dataesr/scientific-paragraphs-categorization huggingface dataset:
Discussion We presented a unique platform for time-resolved spectroscopy which can acquire full spectral decays in parallel and without resorting to monochromator or compromising with low spectral resolution. To the best of our knowledge this is the most parallelized time resolved spectrometer system to date with 256 TCSPC channels. Some improvements are needed. The line rate from chip to PC is currently 200 spectra per second, which is low for TCSPC work in cell biology. However, for analyzing complex decays of fluorophores in solutions with cuvette readouts and time resolved tissue autofluroescence spectra, the photon budgets tend to be low. The PCB and chip architecture should allow an upgrade to 10-20 kHz line rate assuming USB2 data rates (30-40 MB/s). PRNU was measured to be 20% which is poor by today's standards, but this has not seriously affected TRES work as these were scaled by steady state spectra obtained with off-the-shelf spectrometer.
Acknowledgments We would like to thank  Biotechnology and Biological Sciences Research Council  ( BBSRC, United Kingdom ) (grant numbers  BB/I022937/1  and  BB/I022074/1 ),  Engineering and Physical Sciences Research Council (EPSRC, United Kingdom) Interdisciplinary Research Collaboration  (grant number  EP/K03197X/1 ) and the  Medical Research Council  ( MRC, United Kingdom ) (grant number  MR/K015664/1 ) for funding this work. We would like to thank  ST Microelectronics, Imaging Division, Edinburgh , for their generous support in manufacture of spectrometer SPAD array. We would also like to thank  David Tyndall ,  Dialog Semiconductor , for providing support on spectrometer chip PCB design,  David Li ,  University of Strathclyde , for suggesting CMM of IRF as a reference value for CMM estimates,  Richard Walker ,  University of Edinburgh , for help with FPGA firmware,  Dr Lina Imati ,  University of Edinburgh , for preparing ANS fluorescence dyes,  Dr Mike Tanner ,  Heriot-Watt University , for numerous useful discussions.
2% Triton in PBS) and then incubated with secondary antibody (1:300; Alexa Fluor 1 568 Goat anti-Guinea Pig IgG; Molecular Probes A-11075, Carlsbad, CA, USA) and Hoescht (1:100; Sigma-Aldrich). The coverslips were subsequently removed and mounted on microscope slides. The slides were observed under a microscope (Eclipse E800; Nikon, Tokyo, Japan) that was connected to a video camera and an image analyzer (NIS-ELEMENTS AR 2. 30; Imaging Software Nikon, Tokyo, Japan).
For data analysis, Ct values were normalized by a calibration factor that was obtained from interplate calibrators. Raw data from miRNome Panels is available in S2 Table. RQ values were obtained using the 2 ΔΔCt method  [27]  and normalized by the RQ value of miR-16-5p, which led to the best stability value according to NormFinder Software  [28]. Principal component analysis and heatmap generation were performed with an open source R script (available at http://a-slide. github. io/MirStat/) together with detailed online documentation. Prior to analysis, qPCR data were manually preprocessed. To minimize stochasticity observed at high Ct, values above 35 were considered non-detected (ND). Additionally, miRNAs with an intra-replicate Ct fold-change above 2 were excluded from analysis. In the lists of the most differentially expressed miRNAs, 3 detected values versus ! 2 ND values were required to receive the label "Detected vs.
A galaxy survey in the redshift range between z=0. 5 to z=3 is optimum for the BAO experiment. This corresponds to frequencies in the range 350 MHz to 1000 MHz, and continues naturally from the optimum high frequency of the SKA Low Frequency Aperture Array. Moreover, a field of view on the order of 100's of square degrees, and high angular resolution given by the ∼ 200 km baseline, makes the SKA mid frequency aperture array the only instrument capable of performing this experiment after only a few years observing. The SKA catalog of over a billion galaxies, with both their angular position and redshift, will be the ultimate database for BAO analysis. This will give exquisite constraints on the Equation of State of the Universe, and may well indicate that Einstein's Theory of General Relativity, together with a Cosmological Constant, is insufficient to explain Dark Energy.
