dataesr/scientific-paragraphs-categorization huggingface dataset:
For the sake of the illustration, the competence variations over time are here hand-defined (surf surface) and proportional to the values in S (increases for positive values, decreases for negative values). We train a GMM of 6 components, G IM , to learn the joint distribution over T × S × C, represented by the six 3D ellipses. Projections of these ellipses are shown in 2D spaces S × C and T × C in the Top-Right and Bottom-Left plots. To reflect the competence progress in this dataset, we then bias the weight of each Gaussian to favor those which display a higher competence progress, that we measure as the covariance between time and competence for each Gaussian (in the example the magenta ellipse shows the higher covariance in the Bottom-Left plot, then the green one, the sky blue one etc).
Solutions to overcome this problem have been proposed, generally based on adult feedback or reformulations associated with infant productions  (Ishihara et al. , 2009; Howard and Messum, 2011; Miura et al. , 2012). This is outside the scope of this paper where our focus is on the selforganization of the developmental sequence in successive stages of increasing complexity. Extending our model to the interaction with real humans would definitely require to consider this issue. Further works will consider higher-dimensional sensorimotor spaces for more realism. For example, the free software Praat  (Boersma, 2012)  is a powerful tool allowing to synthesize a speech signal from a trajectory in a 29-dimensional space of respiratory and oro-facial muscles. Numerous acoustic features can in turn be extracted from the synthesized sound, among which the Mel-frequency cepstral coefficients (MFCC;  Davis and Mermelstein, 1980).
The World Overview of Conservation Approaches and Technologies (WOCAT) provides a global database   [103] , which provides maps of organic carbon content in the surface horizon of soils in Europe  [20] , and the Global Soil Partnership  [104] , which is a major international initiative that has recently produced an analysis of state of the art of soil information, including information on SOC. Another example is a new network for francophone Africa, which aims to exchange information on SOC storage and methods to achieve this  [105]. A global consortium has been formed to produce a digital soil map of the world at fine resolution  [106]. Finally, the Global Soil Biodiversity Initiative aims at developing a coherent platform for promoting the translation of expert knowledge on soil biodiversity into environmental policy and sustainable land management  [107].
A model combining the partial-equilibrium and para-equilibrium thermodynamic approximations is presented. It accounts for fast diffusion of interstitial elements, such as carbon, and low diffusion of substitutional elements in the solid phases, while complete mixing is assumed for all elements in the liquid phase. These considerations are turned into classical mathematical expressions for the chemical potentials and the u-fractions, to which mass conservation equations are added. The combination of the two models permits application to steels, dealing with partial-equilibrium for solidification and para-equilibrium for both the δ -BCC to γ-FCC peritectic transformation and the γ-FCC to α-BCC solid state transformation. The numerical scheme makes use of calls to Thermo-Calc and the TQ-interface for calculating thermodynamic equilibrium and accessing data from the TCFE6 database.
The LR treatment of the peritectic transformation is also a very crude approximation that does not fix the problem in coherent manner with respect to the PE approximation. In the present study, a new numerical scheme is presented for the computation of phase transformations in steels. It is coupled with thermodynamic equilibrium calculations based on call to the software Thermo-Calc  6)  through the TQ-interface using the TCFE6 database. 7) The so-called para-equilibrium (PA) approximation presented by  Hillert 8)  has been introduced to deal with the peritectic reaction during a PE solidification path, later refereed as PE + PA approximation. This is implemented in previous developments presented by Zhang et al. 4)  for the computation of LR, GS and PE + LR solidification paths. Because PA was initially developed for solid state transformations, it is also used to simulate phase transformations during cooling expe-© 2014 ISIJ rienced during steel processing after solidification.
Solidification Path for S-1 The measured liquidus temperature by means of DTA and the calculated one are shown in Table  2. The calculated value based on thermodynamic equilibrium is slightly lower than measurement. It is yet within the uncertainty of the experimental method. During DTA, the temperature difference between the alloy sample and a reference sample is recorded during heating to reveal the latent heat required during melting. Such a phase transformation, however, needs a driving force leading to overheating of the sample to transform the solid into liquid, and hence uncertainty in the determination of the liquidus temperature. The other possible reason is inherent to the precision of the thermocouples and the accuracy of the thermodynamic database. Overall, the comparison is thus considered as very good.
