening and data extraction will be resolved by consensus or third-party adjudication.
Similarly, Public Health England's recently developed guidance for clinicians includes e-cigarettes as a smoking cessation option to discuss with patients. The guidance indicates that e-cigarettes present less risk than smoking and that they may be as or more effective than nicotine replacement therapy  [73]. Other organizations state that there is currently insufficient evidence regarding the beneficial effects of e-cigarettes to make recommendations  [17, 71]. A majority of the available guidelines are out of date (i. e. last database search range: 2008 to 2015). Although recent, the NICE guideline excludes several smoking cessation interventions including varenicline, exercise, and alternative therapies (e. g. acupuncture, hypnotherapy)  [69]. Limitations in existing clinical practice guidelines necessitate the development of a Canadian guideline on tobacco cessation strategies for adults.
Literature search The search strategy will be developed and tested through an iterative process by an experienced medical information specialist in consultation with the review team. We will search Ovid MEDLINE®, Ovid MEDLINE® Epub Ahead of Print, In-Process & Other Non-Indexed Citations, PsycINFO, Embase Classic + Embase, and the Cochrane Library on Wiley. Databases will be searched from 2008 to the current date. The draft search strategy can be found in Additional file 2. The search strategy will be peer-reviewed using the PRESS 2015 guideline  [86]. Results of the PRESS reviews will be provided in an appendix in the final report. We will search for unpublished literature and reports of ongoing and completed reports using the Canadian Agency for Drugs and Technologies in Health (CADTH) Grey Matters checklist  [87]   Cessation.
The massive interest in these products from the public and tobacco smokers, as well as the evolving evidence base surrounding them, makes them essential to include g The outcome "relapse" was initially considered critical based on WG rating. However, based on discussion with WG members it was decided that this outcome should be considered important. It was also decided that this outcome is most important for KQ1b h Although initially rated as being of limited importance by the WG, based on discussions with WG members, it was decided that this outcome should be considered as important. Clinical experts and patients rated this outcome as important i Reviews will be considered systematic if they meet the four following criteria: (1) searches at least one database, (2) reports their selection criteria, (3) conducts quality or risk of bias assessment on included studies, and (4) provides a list and synthesis of included studies j Overviews will included if they meet the following criteria: (1) search at least one database, (2) report their selection criteria and how they will handle the inclusion of overlapping reviews, (3) provide information on the quality or risk of bias assessment of studies included in reviews, (4) provide a list of relevant reviews, (5) report the synthesized evidence from the included reviews, and (6) explicit declaration that the decision to undertake the network meta-analysis was made with firsthand knowledge of the primary studies, to ensure appropriateness of the analysis  The outcome "relapse" was initially considered critical based on WG rating.
However, based on discussion with WG members, it was decided that this outcome should be considered important. It was also decided that this outcome is most important for head-to-head comparisons. We will only collect data for this outcome when the comparator is an active intervention such as behavioural change techniques or cluster of techniques delivered as part of a behavioural change intervention different from that offered to the intervention group (e. g. behavioural change technique or cluster of techniques delivered as part of practitioner advice versus intensive individual counselling) d Although initially rated as being of limited importance by the WG, based on discussions with WG members, it was decided that this outcome should be considered as important. Clinical experts and patients rated this outcome as important e Reviews will be considered systematic if they meet the four following criteria: (1) searches at least one database, (2) reports their selection criteria, (3) conducts quality or risk of bias assessment on included studies, and (4) provides a list and synthesis of included studies screening will be conducted using an online systematic review managing software, Distiller Systematic Review (DistillerSR) Software©  [92].
The criteria above will be used as a guide; with the pool of candidate reviews in hand, information will be mapped to facilitate decisions about potential exclusion. Decisions to exclude reviews due to redundancy will be tracked and documented in a table of characteristics of excluded reviews. In cases where overlapping data cannot be avoided (i. e. overlapping reviews with similar search dates, quality, and comprehensiveness), we will include overlapping reviews and calculate the degree of overlap using the corrected covered area (CCA)  [83, 93]. Although reporting the degree of overlap is recommended, it does not minimize or omit potential bias caused by inclusion of overlapping reviews  [83, 93]. The CCA is calculated using the formula below, where N is the total number of studies across reviews (including multiple occurrences of the same study), r is the number of unique (first occurrence) studies, and c is the number of reviews.