EMBRACE Monitoring and Control Software The Monitoring and Control software for EMBRACE was developed at Nançay. An extensive Python package library on the SCU (Station Control Unit) computer gives scripting functionality for users to easily setup and run observations depending on e. g. type of the target. Integrated statistics data are acquired from the LCU (Local Control Unit) and saved into FITS files including header information with essential meta data including pointing information, timestamp, frequencies, etc. Raw data (beamlets) are captured from LCU Ethernet 1 Gbps outputs and saved into binary files  [32].
Acknowledgments EMBRACE was supported by the  European Community Framework Programme 6, Square Kilometre Array Design Studies (SKADS) , contract no  011938. We are grateful to ASTRON for initiating and developing the EMBRACE architecture. Maciej Serylak  acknowledges the financial assistance of the South African SKA Project ( SKA SA ). Henrik Olofsson ,  Aris Karastergiou , and  Maciej Serylak  were supported for multiple working visits to Nançay by grants from the  Scientific Council of the Paris Observatory.
This allowed setting the number of juveniles tested per brood to conduct further experiments. Thereafter, we similarly assessed the precision of the estimate of the sire effect (r S-PHS ) in the paternal half-sib design for different numbers of sires tested considering different values of h 2. The distribution of r S-PHS estimates was established from 100 simulated datasets of paternal designs considering two mated females per male, respecting interbrood and residual variance estimated by  Chaumot et al. (2009) , for different numbers of sires  (10, 20, 30, 40, 50, 100, 200, 400)  and for different values of theoretical h 2 (0. 1, 0. 2, 0. 4, 0. 6, 0. 8).
Statistical inference As in  Chaumot et al. (2009) , the observational variance components of Cd sensitivity of full-sibs and paternal and maternal half-sibs were estimated using variance decomposition of log-transformed survival times using linear mixed-effect models. Restricted maximum-likelihood (REML) estimators and 95% confidence intervals were computed with the lme function from the nlme library within the R software. Significance of random effects (brood, sire, dam) was assessed by comparison of models through likelihood ratio tests (LRT), and the significance of fixed effects (batch) was tested by ANOVA  (Pinheiro and Bates 2000). AIC and BIC criteria were also inspected, but they are not presented here because they always agreed with LRT. Hence, we tested for full-sibs the existence of differences in Cd sensitivity between broods (i.
Sib analyses of Cd sensitivity revealed between-brood variability, low heritability, and maternal effect Breeding design optimization The analysis of the 100 simulated full-sib datasets based on the variance components of Cd sensitivity established by  Chaumot et al. (2009)  indicated that the precision of the r B-FS REML estimator was poorly improved by increasing the number of juveniles tested per brood beyond five individuals whatever the number of broods tested (Fig. 3 ). This is why, contrary to our previous study, in a balanced design we exposed only five juveniles for all broods, discarding possible additional released juveniles from the experiment. This allowed testing more broods per batch and population, which increases the precision of r B-FS estimation (Fig. 3 ). Furthermore, the analysis of the 100 simulated paternal half-sib datasets (five juveniles per brood, two dams per sire), assuming different theoretical values for h 2 (from 0.
Statistical analysis We compared the socio-demographic and clinical characteristics between groups at trial entry. For dichotomous outcomes, we calculated the proportions for both groups, and for continuous outcomes, we calculated the means, standard deviations and medians. We used intention-totreat analysis to calculate the relative risk, the risk difference, the number needed to treat and the 95% confidence intervals for these parameters. No subgroup analysis was pre-specified. All analyses were performed using SPSS software (version 17). The protocol was approved by the Federal University Research Ethics Committee in May, 2007. All participants gave written informed consent. The study registry was obtained after participant recruitment began because the Brazilian Clinical Trial registry only became mandatory in 2012.
Full characteristics of the patients at study entry are described in Table  1. The randomisation process was successful in having very similar groups with regard to sex, mean age, guessed probability of TB and MDR-TB (multidrug resistant) and the proportion of subjects infected with HIV. At HUCFF, data on smoking and drinking habits are not routinely collected, and at PAAP, HIV examination is not routinely performed. Overall, the smear results were positive for 10% of the participants (35/348 MGIT vs 34/345 LJ), and active pulmonary TB was bacteriologically diagnosed in 15. 7% (58/348 MGIT vs 51/ 345 LJ). At PAAP, 2 clinical specimens were evaluated per patient in both arms. For the MGIT960 arm at HUCFF, 2, 3 and 4 clinical specimens were evaluated for 73, 31 and 4 patients, respectively, and for the LJ arm, those figures were 72, 37 and 7 patients, respectively.