Next, target sites were aligned, together, and normalized (blue solid lines, Figure  6E ). Internal controls (grey lines, Figure  6E ) were obtained by using the same procedure but for target sites that did not contain any of the features (CP190 or Chromator). This procedure generated background interaction levels reflecting the chromatin context of the anchor site. Frequencies of interactions were statistically tested by Wilcoxon tests. For the analysis of ChIP-chip data (Venn diagrams), publicly available. gff3 files were downloaded from the modENCODE website (http://data. modencode. org/) corresponding to CP190, BEAF32 and Chromator/Chriz ChIP-chip experiments performed in BG3 and S2 cells  [48, 84]  (datasets 274, 275, 278, 279, 280, 921, 924). Overlaps between binding sites were calculated with the intersectBed function of the BEDTools software  [85].
Crystallization, data collection, processing, structure determination and refinement Crystallization trials was carried out by the sitting-drop technique using the classic, PEG, PACT and AmSO4 suites (Quiagen, France) and low-profile microplates (Grenier, France) at room temperature. 0. 5 ml protein solution was mixed with an equal volume of reservoir solution. Several conditions yielded crystals. Optimizations were done with the hanging-drop vapor diffusion technique. 1 ml protein solution was mixed with 1 ml of reservoir. We obtained well diffracting crystals (2. 03 A ˚) using 0. 8 M NaH 2 PO 4 , 0. 8 M KH 2 PO 4 , 0. 1M Hepes/pH 7. 5. Crystals were soaked in 30% glycerol for cryoprotection and diffraction data were collected under cryogenic conditions on our laboratory anode and at the European Synchrotron Radiation Facility (ESRF, Grenoble).
Image data were processed and scaled using the programs MOSFLM (Leslie, 1999) and SCALA of the CCP4 suite  [86]  The structure of CP190-BTB/POZ was solved by molecular replacement with an in-house dataset at 2. 3 A ˚resolution using the program PHENIX (phenix. autoMR) [87]  and a combination of five partial models extracted from the server TOME  [88]  used to gather potential templates through fold-recognition. Structure refinement and rebuilding were performed with COOT  [89] , PHENIX (phenix. refine) [87]  and REFMAC (Murshudov et al, 1997) from the CCP4 suite  [86]  using a dataset recorded at the ESRF at 2. 0 A ˚resolution. Data collection and refinement statistics are summarized in Supplementary Table  S1. The structure has been deposited with the Protein Data Bank (PDB 4U77).
Financial support was provided by  European Research Council Starting  Grant  260787  (MN). We also thank the  French National Research Agency  grant ( ANR-2010-BLAN-1221 01  to OC, MN, and EM), the  France-BioImaging infrastructure  ( ANR-10-INSB-04 ) and the  French Infrastructure for Integrated Structural Biology  ( ANR-10-INSB-05-01 ). The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
Labels, more precisely security clearances, are host attributes Ψ = {unclassified , confidential , secret, topsecret}. The Bell LaPadula's no read-up and no write-down rules can be summarized by requiring that the security clearance of a receiver r should be greater-equal than the security clearance of the sender s, for all (s, r) ∈ E. With a total order '≤' on Ψ , the security invariant template can be defined as m((V, E), P ) ≡ ∀(s, r) ∈ E. P (s) ≤ P (r). Let the scenario-specific knowledge be that database db 1 ∈ V is confidential and all other hosts are unclassified. Using lambda calculus, the total function P can be defined as (λh. if h = db 1 then confidential else unclassified ). Hence P (db 1 ) = confidential. For any policy G, the predicate m(G, P ) holds if db 1 does not leak confidential information (i.
