dataesr/scientific-paragraphs-categorization huggingface dataset:
2011 , Quisberth et al. 2011). The purification and direct sequencing of both strands of the DNA amplicons were performed by MACROGEN in Seoul, South Korea. Sequences were aligned and corrected using BioEdit version 7. 0. 9. Corrected fragments of 454 or 456 bp were resolved. BLAST (http://blast. ncbi. nlm. nih. gov/Blast) was used to determine the best identity with sequences deposited in GenBank. The sex ratio of Ps. coreodes adult specimens was analyzed with a chi-square test.
2006 ). In the current study, a fragment of 388 bp of the mtCytB of the four specimens found in the nest was also sequenced, and four different haplotypes were found (data not shown). Surprisingly, the number of mutations between the haplotypes of the two T. platensis specimens (five mutations) was greater than between T. platensis and T. infestans haplotypes (between two and four mutations). Moreover, it has been previously reported that 18 mutations can be found between mtCytB haplotypes of T. infestans  (Waleckx et al. 2011 ). These observations show that T. infestans and T. platensis are not clearly genetically differenciated. Carcavallo et al. (1998)  reported around 30 experimentally hybrids. Found naturally in Argentina, was the occurrence of T. infestans x T. platensis  (Abalos 1948 , Ronderos et al.
Acknowledgments Our deep acknowledgment and recognition to the late  Dr. Francois Noireau  for his contribution to this work. This study was partially supported by  CONICET , ( PIP 0007 )  Agencia Nacional de Promoción Científica y Técnica, Argentina (ANPCyT)  ( PICT 2011/1081 ). We thank all personnel of the  Virology Lab, Faculty of Veterinary Sciences, National University of La Plata , and  Dra. Catalá Silvia  (CONICET) and  Dra. Melo Cecilia  ( CONICET ) for reconfirmation of triatomine identities. We thank the  Mezza  family for support during the field work, and the communities of  Tres Estacas ,  El Palmar ,  El Picazo , and  Las Leonas.
Most of the published systems target the 5′NCR. However, the high genetic diversity of HRVs makes the detection of all variants difficult as evidenced by the alignment of available GenBank 5′NCR sequences. Indeed, a comparison of published HRV-specific PCR primers pairs showed that no single pair could detect all HRVs  [45]  and that more than one PCR is required for accurate description of HRV epidemiology. The range of detection of HRV variants by a probebased real-time PCR assay is predicted to be additionally restricted by mutations in the region of the probe. Accordingly, we have compared the performances of 3 tests for accurately detecting HRV in clinical samples: (i) a probe-based Taqman RT-PCR assay routinely used in our hospital laboratory; (ii) the same test used without the probe and in the presence of SYBR Green I, making theoretically possible to diagnose HRVs amplified by the primers but not detected by the probe; (iii) the same test used with both the probe and in the presence of the BOXTO intercalating agent, making theoretically possible to detect HRV detected and undetected by the probe in the same reaction.
In this study, we have tested and compared three different HRV molecular diagnostic assays. First, it is obvious that a proportion of samples truly infected by HRVs could not be detected using the Taqman probe test. This is evidenced by a number of probe-negative/BOXTO positive and probe-negative/SYBR green positive samples for which the presence of HRV amplicons was confirmed by direct sequencing of the PCR products. This phenomenon was shown to be highly reproducible and the same HRV positive samples were repeatedly detectable or undetectable using the probe-based assay (data not shown). Since all assays used the same amplification primers, the most likely explanation is a default in probe hybridisation. Analysis of the genomic sequence of HRVs that could not be detected by the probe-based assay showed that only a limited proportion of strains had mutations in the probe hybridisation region.
ELECTROPHYSIOLOGICAL PROCEDURES Electrophysiological single unit activity was recorded in M1 using electrodes pulled from borosilicate glass capillaries (GC 150 F, Harvard Apparatus, England) with a P-97 Flaming Brown (Sutter Instrument, USA). The tip of the electrode was broken to a diameter of 2 μm, and the electrode filled with a 0. 4 M NaCl solution containing 2. 5% neurobiotin (Vector Labs, USA). Electrodes had an in vivo resistance of 12-20 M. Recording electrodes were lowered in M1 (1. 3-1. 5 mm lateral and 1. 0-1. 5 mm anterior to bregma) at a depth of between 0. 65 and 1 mm from the brain surface. Neuronal activity was amplified 10 times, filtered (bandwith: 300 Hz-10 kHz), and further amplified 100 times (Multiclamp 700-B, Axon Instruments, USA). The signal was digitized (Micro 1401 mk II, Cambridge Electronics Design, England) and acquired on computer using Spike 2 software.
