dataesr/scientific-paragraphs-categorization huggingface dataset:
In these cases we corrected the time difference to ensure that the zero-velocity or maximum velocity jets remain in the known positions. We first measure the wind profile and estimate its best fit using a reference wind  profile. It is worth noting that the images we used are not derotated. This novel technique allows the observer to compensate for the shift of the details produced by the rotation of the planet while a video observation of the planet for several minutes is being taken. Derotation allows the signal-to-noise ratio of the final stacked image to be increased, resulting in an improvement of the spatial resolution of the observable details. It is a feature implemented in the popular WinJUPOS software used by many amateurs  (Walker 2013)   3. From these error sources we consider that the minimum error value for each individual wind measurement is 15 ms -1.
Long-term variations Here we compare the mean wind profile obtained from the ensemble of all our measurements during 2011 with previous wind profiles of Jupiter retrieved during several years. We compare the 2011 wind profile with those obtained using HST data from 1995 to 1998 (García-Melendo & Sánchez-Lavega 2001), the Cassini wind profile corresponding to late 2000  (Porco et al. 2003) , and the most recent one retrieved from HST 2008 observations  (Asay-Davis et al. 2011). Figure  9  shows these global wind profiles. Each wind profile was measured by different authors using slightly different methodologies, but all of them are based on the ensemble of a large number of measurements, have removed the effects of large-scale structures, and have associated retrieval errors in terms of standard deviations of wind measurements.
In these high-resolution datasets the standard deviations are always larger than the navigation uncertainties. It is evident from Fig. 9  that some changes at particular latitudes have occurred over the long time scale represented by this data. The most notorious changes happen in the northern hemisphere. There is a large wind variation at the NEB (at 7 • ), the latitude of the dark projections and corresponding infrared hot spots, at the westward jet at 15 • , and at the narrowest and strongest jet of the planet situated at the NTB (at 18 • ). Another appreciable change is present at the 28 • westward jet as discussed by  Asay-Davis et al. (2011). Differences between these wind profiles are examined in further detail in Figs. 10  and 11 , where we also show the significance of wind differences using the p parameter.
Conclusions We have shown that ground-based images of Jupiter obtained with small telescopes (30-50 cm) employing the lucky imaging method can be used to retrieve regularly the Jovian zonal wind profile with good spatial resolution. We demonstrate that an image correlation technique can be successfully used to measure winds in Jupiter after careful selection of images obtained by amateur astronomers and appropriate navigation. The main results of this work are the validation of the amateur data and measurement technique used to retrieve the wind profile at cloud level and the mean 2011 wind profile shown in Fig. 5. These measurements also demonstrate the capability to monitor possible variations in Jovian jets and to establish the temporal scales involved and the relationship to morphology changes.
Study population We retrospectively analyzed a total of 152 consecutive adult patients who underwent kidney transplantation between August 2004 and April 2006 in the Nephrology-Transplantation Department of Strasbourg University Hospital (France). Nine subjects were excluded because of incomplete data (two patients were followed in another center, five died and two experienced graft losses within 3 months). There were 143 patients analyzed at transplantation, 143 at 1 year and 126 at 5 years (nine graft losses; three patients followed in another center and five deaths during the follow-up; Figure  1 ). In the routine pretransplant evaluation, bone mineral density (BMD) was measured using a Hologic Delphi densitometer (Hologic R , Inc. , Waltham, MA) at the lumbar spine (L2-L4), femoral neck and total hip in 133 of 143 patients.
Statistical analysis The analyses were performed using the SPSS 11. 0 software (SPSS, Inc. , Chicago, IL). The data are given as the mean AE standard deviation, the median [interquartile range] or the percentages for parametric, nonparametric parameters and categorical variables, respectively. Correlations were assessed by Spearman's test. Variables between groups were compared using Student's t-test, Mann-Whitney U-test, and chi-square test, as appropriate. Receiver operating characteristic (ROC) curves were plotted for D0 and M3 PTH levels and fractures occurrence, censored for fractures occurring before 3 months. Kaplan-Meier analyses were used to evaluate the time to fracture and to identify the factors associated with fractures using the log-rank test. The date of fracture onset was assumed to be the first date of a documented fracture with patients censored at death, loss to  follow up, dialysis or the end of the follow-up period.