For reviews reporting a meta-analysis, we will collect the pooled effect estimates, corresponding confidence intervals, and results of statistical tests for heterogeneity (e. g. number of studies, number of participants, chi-square, Cochrane Q, corresponding p values, I 2 ). For network meta-analyses, ideally sufficient evidence from direct comparisons will be available, and treatment effect estimates along with measures of uncertainty from those analyses will be extracted. However, where little to no evidence from direct comparisons is available and indirect comparison data exist, we will extract both analyses and determine extent of consistency of results and make appropriate interpretations. For indirect comparison analyses, effect estimates and corresponding credible intervals will be collected from indirect comparisons.
g. quantitative versus qualitative synthesis or in the statistical methods used). If overlapping reviews do not rely on the exact same studies, we will investigate differences in the eligibility criteria. If similar, we will evaluate whether discordance is attributable to differences in the search strategies (e. g. number and type of databases searched, whether grey literature was searched) or in the application of the eligibility criteria. If reviews use different eligibility criteria, Jadad et al. [105]  recommend comparing the publication status of primary studies (e. g. whether there are differences in the inclusion of unpublished reports), evaluation of the methodological quality of primary studies (e. g. differences across reviews regarding the assessment of quality of primary studies and how quality was used in interpreting the results of the review), language restrictions, and quantitative synthesis  [105].
Literature search The search strategy for this update will be developed using the search strategy of the candidate systematic review, once identified. The search strategy of the candidate review will be evaluated and modified as necessary. Databases will be searched from the last search date of the review. Using the OVID platform, we will search Ovid MEDLINE®, Ovid MEDLINE® Epub Ahead of Print, In-Process & Other Non-Indexed Citations, Embase Classic + Embase, and Psy-cINFO. We will also search the Cochrane Library on Wiley. The final search will be peer-reviewed using the PRESS 2015 guideline  [86]. Results of the PRESS reviews will be provided in an appendix in the final report. The grey literature will be searched using the same approach outlined for the overview of reviews.
Study selection and data extraction Study selection and data extraction will follow the same process described for the overview of reviews. Where study eligibility is unclear, authors will be contacted by email twice over 2 weeks for additional information. We will collect both self-report and biochemically validated tobacco abstinence and relapse. Data will be collected for all reported and relevant (see Table  3 ) time points of follow-up. Where needed, we will convert data (e. g. standard error to standard deviation) to facilitate consistent presentation of results across studies. Authors will be contacted by email twice over 2 weeks if any information is missing or unclear. Refer to Additional file 6 for a list of draft items to be collected during data extraction We will consult studies included in the original review to ensure that all outcomes of interest (Table  3 ) have been captured.
Meta-analysis We will examine the extent of clinical and methodological heterogeneity to determine appropriateness of performing meta-analysis. The Cochrane's Q (considered statistically significant at p < 0. 10) and I 2 statistic will be used to assess the statistical heterogeneity across included studies  [113, 114]. If appropriate, data from the original systematic review will be meta-analyzed with data from newly identified studies, using random effects models. For time-to-event data, the hazard ratio will be pooled using the generic inverse variance method. Analyses will be stratified by study design. For observational studies, we will use adjusted risk estimates in the meta-analysis. Should meta-analysis not be appropriate due to considerable heterogeneity, the range of effects will be presented and results will be discussed narratively.
Software The Cochrane Review Manager software version 5. 3  [116]  will be used to conduct analyses. Where needed, Comprehensive Meta-Analysis (CMA) or Stata may be used. The outcome "relapse" was initially considered critical based on WG rating. However, based on discussion with WG members, it was decided that this outcome should be considered important. It was also decided that this outcome is most important for KQ1b c Although initially rated as being of limited importance by the WG, based on discussions with WG members, it was decided that this outcome should be considered as important. Clinical experts and patients rated this outcome as important.
Acknowledgements Other members of the  Canadian Task Force on Preventive Health Care  who provided additional comments:  John Leblanc ,  Guylène Thériault ,  John Riva. Detailed descriptions of each member are available at https:// canadiantaskforce. ca. The authors also acknowledge  Marion Doull  and  Rachel Rodin  from the  Public Health Agency of Canada  for their input and direction during project scoping and refinement.