ANALYSIS OF ELECTROPHYSIOLOGICAL DATA The recordings were analyzed offline. Action potential (AP) duration was measured from the time when AP begins to the time when baseline is recovered. In order to assess the pharmacological modulation of neuronal activity, AP firing rate was analyzed before and after pharmacological treatments of 10 min or 1 min durations, respectively, for i. p. and intracortical drug injection. AP durations, neuron responsiveness to striatal stimulation, and firing frequencies were analyzed using Spike 2 7. 0 (Cambridge Electronics Design, England). AP firing patterns were analyzed using NeuroExplorer burst analysis (maximum interval to start a burst = 40 ms, maximum interval to end a burst = 10 ms, minimum interval between bursts = 20 ms, minimum duration of a burst = 5 ms and minimum number of spikes in a burst = 2).
For the total number of sections containing M1, we sampled every sixth section, starting with a section randomly selected from the first six sections, to generate a set of distributed sections within each sample. After the DAT immunohistochemistry, the average final thickness of the sections was 11. 97 ± 0. 38 μm (i. e. , a shrinkage of ∼70% during processing). The stereological analysis used was described previously by  Mouton et al. (2002). Each section was scanned by a camera (Orca-R 2 , Hamamatsu Electronic, Japan) connected to a microscope (DM 5500, Leica, Germany). Then, virtual sphere probes were scanned on the Z axis of M1 and Cg using the Mercator Software (Explora Nova, France). Each sphere was 4 μm radius and contained in a 10 μm × 10 μm square, spacing between each square was 50 μm × 50 μm.
To further characterize the neuroanatomical distribution of dopaminergic innervation, we measured the distribution of DA fibers within M1. Differences appeared in the rostrocaudal distribution of DA fibers. Indeed, the area innervated by DA fibers is maximal between 0. 2 and 1. 10 mm anterior to the bregma (Figure  1F ). Furthermore, regarding the mediolateral distribution of dopaminergic fibers in M1 (Figure  1G ), we observed that only this area, which corresponds to the forelimb representation area  (Tennant et al. , 2011) , is innervated on the whole mediolateral extend of the structure. Altogether, these data show that DA innervates the deep layers of mouse M1 with a rostrocaudal gradient. The density of this innervation in M1deep layers is comparable to that of Cg. It has been well described that DA could modulate Cg neuronal activity  (Lopez-Avila et al.
Acknowledgment. We are indebted to  Nicolas Burq  for fruitful discussions. The first author was partially supported by the  ANR  project  OPTIFORM. The third author was partially supported by the Grant  MTM2011-29306-C02-00  of the  MICINN (Spain) , project  PI2010-04  of the  Basque Government , the  ERC Advanced  Grant  FP7-246775  NUMERIWAVES, the  ESF   Research Networking Program OPTPDE. This work was done while the third author was visiting the  CIMI (Centre International de Mathématiques et Informatique) of Toulouse (France)  in the frame of the  CIMI Excellence Chair on "Control, PDEs, Numerics  and Applications".
Statistical analysis Statistical comparisons were made using Statview version 5. 0 (SAS Institute, Inc. , Cary, NC). To assess the effect of cognitive disruptor agents (scopolamine or MLA), factor effect (treatment) was first tested for significance by ANOVA (Analysis of variance), and then the effect of each dose of disruptor agent was assessed against the level of T-maze performance of vehicle group using Fisher's protected least significant difference (PLSD) pairwise comparison. To assess the difference between the two dose-response curves of each cognition-enhancing drug, ANCOVA (Analysis of covariance) was carried out using the treatment with disruptor agents as factor and the doses of cognition-enhancing drug as covariate. A P-value level of 0. 05 or less was considered significant.