Comet assay Neutral comet assays were performed using CometSlide assay kits (Trevigen). Treated cells were irradiated with 8 Gy and incubated at 37°C for different periods of time to allow DNA to repair (0, 30, 60, and 90 min). Cells were embedded in agarose, lysed, and subjected to neutral gel electrophoresis. Cells were stained with ethidium bromide and visualized using a fluorescence microscope. Olive comet moments were calculated by multiplying the percentage of DNA in the tail by displacement between the means of the head and tail distributions as described previously  (Olive et al. , 1990). The program CometScore Version 1. 5 (TriTek) was used to calculate olive moments. A total of 30 comets were analyzed per sample in each experiment.
We thank  Ray Kreienkamp  for his contribution to the study during his rotation in the laboratory and  Jesus Caceres  for technical assistance. We thank  D. Ferraro  and  J. Jaboin  for helpful discussions and clinical advice. Work performed in the laboratory of S. Gonzalo was supported by  National Institute of General Medical Sciences  grant  RO1 GM094513-01 ,  Department of Defense Breast Cancer Research Program Idea  Award  BC110089 , and  Research Development Award  from  Siteman Cancer Center. I. Gonzalez-Suarez  was a recipient of a postdoctoral fellowship from the  American Heart Association. Work in the laboratory of J. Zhang was supported by  National Cancer Institute  grant  R01CA154625. A. Novell ,  M. Martinez-Alonso ,  X. Matias-Guiu , and  A. Dusso  were supported by grants  2009SGR794 ,  RD06/0020/1034 ,  Beca Marta Santamaria , and  programa de intensificación de la investigación, Instituto Carlos III.
The first distribution is of obvious interest for resonance searches; the second and the third provide important information in the study of higher-order QCD perturbative effects and fragmentation, especially in some specific regions such as the small ∆φ γγ limit; the fourth can be used to investigate the spin of di-photon resonances. For this purpose, the Collins-Soper rest frame is preferred to other frame definitions because of its robustness with respect to initial state radiation. The results are compared to the predictions from: parton-shower Monte Carlo generators, Pythia  [10]  and Sherpa  [11] ; parton-level calculations with next-to-leading-order (NLO) QCD corrections using the Diphox  [12]  program complemented by gamma2mc  [13] ; and at next-to-next-to-leading-order (NNLO), using 2γNNLO  [14].
Data and Monte Carlo samples The data set analysed consists of the 7 TeV proton-proton collisions recorded by the ATLAS detector in 2011. Only events where the beam conditions are stable and the trigger system, the tracking devices, and the calorimeters are operational, are considered. Monte Carlo (MC) samples are produced using various generators as described below. Particle interactions with the detector material and the detector response are simulated with Geant4  [18]. The events are reconstructed with the same algorithms used for collision data. More details of the event generation and simulation infrastructure are provided in ref. [19]. Simulated di-photon events are generated with both Pythia 6. 4. 21 and Sherpa 1. 3. 1. Pythia uses the modified leading-order MRST2007  [20]  parton distribution functions (PDFs) while Sherpa uses the CTEQ6L1  [21]  PDFs.
Efficiency and unfolding The background-subtracted differential distributions obtained from the data are unfolded to obtain the particle-level spectra by dividing the signal yield in each bin of the di-photon observable under study by a "bin-by-bin" correction, which accounts for signal reconstruction and selection efficiencies and for finite resolution effects. The bin-by-bin nominal corrections are evaluated from the Sherpa di-photon simulated sample as the number of simulated diphoton events satisfying the selection criteria (excluding the trigger requirement) and for which the reconstructed value of the variable X under consideration is in bin i, divided by the number of simulated di-photon events satisfying the nominal acceptance criteria at generator-level and for which the generated value of X is in the same bin i.
The central value of the cross section predicted by Diphox+gamma2mc, 39 pb, is lower than the data but it is consistent with data within the theoretical ( +7 -6 pb) and experimental errors. The NNLO calculation of 2γNNLO (σ NNLO = 44 +6 -5 pb) is in excellent agreement with the data. The differential cross sections, as a function of the di-photon invariant mass, transverse momentum, azimuthal separation and of the cosine of the polar angle of the photon with largest transverse energy in the Collins-Soper di-photon rest frame, are also measured. Rather good agreement is found with Monte Carlo generators, after rescaling the Pythia and Sherpa distributions by a factor 1. 2 in order to match the integrated cross section measured in data and fixed-order calculations, in the regions of phase space studied.