Case Study: A Cabin Data Network In this section, we present a slightly more complex scenario: a policy for a cabin data network for the general civil aviation. This example was chosen as security is very important in this domain and it provides a challenging interaction of different security invariants. It is a small imaginary toy example, developed in collaboration with Airbus Group. To make it self-contained and accessible to readers without aeronautical background knowledge, it does not obey aeronautical standards. However, the scenario is plausible, i. e. a real-world scenario may be similar. During our research, we also evaluated real world scenarios in this domain. With this experience, we try to present a small, simplified, self-contained, plausible toy scenario that, however, preserves many real world snares.
Acknowledgments & Availability. We thank all the participants of our feedback session and the anonymous reviewers very much. A special thanks goes to our colleague  Lothar Braun  for his valuable feedback. Lars Hupel helped finalizing the paper. This work has been supported by the  German Federal Ministry of Education and Research (BMBF)  under support code  16BY1209F , project  ANSII , and  16BP12304 ,  EUREKA  project  SASER , and by the  European Commission  under the  FP7  project  EINS , grant number  288021. Our Isabelle/HOL theory files and topoS's Scala source code are available at https://github. com/diekmann/topoS.
LHC constraints: The new interactions in the leptonic sector can also alter the Higgs boson phenomenology: the presence of a new decay channel for the Higgs boson, with heavy neutrinos in the final state, can enlarge the total Higgs decay width, thus lowering the predicted SM decay branching ratios. Therefore, constraints on sterile neutrinos are also derived from Higgs decays. LHC data already allows to constrain regimes where the sterile states are below the Higgs mass, due to the potential Higgs decays to an active and a heavier, mostly sterile, neutrino. In our analysis we apply the constraints derived in  [17, 19, 20].
Simulation of value network of Alpina Needed data (concerning products, processes, supply chain, distributor, suppliers, etc. ) were collected from the enterprise using different templates and many interviews with different departments of Alpina. An empirical study realized by Alpina permitted obtaining the perceived quality attributes (fitting, aesthetics, material, thermal comfort, flexibility, weight, stability, breathability, durability and waterproofing, brand name, ecological level, shop assistance, customization time and number of proposed product variants). Thus all needed data for building the value model was provided by the real world. The performance indicators measuring customer value were chosen in coherence with the firm's strategy. Concerning the service related attributes, they are chosen according to  (Daaboul et al.
Study design This was a multinational, multicentre, double-blind, randomised, placebo-controlled, 24-week phase 3 study (#NCT01275066). The study was conducted by 34 principal investigators at 33 study centres in 17 countries. A schematic presentation of the study design is shown in Supportive online material 1. After screening, eligible patients completed baseline assessments and were randomised to receive infusions of elosulfase alfa 2. 0 mg/kg/week, elosulfase alfa 2. 0 mg/kg/ every other week (qow) or placebo for a period of 24 weeks. Randomisation was stratified by screening 6MWT category (≤200 and >200 m) and age group (5-11, 12-18, ≥19 years old). Patients, investigators and site personnel were blinded to treatment assignment throughout the study and until the final analysis was complete.
The results of the 3MSCT were tested first, and the urine KS results could only be declared significant if the 3MSCT showed a significant result due to the requirement of the prespecified statistical analysis plan. For the primary and secondary endpoints, the Hochberg method for multiplicity adjustment was used for the two treatment comparisons with placebo  (Hochberg 1988). There was only one subject with missing data points for 6MWT at 24 weeks. Multiple imputation was used in the primary analysis of primary, secondary and respiratory function test endpoints  (Rubin 1987 ) when a measurement was not available. The imputation was based on the joint normal distribution for the endpoint at all scheduled assessments, baseline age and baseline 6MWT scores. Safety analysis included all patients who received any study drug (either elosulfase alfa or placebo) throughout the study duration.
Patient characteristics Of the 204 patients who were screened, 177 were randomised. One randomised patient was not dosed and excluded from all analyses because the diagnosis of Morquio A syndrome was not confirmed. Of the 176 patients, 59 were randomised to placebo, 59 to elosulfase alfa 2. 0 mg/kg/qow and 58 to elosulfase alfa 2. 0 mg/kg/week; 175 patients completed the study. One patient in the elosulfase alfa 2. 0 mg/kg/week population discontinued after the first infusion due to withdrawal of consent. The withdrawal was due to logistic difficulties for attending study visits and not because of safety concerns. All treatment groups achieved high mean dosing compliance (range 96. 8 to 99. 2 %) and few efficacy data points were missing. Baseline demographics and clinical characteristics of the patients are listed in Supportive online material 2, showing a broad distribution of ages ranging from 5 to 57 years (median age 11.