Overviews will included if they meet the following criteria: (1) search at least one database, (2) report their selection criteria and how they will handle the inclusion of overlapping reviews, (3) provide information on the quality or risk of bias assessment of studies included in reviews, (4) provide a list of relevant reviews, (5) report the synthesized evidence from the included reviews, and (6) explicit declaration that the decision to undertake the network meta-analysis was made with firsthand knowledge of the primary studies, to ensure appropriateness of the analysis.
Satellite-based vegetation data sets We further evaluated trends in the activity and growth of vegetation for the different land-cover classes using three satellite-based data sets: leaf-area index (LAI), net primary production (NPP) and above-ground biomass (AGB) stocks. The LAI data set was calculated from satellite imagery from Global Inventory Modeling and Mapping Studies (GIMMS LAI3g) described by  Zhu et al. (2015)  for 1982-2015. LAI data were provided in two time steps per month on a regular latitude-longitude grid of 1/12 • (subsequently aggregated to 0. 5 • ). Smith et al. (2016)  used the MODIS NPP algorithm and data for LAI and the fraction of photosynthetically active radiation from GIMMS to produce a 30-year global NPP data set, provided at monthly timescales for 1982-2011 at a latitude-longitude resolution of 1 • ×1 •.
The data are available at the NTSG data portal (https://wkolby. org/data-code/, last access: 4 August 2017). AGB stocks can be derived from estimates of vegetation optical depth derived from passivemicrowave satellite measurements. Liu et al. (2015)  produced a 20-year data set of AGB stocks for 1993-2012 based on measurements from a series of passive-microwave sensors. The data set is provided at a latitude-longitude resolution of 0. 25 • ×0. 25 • in annual time intervals and is available at http://www. wenfo. org/wald/global-biomass/ (last access: 13 February 2018). We tracked changes in LAI, NPP and AGB stocks for different land-cover types over time by selecting periods of at least 20 years common to ESA-CCI LC and the vegetation data sets  (1992 -2012 for LAI, 1992 -2011 for NPP and 1993 -2012  for AGB stocks).
ecmwf. int/ datasets/data/cams-ghg-inversions/ (last access: 16 November 2017)  (Chevallier, 2017)   Financial support. This research has been supported by the European Space Agency Climate Change Initiative (RECCAP-2 project (grant no. 4000123002/18/I-NB)). Review statement. This paper was edited by Eliza Harris and reviewed by two anonymous referees.
It is a result of the 10th International Carbon Dioxide Conference, Interlaken, Switzerland, 21-25 August 2017. Acknowledgements. This work was partly supported by the European Space Agency Climate Change Initiative (ESA-CCI) RECCAP-2 project (ESRIN/ 4000123002/18/I-NB). Marcos Fernández-Martinez is a postdoctoral fellow of the Research Foundation -Flanders (FWO). Vanessa Haverd acknowledges support from the Earth Systems and Climate Change Hub, funded by the Australian government's National Environmental Science Program.
Isolation and growth conditions In 2017 we isolated from the human sputum an unidentified bacterial strain. The study was validated by the ethics committee of IHU Méditerranée Infection under number 2016-011. Screening was performed by MALDI-TOF MS on a Microflex LT spectrometer (Bruker Daltonics, Bremen, Germany) as previously described  [7]. The obtained spectra (Fig. 1 ) were imported into MALDI Biotyper 3. 0 software (Bruker Daltonics) and analysed against the main spectra of the bacteria included in the database (Bruker database constantly updated with Microbes Evolution Phylogeny and Infections (MEPHI) database; http://www. mediterraneeinfection. com/article. php?larub=280&titre=urms-database). The initial growth was obtained after 48 hours' culture on Columbia agar with 5% sheep's blood in anaerobic conditions at 37°C and pH 7.