The offshore sedimentary cover is thin and limited, dominated by rock outcrops. Generally, terrigeneous sediment supply by rivers is limited. Southern Brittany, especially to the East, is an exception due to important rivers and old marine formations that provide a larger sand supply. Soil erosion is the main provider for coastal sands via the rivers  (Fan et al. , 2004; Guillén et al, 2006). Slash and burn practices produced a limited forest clearance from c. 4000 cal BP (Early Bronze Age;  Marguerie, 1992)  exposing to interglacial rainfall a relictual periglacial topography  (Van Vliet-Lanoë and Guillocheau, 1995)   1 ), exclusively in connection with dune building phase, with a calibration using the CALIB 7. 0. Software  (Stuiver and Reimer, 2005)  and the radiocarbon calibration (IntCal13;  Reimer et al.
Data Analysis Principal components analyses (PCA) were used post hoc to determine the associations among the dependent measures from all six assessments. PCA is a data mining procedure that finds the best linear fit to the data using a series of perpendicular vectors or principal components (PCs;  Clewley et al. , 2008). Within each PC vector (i. e. , column) the structure of the correlations and non-zero numerical values in each column quantify the relative positive or negative correlations among variables  (Clewley et al. , 2008). To put it simply, we used PCA as a method of dimensionality reduction that, in this case, examines the contributions of the dependent measures to hand function and the associations among these measures. Due to the differences in units and normal distributions among variables, and for comparison purposes, we calculated the standard score (z-score) of each variable and used their standardized normal distribution values for the PCA dataset  (Jolliffe, 2005).
The PCs are presented in descending order quantifying their contributions to hand function such that the first principal component explained the largest amount of variance. We note that the first three PCs sufficed to capture approximately 85% of the total variance for both datasets; therefore, we limited our analysis to them. Significance was set at p < 0. 05 and Matlab and SPSS (version 22, IBM, Armonk, NY) was implemented for these analyses.
Discussion Understanding the latent domains of hand function has important implications for both the basic and clinical research communities. The multidimensional ICF model underscores the need to examine outcome measures across the three ICF domains, while at the same time, mapping them to meaningful functional domains. This holds especially true when considering the highly complex nature of the hand and its impact on activity and quality of life. Therefore we applied a dimensionality reduction technique (e. g. , PCA) to datasets from six hand-specific outcome measures to determine if and how they mapped into distinct functional domains. We find that the associations and disassociations among the six measures we included reveal three interpretable latent domains of hand function in older adults with and without CMC OA defined as strength, coordinated upper extremity function, and sensorimotor processing.
Acknowledgments We thank  Veronica Lothan ,  Kathleen Shanfield ,  Allison Chu ,  Juan Garibay ,  Isak Hagg , and  Novalie Lilja  for their assistance in data collection and collation. The contents of this publication were developed under a grant from the  Department of Education ,  NIDRR  grant number  H133E080024. However, those contents do not necessarily represent the policy of the Department of.
Statistics Statistical analyses were performed using Analyse-it 2. 30 version, for Microsoft Excel (Leeds, U. K. ). Results of within-day and the between-day imprecision are presented as mean ± standard deviation (SD) and relative SD (RSD %). One-way analysis of variance was used to compare the coefficient of variation (CV) calculated for different groups of BAL samples. Multiple curve estimation procedure, using SPSS 15. 0 for Windows (SPSS Inc. , Chicago, IL), was performed to compare regression curves and study the matrix effect. 11 p ≤ 0. 05 was considered statistically significant.
For this reason, carryover was assessed during validation by assaying blank sample after a high urea nitrogen concentration sample (1. 58 mg/dL) five times. This test demonstrated that the assay is not affected by sample carryover. All experiments were performed with both 4 and 6 µl of samples obtaining same results (data not shown), and there was a close correlation between urea values measured using the two different volumes (r = 0. 98; p < 0. 001).
