dataesr/scientific-paragraphs-categorization huggingface dataset:
A. Correlation functions and spectra In this section we present results obtained from fully corrected correlations for each p T bin studied for both d + Au and Au + Au datasets. The 2D correlations themselves are shown in Figs. 4 5 6 7 for primary triggers with transverse energy   [8, 10]  GeV; the bottom row shows that for  [10, 15]  GeV. For all correlations the away-side trigger p T is in  [4, 10]   [8, 10]  GeV; the bottom row shows that for  [10, 15]  GeV. For all correlations the away-side trigger p T is in  [4, 10]  GeV/c. From left to right, the associated p T ranges are [1,10] GeV/c, [1. 5, 10]  GeV/c,  [2, 10]  GeV/c, and [2. 5,10] GeV/c. η Δ d φ Δ N/d 2 )d trig (1/N η Δ d φ Δ N/d 2 )d trig (1/N φ Δ -1 0 1 η Δ -1 -0.
We find that for each T1 bin studied, the correlation functions and associated particle spectra from Au + Au events are similar to those observed in the d + Au data in spite of increased asymmetry between T1 and T2 triggers. The near-side yields of both the d + Au and the Au + Au data are smaller than their respective away-side yields, and the near-side Au + Au yield slightly drops when E T of T1 increases from  [8, 10]  to  [10, 15]  GeV. Both observations are possibly attributable to the increased direct γ contamination. This effect is further discussed later.
We note an increase in the correlation magnitude on the away side with respect to the near side in both Au + Au and d + Au correlations for our most asymmetric trigger pair selection. This increase by itself, as observed in both systems, is likely not related (or not in full) to the parton/jet energy loss. Because the trigger pairs preselected some di-jet asymmetry, the total yields and p T of the associated particles from the higher-energy-trigger side must be lower owing to energy conservation without any energy loss. Hence, the relative change between Au + Au and the reference d + Au data is a more relevant measure. Additionally, because the majority of the systematic errors are strongly correlated in this analysis between the near and away sides, the measurements of relative differences also have an advantage from an experimental point.
The spectra of associated charged particles for each trigger side from central Au + Au events are compared to the corresponding distributions from d + Au data in Figs. 8  and 9. The ratios of Au + Au to d + Au spectra are close to unity and have no prominent p T dependence, indicating that the softening or suppression, if present, is not nearly as strong as observed in the single-particle R AA. An additional factor to consider in the comparisons is a possible direct-γ contamination of the primary triggers measured by BEMC clusters, because the near-side yields of direct-γ triggers are expected to be close to zero  [27, 28] , potentially reducing the per-trigger measured yields on the near side. While the primary triggers from BEMC clusters of 8 < E T1 T < 15 GeV are dominated by photon pairs from π 0 decays, grouped into the same BEMC cluster owing to large tower size, the direct γ contamination may not be negligible over the E T range of this study  [20].
5 GeV/c, and decreasing for the softer associated hadrons to approximately ∼1 GeV/c. This trend can indicate that the jet fragmentation is shifted to the lower-p T regime (softening), or that the lower-energy fragmentation products are at larger angles from the jet axis (broadening). The later is less likely attributable to consistent jetlike peak widths observed in Au + Au and d + Au events. In either of the two cases, in the limit of associated hadron p T approaching zero, the value of relative ( E T ) Au+Au -( E T ) d+Au consistent with zero would indicate that full jet energy is recovered. Extrapolating our data to very low momenta, albeit large uncertainties, seems consistent with this scenario. Additional information could be obtained from the relative di-jet production rates. For the surface-emission scenario the jets and di-jets production rates are determined by the surface d+Au as a function of centrality.
[16]. The size of the permeable corona was first determined from tuning to the measured single charged hadron R AA results from RHIC. It was then used to predict the di-jet survival probability for the back-to-back triggers. To minimize systematic uncertainties related to the determination of the number of binary collisions (N coll ) and the number of participating nucleons (N part ) in the Glauber model, the double ratios measuring conditional di-jet survival probability were used. Such a double ratio, I Au+Au d+Au = R di-jet triggers AA R single triggers AA , constructed from nuclear modification factors (R AA , the binary scaled ratios of the observables in Au + Au and d + Au collisions), reflects any changes in probability to find an away-side trigger for each primary trigger observed in Au + Au data relative to d + Au.