CMS detector and event samples The data used in this analysis were collected with the Compact Muon Solenoid (CMS) detector. The central feature of the CMS apparatus is a superconducting solenoid of 6 m internal diameter that provides a magnetic field of 3. 8 T. Within the field volume are a silicon pixel and strip tracker, a crystal electromagnetic calorimeter (ECAL), and a brass/scintillator hadron calorimeter. Muons are detected in gas-ionisation detectors embedded in the steel flux return yoke of the magnet. A more detailed description of the CMS detector can be found elsewhere  [20]. A right-handed coordinate system is used in CMS, with the origin at the nominal interaction point, the x axis pointing to the centre of the LHC ring and the y axis pointing up, perpendicular to the plane of the LHC ring.
The dielectron trigger has transverse momentum (p T ) thresholds of 17 and 8 GeV, loose identification criteria, and very loose isolation requirements  [23]. In order to compare the data to the theoretical expectations, signal events and the expected backgrounds (Z+jets, tt, and ZZ) are generated by MC simulation and simulated within the CMS detector using GEANT4  [24]. Inclusive Z+jets and tt events are simulated with MAD-GRAPH 5. 1. 1. 0, using PYTHIA 6. 424 with the Z2 tune  [25, 26]  for the parton showers, hadronization, and MPIs. The CTEQ6L1 parton distribution functions (PDFs)  [27]  are used. The ZZ sample is simulated using PYTHIA. The Z+jets sample is also used to extract the signal efficiencies and for the comparison of kinematic distributions. The simulated samples used for comparison with data are normalized to the cross sections expected from theory in the full acceptance.
5. This factor corresponds approximately to the ratio of neutral to charged hadron production in the hadronization process of pileup interactions  [22, 23]. After this correction, the isolation variable is required to be less than 20% for muons and 15% for electrons. Both leptons are required to have p T > 20 GeV and pseudorapidity |η | < 2. 4. Opposite charges for the leptons are required when forming pairs. In the case of multiple lepton combinations, the lepton pair with the invariant mass closest to the nominal Z-boson mass is selected as the Z candidate. The efficiency of the dilepton selection is estimated using the tag-andprobe method  [32]  in events with at least two leptons and a jet passing the requirements detailed below. The offline selection efficiencies are estimated from data and simulations, and data/simulation 'scale factors' are estimated to correct for the differences; trigger efficiencies are estimated from data alone.
This is done by applying a veto on the azimuthal angle ∆φ Z,bb , which has been shown to be a discriminant observable for MPIs  [44]. The effect of this requirement on the cross sections has been found to be less than 0. 5%. Together, this leads to an uncertainty of at most 3% in the cross sections. • Vertex association: For the estimate of the cross section ratio σ Z+b/Z+j , an additional uncertainty arises from the contribution of jets not associated with the primary vertex. After the requirement on the momentum fraction of tracks originating from the primary vertex, the background due to pileup is estimated from simulation to be 2. 2%. The efficiency of the requirement is estimated from the distribution of this observable in data before applying the requirement. The corresponding systematic uncertainty is evaluated by comparing the distributions of this observable in data and simulation; it is assumed that the difference observed for the variable used for the vertex association is entirely due to events originating from pileup.
Acknowledgements We thank  Marco Zaro  for his help in simulating aMC@NLO samples for this analysis. We congratulate our colleagues in the CERN accelerator departments for the excellent performance of the LHC and thank the technical and administrative staffs at  CERN  and at other  CMS institutes  for their contributions to the success of the CMS effort. In addition, we gratefully acknowledge the computing centres and personnel of the Worldwide LHC Computing Grid for delivering so effectively the computing infrastructure essential to our analyses. Finally, we acknowledge the enduring support for the construction and operation of the LHC and the CMS detector provided by the following funding agencies: the  Austrian Federal Ministry of Science and Research and the Austrian Science Fund ; the  Belgian Fonds de la Recherche Scien-.
We then adjust the σ ij terms in simulation to match those found in data. The magnitude of the correction varies from a few percent to as high as 30%. To evaluate a systematic uncertainty for this procedure, we vary the level of E miss T smearing and determine the migration between different E miss T and M T bins in the simulated WZ sample. We find the uncertainty of the WZ background to be 20-35%, depending on the search region. The final WZ estimate is obtained by normalizing the corrected E miss T and M T shape to the theoretical cross section. The theoretical cross section is used to evaluate the SM background from WZ events because the contributions of signal events to WZ data control samples are expected to be significant.