(2. 6)-  (2. 10). This would allow to considerably simplify phenomenological analyses of the MSSM Higgs sector which, because of the large number of SUSY parameters to be taken into account, rely up to now either on large scans of the parameter space or resort to benchmark scenarios in which most of these parameters are fixed. Nevertheless, the most interesting aspect of the hMSSM is that it easily allows to describe scenarios with large values of the SUSY scale, M S 1 TeV, but weak-scale masses for the extended Higgs sector. Because of the large log(M S /m h ) that occur, the high SUSY scale scenarios are notoriously difficult to analyze and, before resuming the large logarithms, the MSSM Higgs spectrum could not be calculated in a reliable way. Until very recently, this was the case of the numerical tools that deal with the MSSM, such as the renormalisation group program Suspect  [35]  or the program FeynHiggs  [36]  that is more specialized on the MSSM Higgs sector, which were not reliable at too high M S outside the decoupling regime.
A new version of FeynHiggs in which some partial resummation of the large logarithmic terms is performed has become available and allows to address low tan β values in a somewhat reliable way  4  (albeit with M h values still below M h ≈ 125 GeV at tan β < ∼ 2). The hMSSM approach is currently being implemented in an updated version of the program Suspect. An immediate advantage of the hMSSM is that it re-opens the possibility of studying the MSSM low tan β region  [12] , which was for a long time overlooked. Indeed, as only SUSY scales of the order of M S ≈ 1 TeV were assumed in the analyses performed in the past, one always had a too light h boson with a mass below the limit M h > ∼ 114 GeV derived from the negative searches of a SM-like h boson at the LEP2 collider  [18, 19]. For a scale M S = 1 TeV, the possibilities tan β < ∼ 3 and tan β < ∼ 10 were excluded for, respectively the maximal-mixing scenario X t = √ 6M S and the no-mixing scenario X t = 0.
The bosonic decays will also be non-negligible at intermediate values of tan β, tan β ≈ m t /m b ≈ 5-10, when the A/H couplings to top quarks are suppressed while those to bottom quarks are not yet strongly enhanced. However, below the 2m t threshold, when the Higgs couplings to the bosonic states are not too suppressed and the only competition will be due to the Φ → b b decays that is only slightly enhanced, the rates for the H → W W, ZZ, hh and A → Zh channels will be smaller than at low tan β values. The branching fractions for the various Higgs decays discussed above are displayed in Fig. 4  in the [tan β, M A ] plane assuming the hMSSM with M h = 125 GeV. The Fortran program HDECAY  [41]  where the hMSSM relations were implemented has been used. The color code is such that the red area is when the considered decay rates are large, while the blue area is when they are small (for alternative and more easily readable figures for the branching ratios, as well as for the production cross sections, see for instance Refs.
The rates for b b → Φ have been obtained using the program SusHi  [51]  and an adapted version of HIGLU  [52]  has been used for gg → Φ. As can be seen, the cross sections are rather large in particular at high tan β and, for gg → Φ, also at low tan β when the Higgs couplings to b-or t-quarks are strong and at relatively low M A when the phase space is not too penalizing. Even for M A = 500 GeV (1 TeV), the production rates are significant at √ s = 8 TeV (14 TeV), if tan β is sufficiently high or low.
In particular, the associated production of the lighter chargino and the next-to-lightest neutralino q q → χ ± 1 χ 0 2 would lead to large cross sections at √ s = 8 TeV and the decays χ ± 1 → W χ 0 1 and χ 0 2 → Zχ 0 1 , with leptonic gauge boson decays, would have significant branching fractions. The search for leptons plus missing energy at the first run of the LHC, in particular the clean trilepton events from the chain pp → χ ± 1 χ 0 2 → W Zχ 0 1 χ 0 1 → E mis T , imposes severe restrictions on the parameter space. For instance, for M 1 ≈ 100 GeV, the area µ ≈ M 2 < ∼ 200 GeV that corresponds to the choice adopted for Fig. 9  is by now excluded by the LHC data  6  [62]. To evade these experimental bounds, one needs either to increase the parameters µ 2 ≈ M 2 well above 200 GeV with a consequence that the phase space for the Higgs decays will be limited, or to make that the light χ states are either pure higgsinos (µ M 2 ) or pure gauginos (µ M 2 ), which then suppresses the Zχχ couplings e.