ACKNOWLEDGMENTS We thank the  RHIC Operations Group  and  RCF at BNL , the  NERSC Center at LBNL , and the  Open Science Grid consortium  for providing resources and support. This work was supported in part by the offices of NP and HEP within the  US DOE Office of Science , the  US NSF , the  Sloan Foundation ,  CNRS/IN2P3 ;  FAPESP CNPq of Brazil; Ministry of Education and Science of the Russian Federation ;  NNSFC, CAS, MoST , and  MoE of China ; GA and MSMT of the Czech Republic; FOM and  NWO  of the Netherlands; DAE,  DST , and  CSIR of India ;  Polish Ministry of Science and Higher Education; National Research Foundation  ( NRF-2012004024 ),  Ministry of Science, Education, and Sports of the Republic of Croatia ; and  RosAtom of Russia.
Statistical analysis A statistical analysis was performed using R-project 2. 14 for GNU Linux Ubuntu. With respect to continuous variables, data were expressed as median and interquartile range (25% to 75%). With respect to dichotomous variables, percentages were calculated. Regarding MSSA and MRSA, sensitivity, specificity, positive predictive value, negative predictive value, positive likelihood and negative likelihood were computed. In order to assess the efficiency of the rapid diagnostic test, the Youden index was calculated as follows: Youden index = (sensitivity + specificity -1). A level of P below 0. 05 was considered as significant.
The membranes were probed with specific antibodies as described in the figure legends followed by detection with HRP-conjugated goat anti-rabbit IgG. Bands were visualized by enhanced chemiluminescence (Super Signal; Pierce Biotechnology, Rockford, IL, USA) and quantified by AlphaEaseFC software (Alpha Innotech, San Leandro, CA, USA). Each experiment was carried out two or more times using cell populations obtained from separate groups of mice.
Statistical Analysis Statistical significance was determined by the Wilcoxon rank sum test (independent two-group Mann-Whitney U test) as well as Student t test for comparisons between two groups. Multigroup comparisons were performed using one-way analysis of variance (ANOVA) with Tukey post hoc test. A value of P less than 0. 05 was considered significant. Analyses were performed on SPSS version 16. 0 (IBM, Armonk, NY, USA) for Windows (Microsoft Corporation, Redmond, WA, USA).
Study Design The study was conducted at the University Hospital of Clermont-Ferrand (France) in consecutive patients admitted for suspected meningitis between January 1, 2008 and December 31, 2009. We prospectively analyzed their CSF specimens using a real-time EV molecular assay irrespective of cytological examination results  [12]. Patients were eligible for inclusion in the study on condition of a positive detection of EV genome in CSF by an EV molecular assay (see below). In patients with proven enteroviral meningitis, data were extracted from medical charts and hospital computer records. A standardized questionnaire was used to collect information related to patients' clinical history, demographic information, CSF parameters, the use of cranial CT scan, and administration of antibiotic or antiviral treatments.
Statistical Analysis The data were organized in a database for the purposes of statistical analysis. We calculated the molecular test TAT (date and time molecular test result was reported minus date and time of the arrival of CSF sample in the laboratory), molecular test-todischarge time (date and time of discharge minus date and time of test result), and length of stay (LOS; date and time of discharge minus date and time of admission). Continuous variables were displayed either as mean 6 SD or median and interquartile range (IQR). Categorical variables were described by using frequencies and percentages. Comparisons of patient management in the two study periods (2005 versus 2008-09) were performed with Wilcoxon rank sum tests for continuous variables. Categorical variables were described using the Pearson chi-square test, Fisher exact test (if needed), and odds ratios (OR) with their 95% confidence intervals (95% CI).
Acknowledgments We thank  E. D. Schulze  and  W. W. Weisser  for allowing us to work in the framework of the  Jena Experiment. We also thank  E. Marquard  for the comparison of sown and realized diversity in the Jena Experiment, and  S. Rosenkranz  for data provision. Nitrification and denitrification measurements were performed at the AME platform ( UMR5557-USC1364 , Lyon).