The present study was designed to determine whether ERT with elosulfase alfa could be a therapy for Morquio A syndrome. ERT replaces the deficient GALNS enzyme by a functioning enzyme (rhGALNS or elosulfase alfa), thus repairing the mechanism for degrading keratan sulfate and chondroitin sulfate which is believed to lie at the basis of the disease manifestations. The dosing regimen of 2. 0 mg/kg/week was selected on the basis of data from a phase 1/2 clinical study  (Hendriksz et al 2012)  evaluating dose escalation which showed greatest reduction in urine KS at 2. 0 mg/kg and on nonclinical and in vitro studies with elosulfase alfa (Dvorak-Ewell et al 2010). A more convenient 2. 0 mg/kg/qow dosing regimen was also evaluated to determine whether patients could derive benefit (and a lower risk of AEs) with less frequent dosing and lower cumulative exposure.
The percent of subjects with SAEs was approximately four-fold higher on the once weekly regimen than on placebo. A majority of the SAEs in the weekly dose group were either infusion-related, surgical procedure-related, or disease-related. All patients receiving elosulfase alfa developed antielosulfase alfa antibodies. Although it is not possible to determine whether this had an effect on the magnitude of the efficacy responses or on the incidence of hypersensitivity AEs, it is of interest that neither total antibody titres nor NAb positivity were associated with hypersensitivity AEs. The present study is the largest placebo-controlled trial conducted to date in MPS patients and has generated a reasonable safety database for this ultra-rare disease. The impact of elosulfase alfa on 6MWT distance and urine KS levels shows that the therapy indeed has the potential to correct the biological cause of Morquio A syndrome.
Acknowledgments We acknowledge the participation of study patients and their families and the expert assistance of all study site coordinators and personnel. This study was sponsored by  BioMarin  and supported, in part, by the  National Center for Advancing Translational Sciences, National Institutes of Health , through  UCSF-CTSI  Grant Number  UL1 TR000004  ( Dr. Harmatz ), and the  Manchester NIHR/Wellcome Trust Clinical Research Facility  ( Dr. Jones ). Its contents are solely the responsibility of the authors and do not necessarily represent the official views of the  NIH. The authors are also grateful to  Ismar Healthcare NV , funded by  BioMarin Pharmaceutical Inc. , for support in the process of manuscript development.
The volatility modeling for autoregressive univariate time series is considered. A benchmark approach is the stationary ARCH model of Engle (1982). Motivated by real data evidence, processes with non constant unconditional variance and ARCH effects have been recently introduced. We take into account such possible non stationarity and propose simple testing procedures for ARCH effects. Adaptive McLeod and Li's portmanteau and ARCH-LM tests for checking for second order dynamics are provided. The standard versions of these tests, commonly used by practitioners, suppose constant unconditional variance. We prove the failure of these standard tests with time-varying unconditional variance. The theoretical results are illustrated by mean of simulated and real data.
In summary LM cv,ALS , LM mc cv,ALS and LB cv,ALS , LB mc cv,ALS correspond to tests for which the bandwidth is selected automatically from the data. Tests like LM b sm,ALS , LM b la,ALS , and LB mc sm,ALS , LB mc la,ALS correspond to tests with bandwidths b = γ(σ 2 /n) 1/5 for suitable γ. The constant γ for such bandwidths may be fixed in practice using a preliminary simulation experiment as illustrated in the real data analysis below.
2 and for the homoscedastic case. From Figure  8. 1 it appears that the GLS tests are more powerful than the ALS tests. Nevertheless recall that the GLS tests are built on the unrealistic assumption of known h t which make them infeasible in applications. Now considering the outputs for the homoscedastic case in Figure  8. 2, it turns out that the standard tests have some power advantage on most of the adaptive portmanteau tests. However, we noted that the LM b la,ALS has similar properties to the standard tests, which may be explained by the fact that larger bandwidths allows for more accurate estimates of a constant variance function. Finally it seems that all the tests are subject to a loss of power as m is increased. In the light of our simulation experiments we could draw some conclusions and provide some guidelines for the real data applications.