Acknowledgments We thank the 2γNNLO authors for providing theoretical predictions of the NNLO di-photon cross section based on their code. We thank  Leandro Cieri ,  Stefano Catani ,  Daniel De Florian ,  Michel Fontannaz ,  Jean-Philippe Guillet ,  Eric Pilon  and  Carl Schmidt , for fruitful discussions on the theoretical calculations and their uncertainties. We thank  CERN  for the very successful operation of the LHC, as well as the support staff from our institutions without whom ATLAS could not be operated efficiently. We acknowledge the support of  ANPCyT , Argentina; YerPhI, Armenia; ARC, Australia; BMWF and FWF, Austria; ANAS, Azerbaijan; SSTC, Belarus;  CNPq  and  FAPESP, Brazil ;  NSERC ,  NRC  and  CFI ,  Canada ; CERN; CONICYT, Chile; CAS,  MOST  and  NSFC , China; COLCIENCIAS, Colombia; MSMT CR, MPO CR and VSC CR, Czech Republic; DNRF,  DNSRC  and  Lundbeck Foundation , Denmark; EPLANET,  ERC  and  NSRF ,  European Union ;  IN2P3-CNRS ,  CEA-DSM/IRFU , France; GNSF, Georgia; BMBF,  DFG ,  HGF ,  MPG  and  AvH Foundation, Germany ;  GSRT  and  NSRF, Greece ;  ISF, MINERVA, GIF, DIP and Benoziyo Center, Israel ;  INFN, Italy ;  MEXT  and  JSPS, Japan ; CNRST, Morocco; FOM and  NWO, Netherlands ;  BRF  and  RCN, Norway ;  MNiSW , Poland; GRICES and FCT, Portugal; MERYS (MECTS), Romania; MES of Russia and ROSATOM, Russian Federation; JINR; MSTD, Serbia; MSSR, Slovakia; ARRS and MVZT, Slovenia; DST/NRF, South Africa; MICINN, Spain;  SRC and Wallenberg Foundation, Sweden ;  SER ,  SNSF  and  Cantons of Bern and Geneva, Switzerland ;  NSC, Taiwan ;  TAEK, Turkey ;  STFC , the  Royal Society and Leverhulme Trust ,  United Kingdom ;  DOE  and  NSF ,  United States of America.
Dynamics of B + → pph + decays To probe the dynamics of the B + → pph + decays, differential production spectra are derived as a function of m pp and cos θ p , where θ p is the angle between the charged meson h and the opposite-sign baryon in the rest frame of the pp system. The pph + invariant mass is fitted in bins of the aforementioned variables and the signal yields are corrected for trigger, reconstruction and selection efficiencies. They are estimated with simulated samples and corrected to account for discrepancies between data and simulation. The signal yields are determined with the fit models described in the previous section, but allowing the combinatorial background parameters to vary. The systematic uncertainties are determined for each bin and include uncertainties related to the PID correction, fit model, trigger efficiency, and the size of the simulated samples.
Acknowledgements We express our gratitude to our colleagues in the CERN accelerator departments for the excellent performance of the LHC. We thank the technical and administrative staff at the LHCb institutes. We acknowledge support from  CERN  and from the national agencies:  CAPES ,  CNPq ,  FAPERJ  and  FINEP (Brazil) ;  NSFC (China) ;  CNRS/IN2P3  and  Region Auvergne (France) ;  BMBF ,  DFG ,  HGF  and  MPG (Germany) ;  SFI (Ireland) ;  INFN (Italy) ;  FOM  and  NWO  (The Netherlands); SCSR (Poland);  MEN/IFA (Romania) ;  MinES, Rosatom ,  RFBR  and  NRC "Kurchatov Institute" (Russia) ;  MinECo, XuntaGal and GENCAT (Spain) ;  SNSF  and  SER (Switzerland) ;  NAS Ukraine (Ukraine) ;  STFC  ( United Kingdom );  NSF (USA). We also acknowledge the support received from the  ERC  under  FP7.