The main background, from ZZ production, is thus estimated from simulation, with corrections applied to the predicted E miss T spectrum as described in Section 3. 1. 1. Backgrounds from hadrons that  Table  1 : Observed yields and SM expectations for three-lepton events with an ee or µµ OSSF pair, where the third lepton is either an electron or muon. The uncertainties include both the statistical and systematic components. are misreconstructed as leptons or from non-prompt leptons are evaluated using control samples in the data as described in Section 3. 1. 2. M T (GeV) E miss T (GeV) M < Table  2  summarizes the results. We consider events with exactly one OSSF pair and no τ h candidate, with exactly one OSSF pair and one τ h candidate, and with exactly two OSSF pairs and no τ h candidate.
4. To better reject background from fake leptons, we tighten the e (µ) isolation requirement to I rel < 0. 09 (0. 10) and the d 0 requirement to 0. 1 (0. 05) mm. Background from processes such as WZ and ttZ production is reduced by requiring E miss T > 120 GeV. This background is further reduced by rejecting events that, after applying looser e and µ selection criteria, contain an OSSF pair within 15 GeV of the Z boson mass. We evaluate the background from WZ events using simulated events and assign a 15% systematic uncertainty, which accounts for the difference between the observed and simulated yields in a WZ-event-enriched data control sample obtained by inverting the Z-boson veto. A second background is from events containing a prompt lepton from a W boson decay and a genuine lepton of the same sign from heavy-flavor decay or a misidentified hadron (mainly from tt Table  2 : Observed yields and SM expectations for exclusive channels of four-lepton final states.
The Z + jets process has a large cross section but is included in the rare background category because its contribution is very small after the signal-region requirements are imposed. With the exception of the W + light-flavor jets background, the background estimation is based on simulation. The simulation is validated in three data control regions (CR) that are enriched in different background components. A data sample enriched in W + light-flavor jets is obtained by vetoing events with b-tagged jets (CR-0b). A data sample enriched in the dilepton top-quark background is obtained by requiring either exactly two leptons satisfying the lepton selection criteria, or one such lepton and an isolated high-p T track (CR-2 ). Finally, the M bb requirement is inverted to obtain a data sample (CR-M bb ) consisting of a mixture of backgrounds with similar composition as the signal region.
The agreement between the data and the simulation in the three data control regions is used to determine scale factors and uncertainties for the background predictions. In CR-2 , the data are found to agree with the predictions from simulation, which are dominated by the dilepton top-quark background. A 40% uncertainty is assessed on the dilepton top-quark background, based on the limited statistical precision of the event sample after applying all the kinematical requirements. Correction factors of 0. 8 ± 0. 3, 1. 2 ± 0. 5, and 1. 0 ± 0. 6 are evaluated for the WZ → νbb, W + bb, and single-lepton top-quark backgrounds, respectively, based on studies of the CR-M bb and CR-0b samples. The rare backgrounds are taken from simulation with a 50% systematic uncertainty. The W + light-flavor jets background prediction is evaluated using the CR-0b sample, using the b-tagging misidentification rate for light flavor jets predicted by simulation.
Search in the multilepton final state For the multilepton search presented in Ref. [57] , events with at least three leptons are selected, including up to one τ h candidate. These events are categorized into multiple exclusive signal regions based on the number and flavor of the leptons, the presence or absence of an OSSF pair, the invariant mass of the OSSF pair (if present), the presence or absence of a tagged b jet, and the E miss T and H T values. The most sensitive signal regions for this search are those with exactly three leptons, no tagged b jets (using the CSVM criteria), and a low H T value. Backgrounds from dilepton tt events with non-prompt leptons are evaluated from simulation, while other backgrounds with non-prompt leptons are determined using data control samples. Backgrounds from WZ and ZZ diboson processes are estimated from simulation, with a correction to the E miss T resolution based on comparisons to data in control regions.
Outcome assessment Health-related QOL was evaluated with the validated French version of the Medical Outcomes Study 36-Item Short Form Health Survey (SF-36). The QOL protocol was added after the start of data collection. The SF-36 captures the following eight domains: physical functioning, role limitations due to physical problems, bodily pain, general health perceptions, vitality, social functioning, role limitations due to emotional problems, and general mental health  [37, 38]. All except one item (self-perceived health) were used in scoring these eight measures (score range: 0 = worst, 100 = best). Next, summary measures of physical health (PCS, physical component summary, including physical functioning, role limitations due to physical problems, bodily pain, and general health perceptions) and mental health (MCS, mental component summary, including vitality, social functioning, emotional problems, and general mental health) were computed using established, normed reference values (expected mean = 50.