8 ns Least Significant Bit and integral non-linearity lower than 0. 3 ns, multi-hits feature). The TDC and the slave clock are acquired by means of a CAEN V1718 VME bridge. The acquisition system is triggered by a 4/14 majority of the RPC layers. To obtain a ns-precision over the full range, the TDC was calibrated with a ppm precision. For this purpose a thermally stabilized oscillator producing a 5 kHz reference signal sent into a TDC channel was used during the whole data taking period. This way, the stability of the TDC oscillator can be monitored event by event, performing also the calibration with the required precision.
Methods 1 and 2 were applied to TT data and Methods 3 and 4 to RPC data. For events where the muon crosses at least one spectrometer its momentum and charge are measured. In 3 such events out of 58 CC events used in this analysis, the muon charge is positive. One event is CONTAINED (p µ ∼12 GeV/c), the other ones are FRONTMUON events (p µ ∼46 GeV/c and ∼ 79 GeV/c). They exhibit a clear muon track crossing both spectrometers and thus all drift tube stations could be exploited for charge and momentum reconstruction. The overall charge mis-identification probability for these events is below 1. 5%. Considering also the charm background contribution, the number of expected fake positive muons from the whole BB sample is < 0. 7 for the 3 observed events. If the analysis is restricted only to contained events for which both charm contribution and charge misidentification are lower, the expected number of fake positive muons is < 0.
Target Tracker data All 104 on-time recorded events were analyzed using the TT hit information, applying the same selection procedures as described in  [3]. The selected data sample includes 63 events. Four of them were rejected by the TDC cut to remove outliers (as reported in Section 3). The neutrino interaction time and the corresponding time of flight T OF ν were computed using two different methods. The first method (Method 1) relies on the information of the earliest hit as described in  [3]. The second method (Method 2) exploits the time information of all TT hits of the 3D muon track. Using the latter method, 48 CC events were selected. Method 2 results in a better time resolution (see last column of Tab. 3).
RPC Timing Board data With this new method (Method 4) the extra information provided by the special TDC (see Section 3) complements CNGS events acquired by the standard OPERA DAQ. The association of the additional data is performed on the basis of the UTC time readout by the slave clock and of the VME TDC data. In each event, accidental RPC hits inside the multi-hit 800 µs buffer of the VME TDC are rejected considering only those hits in a 128 ns window around the acquired trigger time. The remaining hits acquired by the VME TDC are then corrected by the calibrated delays (for the position along the read-out strip, information from the DAQ is again used) and averaged. The fit procedure is similar to the one used for Method 3. The intrinsic time resolution computed using muons crossing both spectrometers is 1.
Acknowledgements We thank  CERN  for the successful operation of the accelerator complex and the  CNGS facility , and for the prompt setting up of the bunched proton beam. We are indebted to INFN for the continuous support given to the experiment during the construction, installation and commissioning phases through its  LNGS laboratory. Funding from our national agencies is warmly acknowledged:  Fonds de la Recherche Scientifique -FNRS  and  Institut Interuniversitaire des Sciences Nucléaires for Belgium ; MoSES for Croatia; CNRS and IN2P3 for France; BMBF for Germany; INFN for Italy; JSPS ( Japan Society for the Promotion of Science) ,  MEXT (Ministry of Education, Culture, Sports, Science and Technology) ,  QFPU  ( Global COE program  of  Nagoya University, "Quest for Fundamental Principles in the Universe " supported by  JSPS  and  MEXT)  and  Promotion and Mutual Aid Corporation for Private Schools of Japan  for Japan; the  Swiss National Science Foundation (SNF) , the  University of Bern  and  ETH Zurich for Switzerland ; the  Russian Foundation for Basic Research  (grant  09-02-00300  a), the  Programs of the Presidium of the Russian Academy of Sciences "Neutrino Physics" and "Experimental  and theoretical researches of fundamental interactions connected with work on the accelerator of CERN", the  Programs of support of leading schools  (grant  3517.