Data collection and follow-up The patients will be followed-up at 45 days, 3 and 6 months, and 1, 2 and 3 years after randomization. The follow-up protocol includes a physical examination to assess wound events, wound pain, patient temperature and adverse events, and a biological investigation (leukocyte count and C-reactive protein). At 6 months and 3 years, a CT scan and a bacteriological investigation are mandatory. These investigations may be performed at any other consultation according to clinical requirements. The quality of life questionnaires EuroQol 5D, SF-12 and CCS will be completed by the patient at each stage of the 3 years of follow-up. The necessity for follow-up beyond the scheduled formal consultations will depend upon the surgeon's clinical judgment. All events and additional costs will be listed.
Medico-economic analysis A cost-effectiveness analysis will be performed alongside the clinical evaluation. The direct medical costs (hospital and ambulatory costs) and non-medical costs (transportation costs) will be collected prospectively over the 3year follow-up period. The patients' quality of life will be assessed using two generic questionnaires (SF-12 and EuroQol 5D) and the Carolinas comfort scale, a specific, validated questionnaire for patients undergoing hernia surgery. An intermediate analysis will be conducted at 6 months. A Markov model will be constructed using 3 years' worth of follow-up data to assess the costeffectiveness of biologic meshes versus standard wound care taking into account all intercurrent events (hernia, infections, encapsulation and so on) that affect both costs and patients' quality of life.
This research program is funded by the French Ministry of Health through Soutien aux Techniques Innovantes et Coûteuses (STIC) 2011. This study protocol was approved by the national ethics board (the Committee for the Protection of People) on 12 February 2012 under the registration number 2012-A00088-35 and received the authorization of the Agence Française de Sécurité Sanitaire des Produits de Santé on 30 March 2012 under the registration number 2011-A00059-34. The study is registered on the Clinicaltrials. gov website under the identifier NCT01594450.
The resultant images were analysed by fitting an ellipse to the diffraction pattern, and an RBC elongation index (EI) calculated for the different shear stress applied using the following equation: EI = (A -B)/(A+B), where A is the length of the major axis of the ellipse, and B is the length of the minor axis of the ellipse. Measurements were performed in duplicate, and the average EI values were subsequently fit with a non-linear regression (Prism, GraphPad Software Inc, Release 5. 0, USA) to identify two parameters that describe RBC deformability: SS 1/2 , the shear stress required for half of maximal deformation, and; EI max , the maximum elongation index (deformability) at infinite shear stress  [15].
Data Analyses Results are reported as means 6 standard deviation. Normality of the data was tested using the D'Agostino & Pearson omnibus normality test (GraphPad Software Inc, Release 5. 0, USA). Data for each sampling method were compared using a one-way ANOVA with repeated measures to determine whether significant differences in the means existed (SPSS Inc, Release 19. 0, USA). Tukey's adjustments were used when appropriate to determine differences between time points. Eta-squared (g 2 ) was calculated to determine the mean difference effect for each dependent variable. Relationships between blood lactate concentration and RBC deformability were assessed using parametric correlation analyses: the delta change in dependent variables (e. g. , lactate concentration; EI max , etc) was calculated for each exercise condition, when compared with rest (e.
Acknowledgements. The authors thank the EDC4 discussion team for stimulating the discussion around the building of AICC2012 and helping to decide on the best parameters to feed the DAT-ICE tool. We are particularly indebted to  V. Masson-Delmotte ,  C. Ritz ,  H. Fisher , and  D. Fleitmann  for their constructive suggestions. We further thank the anonymous reviewers and handling editor  E. Brook  for the critical reviews that improved the manuscript. This work was financially endorsed mainly by LGGE the  CNRS/INSU LEFE program  and " Fondation Ars Cuttoli ". The research leading to these results has also received funding from the  European Union 's  Seventh Framework programme  ( FP7/2007-2013)  under grant agreement no  243908 , " Past4Future. Climate change -Learning from the past climate " and is Past4Future contribution number  47.
Statistical analysis of behaviour data The Kruskal-Wallis test (KWT) was used to compare the different treatment groups. When a significant difference was observed, the Mann-Whitney U-test (MWT) was performed to compare each group to the control group. For the repeated measures, the Wilcoxon test (WT) was used for each variable in each treatment group. The results are expressed as median with interquartile range values. Differences were considered to be significant at the level of P<0. 05. All statistical analyses were carried out using the StatView W 5 statistical package (SAS, Institute, Inc. , USA).