From 1973 for the PPI and from 1979 for the M1, we also observe clusters of large values which may indicate the presence of second order dynamics. It also emerges that the CPI data display a declining variance. In order to study the variance structure of the innovations, we adjusted AR models to the PPI and M1 series. Meanwhile, it was found that the CPI series is uncorrelated. To check the AR models adequacy we used the portmanteau tests developed in  Patilea and Raïssi (2011)  which are valid under A1 (the outputs are not displayed here). Once the linear dynamics of the series are well captured, we can turn to the analysis of the second order dynamics in the uncorrelated processes. For the variance specification of the series a practitioner would likely use a model which takes into account for possible non constant unconditional variance but excludes second order dynamics as in * * The data are available in the website of the research division of the federal reserve bank of Saint Louis: www.
We first remark that the p-values of the standard tests are very close to zero so that the null hypothesis of no second order dynamics is clearly rejected for the three data series. On the other hand, for the PPI and M1 data, for any of the values of m we considered, the p-values of the adaptive tests are far above 0. 05, so that the null hypothesis of no second order dynamics is not rejected. For the CPI data, all but one p-values of the adaptive tests are above 0. 05, some of them far above 0. 05, the exception being the case m = 1. In view of Figure  8. 3 which clearly reveals a non stationary in variance behavior of the three series we investigated, it is likely that the standard tests spuriously reject the null hypothesis. Meanwhile, our adaptive tests provide very different conclusions which could lead one to confidently reconsider the possibility of using an elaborated specification which allow for second order dynamics for the M1 and PPI series.
Moreover, the transitions at sunset and sunrise were found to be difficult to simulate correctly. In separate studies, Holtslag et al. Holtslag et al. (2007)  and  Baas et al. (2008)  showed that the spread in terms of SBL structure, when using various SBL parametrizations, tends to decrease when there is interaction with the surface instead of using prescribed surface flux or surface temperature as a lower boundary condition. The third GABLS case addresses the issues of the large-scale forcings, the interaction with the surface, evening and morning transitions and the direct evaluation of models with observations. The case was derived from the long-term dataset at Cabauw, The Netherlands. The specific characteristics of the Cabauw site, e. g. its flat topography and sufficient homogeneity (Ulden and Wieringa 1996;  Beljaars and Bosveld 1997) , make it well-suited to study momentum decoupling around sunset, low-level jet (LLJ) formation, and the morning transition  (Angevine and Klein Baltink 2001).
Soil heat-flux observations are made with soil heat-flux plates, and together with soil temperature observations they are used to derive the surface soil heat flux  (Beljaars and Bosveld 1997 ). Friction velocity is derived from the wind speed at 10-m height and the same regional scale roughness length as prescribed in the case set-up. Observed sensible heat flux is used to correct for stability effects. Taking the eddy-correlation observations would result in too low a friction velocity, induced by the local low roughness length. This friction velocity would not be representative of the scale of the boundary layer  (Bosveld et al. 2014). All data are processed to 10-min mean values and archived in the CESAR database (http://www. cesar-database. nl). When comparing model results with observations, it is important to assess the uncertainty in the observations.
With sufficient stratification, z will become less important at greater heights and the length scale will largely be determined by Ri G. For a given z, we can compare the mixing efficiency deduced from the models and from observations. In Fig. 9  the mixing lengths for heat and momentum around midnight, deduced from Eq. 3, are plotted as a function of the gradient Richardson number. Data from the models are shown for the grid level closest to the 60 m. The 60-m level is well within the turbulent SBL and above the lowest grid level of all models. For models with a staggered grid, where the state variables and fluxes are on different levels, the calculations were straight forward. Some models had a different grid configuration and an extended version of Eq. 3 was applied, allowing for different levels for momentum and temperature.