2010. 2 ),and the  Ministry of Education and Science of the Russian Federation for Russia ; the  Korea Research Foundation  Grant ( KRF-2008-313-C00201 ) for Korea; and  TUBITAK The Scientific and Technological Research Council of Turkey , for Turkey. We are also indebted to INFN for providing fellowships and grants to non-Italian researchers. We thank the  IN2P3 Computing Centre  ( CC-IN2P3 ) for providing computing resources for the analysis and hosting the central database for the OPERA experiment. For the measurement of the neutrino time of flight with the timing boards we thank the  LNF ROG group , the electronics workshops of  LNF  and  LNGS  for the finalization of the VME clock slave and the  LNGS computing center  for the support in the calibration of the 1PPmS signal fiber delay.
Acknowledgments We thank  Wim Beenakker  and  Eric Laenen  for many useful discussions. IN and LH are supported by the  Foundation for Fundamental Research of Matter (FOM) , program 104 "Theoretical Particle Physics in the Era of the LHC". RG wishes to acknowledge the  Department of Science and Technology of India , for financial support under the J. C. Bose Fellowship scheme under grant no. SR/S2/JCB-64/2007  and  NIKHEF as well as LPSC, Grenoble  for hospitality when part of this work was done. Note added: As this paper was finalised new results from direct stop searches were presented by ATLAS including 13f b -1 of data from the 8TeV run [78]. These extend the stop exclusion to 580 GeV for massless neutralinos. When they decay exclusively into t χ0 1 stops of 500 GeV are excluded if the neutralino LSP is lighter than 200 GeV.
SNP6. 0 analyses for tumor genomic complexity evaluation The Affymetrix GeneChip Human Mapping 6. 0 ® was normalized using Affymetrix Genotyping Console ® (version GTC 3. 0. 1) (. cel files and data available under accession number GSE48064 in GEO database). The signal from SNP probes was then segmented using Colibri  [32]. A first segmentation round was performed to identify and discard outlier probes giving rise to singleton segments. The number of breakpoints was estimated according to the Zhang and Siegmund's BIC-based model selection criterion (Data S2)  [33]. The optimal segmentation in terms of least-square fit was recovered via dynamic programming. The pruned version proposed in [  [32] ] can be used to achieve this optimization step with almost linear complexity. We used the implementation available in the cghseg package  [34]  via the function The breakpoint number (assessing the number of chromosomal segmental alterations) cut-off able to accurately identify B tumors (poor prognosis tumors) was determined using the Youden index.
Some few aspect-oriented modeling techniques, whose purpose is to weave changes into a (meta)model, provide means for deleting modeling constructs as a "removal" advice. One example is MATA  [11]  for class diagram-like models. A strength of these techniques is that they can designate various elements in a metamodel using a single rule. Such multiple designation rules could easily be integrated in package unmerge (and package merge), e. g. by introducing more sophisticated pattern matching constructs. Compared to aspect-oriented modeling, package merge and unmerge clearly separate the notions of adding information from removing information in two distinct specifications. Another difference is that package unmerge is one simple additional relationship construct to be added to metamodeling languages, unlike aspect-oriented modeling which requires completely new languages, even if aspect languages are defined as extensions to the languages to which aspects are to be applied.
An example found in section 5 was the Core::Suite that had to be dropped even though Core::Project had to be kept. Purpose of model slicing is more about model understanding and impact analysis while purpose of package unmerge is metamodel reuse. Steel et al. [18]  define rules for comparing two metamodels. This way model transformations may declare their input and output domains, so as to check that a given model can actually "enter" a transformation. As such, they check that a model which conforms to a given metamodel also conforms to another metamodel. Unfortunately, a model conforming to a reduced metamodel may not always conform to the metamodelto-be reduced. This stems from the properties of the merge transformation. As pointed out in  [19] , a model conforming to a metamodel-to-be-merged may not conform to the merged metamodel.
Methods The data set for this study was obtained from the official home page of the Swiss Cycling Marathon  [19]  and from the race director. All athletes who ever participated in the Swiss Cycling Marathon between 2001 and 2012 were analyzed regarding participation, performance, and age. The present study was approved by the Institutional Review Board of St. Gallen, Switzerland, with a waiver of the requirement for informed consent given that the study involved the analysis of publicly available data.