2% at M H ± = 80 GeV (about the exclusion limit obtained on M H ± from LEP2 searches  [18, 19] ) to 0. 16% at M H ± = 160 GeV (beyond which phase space effects start to be too penalizing H ± = M 2 A + M 2 W. This is what is illustrated by the dark blue area of Fig. 11  in which the constraints on the [M A , tan β] plan are shown: we take the limits on BR(t → bH + )×BR(H + → τ + ν), that we calculate using the program SDECAY  [68] , and interpret them in the hMSSM. We see that in our case, the entire area M A < ∼ 140 GeV is excluded at low tan β values, reducing to M A < ∼ 130 GeV at high tan β. In contrast to ATLAS and CMS, which use different means to calculate the product of branching ratios, we do not have the holes at the extreme values of M H ±. In the previous references, both experiments performed also searches for heavier H ± states with M H ± > ∼ m t +m b ≈ 180 GeV, by considering the process pp → H ± t(b) with again H + → τ + ν.
The main ingredients of the analysis are as follows. The normalization of the Higgs signal has been obtained using the programs HIGLU for the production cross sections and HDECAY for the decay branching ratios. The total cross section of the SM background (which will serve as a normalization) has been obtained using the program Top++  [80]  when the renormalisation and factorization scales are fixed to µ R = µ F = m t. In this equation, the first error is the one due to the scale variation within a factor of two from the central scale, and the second one the PDF+α s uncertainty. This value for the cross section is obtained at NNLO in QCD including the resummation of next-to-next-to-leading logarithmic (NNLL) soft gluon terms and it turns out that it is only 3% larger than the value of the cross section when evaluated at NNLO  [82].
Note that at √ s = 14 TeV, using the same approximation and ingredients, one would obtain for the cross section σ QCD tot (pp → t t) = 966. 0 +22. 7 -33. 9 +40. 5 -40. 5 pb at √ s = 14 TeV (4. 4) Using the program MadGraph5  [83] , we have generated the signal and background cross sections for the process pp → t t. The differential cross section as a function of the invariant mass of the t t system, dσ/dm tt , is shown at √ s = 8 TeV in the upper part of Fig. 16  where mass bins of 10 GeV have been assumed. We overlay on the continuum QCD background distribution (in black solid line), the distributions for the A signal only (the colored lines) with tan β = 1 and three possible mass values, M A = 400, 600 and 800 GeV. In order to see the signals in the figure, we have multiplied the distributions by a factor of 5, 50 and 300, respectively.
We have not performed a detailed and realistic study of this process but attempted to roughly quantify the observation of a signal at the LHC, relying on present ATLAS and CMS analyses in searches for heavy (non Higgs) resonances decaying into top quark pairs at 8 TeV center of mass energies, and discussed its possible implications. It appears that the channel gg → H/A → t t, would be capable of covering partly the area at low tan β and high M A , hence allowing for a full coverage of the [tan β, M A ] plane of the MSSM up to Higgs masses M A ≈ 600 GeV with 300 fb -1 data at √ s = 14 TeV. At the high luminosity option of the LHC with 3000 fb -1 data, one could reach a full coverage of the MSSM parameter space for pseudoscalar masses closer to M A ≈ 1 TeV. More refined analyses are required in order to firmly establish the viability of the various processes discussed here, in particular the H/A → t t channel.
Acknowledgements: Discussions with the LHC Higgs cross section working group on the hMSSM, in particular,  S. Heinemeyer ,  G. Lee ,  M. Muhlleitner ,  S. Nikitenko ,  N. Rompotis ,  P. Slavich ,  M. Spira ,  C. Wagner  and  G. Weiglein , are greatfully acknowledged. AD is supported by the  ERC  advanced grant Higgs@LHC and JQ by the  STFC  Grant  ST/J002798/1.
The usefulness of monitoring this indicator to detect a disease-related increase in mid-term abortions was evaluated using data from the 2007-2008 episode of bluetongue serotype 8 (BT8) in France. An increase in the MAIR was identified in heifers and parous cows in 47% (n = 24) and 71% (n = 39) of the départements. On average, the weekly MAIR among heifers increased by 3. 8% (min-max: 0. 02-57. 9%) when the mean number of BT8 cases that occurred in the previous 8 to 13 weeks increased by one. The weekly MAIR among parous cows increased by 1. 4% (0. 01-8. 5%) when the mean number of BT8 cases occurring in the previous 6 to 12 weeks increased by one. These results underline the potential of the MAIR to identify an increase in mid-term abortions and suggest that it is a good candidate for the implementation of a syndromic surveillance system for bovine abortions.