Strain identification The 16S rRNA gene was sequenced in order to classify this bacterium. Amplification was done by using the primer pair fD1 and rP2 (Eurogentec, Angers, France), and sequencing by the Big Dye Terminator v1. 1 Cycle Sequencing Kit and ABI Prism 3130xl Genetic Analyzer capillary sequencer (Ther-moFisher, Saint-Aubin, France), as previously described  [8]. The 16S rRNA nucleotide sequences were assembled and corrected using CodonCode Aligner software (http://www. codoncode. com). Strain Brachybacterium timonense exhibited a 97. 24% sequence identity with Brachybacterium faecium strain DSM 4810 (GenBank accession number NR_074655. 2), the phylogenetically closest species with standing in nomenclature (Fig. 2 ). We consequently classified this strain as a member of a new species within the genus Brachybacterium, family Dermabacteraceae, phylum Actinobacteria.
Genome sequencing Genomic DNA was extracted using the EZ1 biorobot (Qiagen, Courtaboeuf, France) with the EZ1 DNA tissue kit, then sequenced using MiSeq technology (Illumina, San Diego, CA, USA) with the Nextera XT Paired end (Illumina), as previously described  [10]. The assembly was performed with a pipeline incorporating different software (Velvet  [11] , Spades  [12]  and Soap Denovo  [13] ) on trimmed (Trimmomatic  [14] ) or raw data. GapCloser was used to reduce assembly gaps. Scaffolds <800 bp and scaffolds with a depth value lower than 25% of the mean depth were removed. The best assembly was selected by using different criteria (four scaffolds, nine contigs). The genome of strain Marseille-P4339 is 3<thinsp>092<thinsp>417 bp long with a 67. 3 mol% G+C content and contains 2727 predicted genes.
The degree of genomic similarity of strain Marseille-P4339 with closely related species was estimated by OrthoANI software  [14]. Values among closely related species (Fig. 4 ) ranged from 73. 98% between Brachybacterium nesterenkovii and strain Marseille-P4339 to 83. 79% between Brachybacterium faecium + Trypsine + α-Chymotrypsine - Acid phosphatase - Naphtalo-AS-BI-phosphohydrolase + α-Galactosidase + β-Galactosodase + β-Glucuronidase - α-Glucosidase + β-Glucosidase + N-Acetyl-β-glucosaminidase + α-Mannosidase + α-Fucosidase - +,.
Acknowledgements This work was funded by the  IHU Méditerranée Infection (Marseille, France)  and by the  French government  under the 'Investissements d'avenir' (Investments for the Future) programme managed by the  Agence Nationale de la Recherche (National Agency  for Research; Méditerranée Infection  10-IAHU-03 ). This work was also supported by ' Région Provence Alpes Côte d'Azur' and European funding 'Fondo Europeo de Desarrollo Regional' (FEDER). The authors thank  Hitachi Corporation  for providing the TM4000Plus Tabletop microscope. They also thank  M. Lardière  from  IHU-Méditerranée Infection, Marseille  for Englishlanguage review and  A. Caputo  from  IHU-Méditerranée Infection, Marseille  for submitting the genomic sequences to GenBank.
Introduction Bacterial genomes vary in size extensively, sometimes even within a species  (Bobay and Ochman 2017). As of today, the largest bacterial complete genome in GenBank is the one for the Sorangium cellulosum strain So0157-2 at 14,782,125 bp  (Han et al. 2013) , while the smallest one is described for the Candidatus Nasuia deltocephalinicola strain NAS-ALF at only 112,091 bp  (Bennett and Moran 2013) , more than 2 orders of magnitude smaller. Focusing on the 10 major bacterial species involved in global healthcare-associated infections (HAIs)  (Mirande et al. 2018) , median genome sizes range from 2. 9 megabase pairs (Mbp) for Staphylococcus aureus to 6. 5 Mbp for Pseudomonas aeruginosa. Whole-genome sequencing (WGS) has become an indispensable tool of modern microbiology  (Land et al.
Strains and culture conditions Strains were selected from the internal bioMérieux collection and involved 13 bacterial species (Table  1 ) (BIOMÉRIEUX EPISEQ© CS 2019). All strains were described in Additional file 1: Table  S1. As mentioned in Table  S1 , some strains belong to a type culture collection (i. e. , ATCC or NCTC). When the genome had been sequenced before, the GenBank accession number is indicated. All strains were grown at 37 °C on Columbia agar with 5% sheep blood (bioMérieux, Marcy l'Etoile, France) in an aerobic atmosphere for 12-24 h, except for C. difficile which was cultured for 24-48 h in an anaerobic environment using GENbag anaer (bioMérieux).