Data analysis In order to increase the comparability of this study with the results from similar studies with data from different races, race times were converted to cycling speed (km h -1 ) by calculating (race distance in kilometer) / (race time in hours). To determine the change in cycling speed over time, the annual top (fastest cyclist for men and women) and the annual top three men and women were analyzed separately. Additionally, the age of the annual top and the annual top three women and men was determined. The gender difference in both cycling speed and age of peak performance was calculated using the equation [(cycling speed or age in women) -(cycling speed or age in men)] / (cycling speed or age in men) × 100. The fastest women and men ever (the course record holder in the regarded time period), the three fastest women and men ever, and the ten fastest women and men ever were determined and compared in order to find the absolute fastest performance and the gender difference of the top finishers.
Statistical analysis In order to increase the reliability of the data analyses, each set of data was tested for normal distribution as well as for homogeneity of variances prior to statistical analyses. Normal distribution was tested using D' Agostino and Pearson omnibus normality test, and homogeneity of variances was tested using Levene's test. To find changes in the development of a variable over time, linear regression was used. To find the differences between two groups a Student's t test was used, with Welch's correction in case of significant different variances between the two compared groups. Statistical analyses were performed using IBM SPSS Statistics (version 19, IBM SPSS, Chicago, IL, USA) and GraphPad Prism (version 5, GraphPad Software, La Jolla, CA, USA). Significance was accepted at p < 0.
Data analysis Weekly counts of immature anopheline mosquitoes in 23 treated and untreated ponds were analyzed by life stage categories including early instars (L1 and L2), late instars (L3 and L4), and pupae. The average number of each stage collected in treated ponds (n=9) and untreated ponds (n=2) was calculated weekly. The means of weekly averages in treated and untreated ponds were analyzed across weeks 3 to 52 (n=51) of the study using both a z-test and an ANOVA in order to compare the number of immature stages collected during the entire treatment period. Adult landing collections in treated and untreated areas were similarly compared across time applying ANOVA to monthly collections in the dry season (May to December, n=7 months) and wet season (January to May, n=5 months). Correlation of adult population densities and rainfall in treated and untreated areas were evaluated using the correlation function of the MS Excel data pack (Pearson's correlation coefficient).
ACKNOWlEDGMENTS The authors would like to thank team GIS Division and Technical entomology of the Centro de Pesquisas Zoobotânicas e Geológicas of the Instituto de Pesquisas Científicas e Tecnológicas do Estado do Amapá Aderbal A. Santana, Francisco Redivaldo A. Souza, Jorge P. Duarte and José Claudio C. Mendes. We also thank to Paulo de Tarso R. Vilarinhos for advising on the protocol and contributing to the edits of the article. The authors declare that there is no conflict of interest.
Analysis The transcribed interviews were analyzed and coded by DG and HA, who used both case-oriented and variable-oriented methods  [30]. Each interview was parsed by theme, and recurring themes were identified inferentially. Similarities and differences for variables in each theme were listed. DG, HA, and CA discussed the development of the themes and variables and validated the process. In addition, cross-validation of the thematic analysis was performed simultaneously by DG using the text analysis software TropesH (Semantic Knowledge, France)  [31]. The results were compared and discussed with all authors. Three topics pertaining to the implementation of pediatric trials involving drug therapy were identified: global perception of implementation, problems with implementation, and solutions.
Strengths and Weaknesses of the Study (Internal Validity) We studied perceptions and experiences of several types of stakeholders regarding the implementation of institutionally sponsored pediatric clinical trials of experimental drugs. Clinical research nurses are assuming a growing role in therapeutic trials in many countries  [33] [34] [35]. However, there are few clinical research nurses in France, and their role remains ill-defined. Clinical research nurses were not identified in any of the protocols for pediatric trials of experimental drugs sponsored by the AP-HP between 2002 and 2008. We chose semi-structured interviews to explore participants' opinions without inducing or guiding their answers. Results of qualitative studies should not be extrapolated to the general population. In keeping with qualitative study principles, our objective was not to obtain quantitative data or an exhaustive list of participants' views but, instead, to identify different types of obstacles to the implementation of pediatric clinical trials involving drug therapy.