0, SD = 10. 0) [39]. The SF-36 was administered at Years 3 and 5 of follow-up. In total, 2,100 participants completed the SF-36 at Year 3; 1,329 -at Year 5; and 1,263 -at both waves. Consistent with our objective to assess the medium/long-term supplementation effect, we retained participants with QOL data provided between 2. 5 (ie, Year 3) and 5 y post-baseline. Individuals with incomplete QOL data were excluded. Thus, we retained 1,978 individuals who had completed the SF-36 at Year 3 and 51 individuals who had completed it at Year 5 (with missing or incomplete Year 3 data).
We also performed tests for interaction between sex and prior CVD, respectively, and supplement type. For the bivariate analysis and for the tests for interaction, the significance level was set at 0. 20, whereas for the principal ANCOVA models the significance level was 0. 05 (2sided). Analyses were conducted with SAS software (version 9. 2; SAS Institute, Inc. ) without interfering with the intent-to-treat principle regarding supplement allocation.
Results The final sample consisted of 2,029 individuals (81. 1% of the SU. FOL. OM3 cohort) with QOL data from a single timepoint after a mean follow-up of 3. 160. 4 y. Baseline characteristics by treatment type are summarized in Table  1. The mean age was 61. 268. 8 y and men constituted 79. 6% of the sample. Treatment groups were well balanced regarding all baseline characteristics except for a slightly higher proportion of heavy alcohol users among those not receiving B vitamins (p,0. 05). Compared with individuals excluded from the analysis (n = 472), those included had higher baseline concentrations of folate, vitamin B6 and EPA+ DHA, and were less likely to be foreign-born and current smokers. QOL score distribution and sample characteristics by prior CVD are presented in Table  2. Most baseline characteristics as well as PCS, MCS, and all eight QOL variables were significantly different across CVD type.
This work was supported by the  French National Research Agency [ANR  grant  R02010JJ ], the  Ministry of Health, Sodexo, Candia, Unilever, Danone, Roche Laboratories, Merck Eprova AG, Pierre Fabre Laboratories , and  Catalent Pharma Solutions. The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript. This study was partly funded by  Sodexo ,  Candia ,  Unilever ,  Danone ,  Roche Laboratories ,  Merck Eprova AG, Pierre Fabre Laboratories , and  Catalent Pharma Solutions. The treatment capsules (active and placebo) were provided free of charge by  Roche Laboratories (Basel, Switzerland) ,  Merck Eprova AG (Schaffhausen, Switzerland) ,  Pierre Fabre Laboratories (Ramonville, France.
Tandem mass spectrometry (MS/ MS) was performed for molecular confirmation of HAQs, and quantification of HAQs was performed in full scan mode using HHQ-d4 and PQS-d4 as internal standards. Results were analyzed using the MassLynx MS software v4. 1 (Waters Corporation). HAQ concentrations were normalized to the bacterial protein concentration. All results are the means from at least three independent replicates. For AHL extraction, 10-ml bacterial cultures were mixed with 2 ml of ethyl acetate and 2. 4 g HHQ-d4 as an internal standard and then centrifuged at 7,800 rpm for 25 min. The top organic layer was carefully removed and evaporated in a glass vial under continuous high airflow in a heat block at 37°C. The ethyl acetate extraction was repeated three times for each sample. After complete evaporation, samples were stored at Ϫ20 C until analysis.
Five hundred microliters of Elastin Congo red (ECR) buffer (100 mM Tris-Cl, 1 mM CaCl 2 , pH 7. 5) containing 5 mg/ml ECR (Sigma) was added to 100 l of overnight cultures, and the mixture was incubated for 24 h at 37°C with shaking at 250 rpm. Samples were then centrifuged for 20 min at 4,680 rpm, and absorbance of the supernatant was measured at 492 nm. Data analysis. Prism 5 (GraphPad Software) was used to calculate the means and standard deviations and perform statistical testing. Means were compared using the Student t tests.