The cDNA was diluted 10 times in RNAse and DNAse free water and analyzed with real time PCR on a Roche LightCycler 480. 10 μl reactions were run in 384-well plates using gene specific primers (Additional file 1: Table  S7 ) and 2x PerfecCTa ™ SYBR W Green FastMix ™ (Quanta BioScience, Inc. , Gaithersburg, MD) at 60°C. A pooled sample of all cDNAs was used to generate standard curves for all genes analyzed. The standard curves were used for relative quantification of the individual samples. NormFinder was used to check the stability of three different normalization genes  [68]. In both the male and the female groups cyclophilin was clearly more stable than the other two and chosen for normalization. The GraphPad Software was used to remove outliers.
Ethics Statement This non-interventional study was an evaluation of standard management at both hospitals and did not require any introduction of new diagnostic and therapeutic strategy (article L. 1121-1-2°, décret 2006-477). Therefore, the ethics committee (Comité de Protection des Personnes Ile de France III) has specifically waived the requirement for approval. All US examinations were performed as part of the medical care of women and the requirement for written informed consent has also been waived by the ethics committee. All personal health information data were deidentified.
Statistical analysis The Mann-Whitney nonparametric test and Pearson's Chi square test were used to compare quantitative and qualitative data, respectively (p <0. 05 was considered as significant). For multivarite analysis, variables with a p<0. 05 were included in a logistic regression model. Data are expressed as odds ratio (OR) with 95% confidence interval (CI). P<0. 05 was considered as significant. A linear regressions was used to establish a relationship between PVC-UA-PI max and PVC-UA-PI min. Statview 5. 0 software, SAS Institute, was used for statistical analysis.
Search strategy and eligibility criteria At least two of the authors searched independently the bibliographic databases such as SpringerLink, Science Direct, Wiley Online Library and PubMed in order to find essential articles on meniscal allograft preservation and sterilization methods. To obtain only the preferable articles from all the papers on menisci, the authors used the following key words: ''meniscal preservation'' and ''meniscal sterilization'' alone as well as in combination with ''cryopreserved'  ', ''deep-frozen'', ''fresh allograft'', ''lyophilized'', ''irradiated'' and ''ethylene-dioxide sterilization'' (in various combinations, using Boolean operators AND and OR). After the first review of the chosen articles, those with some of the key words in title were classified for further analysis.
Local stakeholders use these assessments to establish lists of protected species on their territory, which take into account factors such as population size, growth rate, population fluctua-tions, habitat fragmentation and range size  [12]. However, one of the difficulties of these assessments is that they are time consuming and require data that are not always available. Typically this involves obtaining information on contemporary population sizes or temporal changes in abundance, range or habitat quality. Because of this, Red Lists in tropical countries are known to be incomplete; therefore it's difficult to estimate the number of truly threatened plant species at a global scale  [13]. As a more immediate method of identifying species and areas of high conservation priority in New Caledonia, we have investigated the frequency and distribution of ''narrow endemic species'' (NES).
These are species ''that occur in one or a few small populations and hence are confined to a single domain or to a few localities''  [14]. Our rationale is not to circumvent the Red-List process; rather it is to provide a first-pass floristic scale assessment of where the conservation issues are most likely to be concentrated and to target further threat assessment. Although widespread species may also be threatened, we focus on Narrow Endemic Species, as they are inherently vulnerable due to their limited distributions in a country with high levels of environmental degradation. This assessment of NES can then be used to target further more detailed conservation assessments on individual species and sites in the context of the IUCN red-list framework. The use of herbarium records to obtain distributional data for rare or narrowly distributed species has already been identified as being useful in accelerating the establishment of conservation assessments  [15]  and for prioritizing conservation actions providing collection effort is taken into consideration  [16].
Data Recording We reviewed taxonomic descriptions and distributional data of all angiosperm and gymnosperm plant species (pteridophytes were discarded due to a shortage of distributional data and recent taxonomic revisions). This review used 25 volumes of ''La Flore de Nouvelle-Caledonie'' including 54 families of angiosperms and 5 families of gymnosperms and other taxonomic references (See Appendix S1). Distributional data were collected from the literature and from locality information on herbarium specimens from the IRD Noumea (NOU) using the ''Virot'' database, Paris (P) and Zurich (Z) herbaria (the latter two were consulted through their websites (http://coldb. mnhn. fr/and http://www. zuerichherbarien. ethz. ch)). The geographical coordinates (and their precision) of the numerous samples collected by H.