Projection pursuit searches for a direction along which the data look least Gaussian. When the observation space contains a large Gaussian complement, the empirical objective can be minimized by a direction that carries no signal, with empirical kurtosis as low as at the truth. Sample splitting exposes rather than repairs this failure. Appending coordinates independent of the latent regime degrades the search while leaving Bayes recoverability unchanged. Restricting the search to the column space of a known forward operator removes the failure exactly on the negative-kurtosis branch. Estimating a principal subspace from the data is the alternative. In a controlled two-component model, the leading sufficient scalings differ in the gain with which the operator transmits the discriminant: ς−4 for covariance-spike estimation and ς−8 for fourth-moment search. At fixed search dimension, the measured threshold ratio collapses onto n/p2 with exponent 0.156, close to the predicted 1/8. This is an empirically supported scaling motivated by sufficient bounds, not a proved asymptotically tight law. When the search dimension is varied, the measured exponent is 0.325, substantially larger than 1/8, and the tested range does not identify its functional form. The crossing location also depends on calibration and model configuration. Under a downstream excess-error criterion, the scaling largely disappears.
Figures & tables
exponent
95% CI
R2
Collapse on n/p2 at fixed dsearch
fixed 15∘ criterion
0.150
[0.110,0.166]
0.964
calibrated criterion
0.156
[0.118,0.174]
0.965
Rank dependence, dsearch∈{2,…,32}
ςKPP
0.325
[0.259,0.399]
ςPCA
−0.031
Table 1: Measured threshold scalings. The fixed-rank collapse is fitted over 11 configurations and the rank comparison over 28 . The calibrated criterion is 15.4∘ – 20.5∘ on the collapse grid. The tested rank range does not distinguish the candidate functional forms.
p
n
n/p2
ςPCA
ςKPP
ratio
1024
4096
0.004
2.200
0.924
0.42
512
4096
0.016
1.687
0.868
0.51
256
4096
0.062
1.240
0.911
0.73
128
4096
0.250
1.022
1.098
1.07
128
16384
1.000
0.659
0.819
1.24
32
4096
4.000
0.676
0.908
1.34
Table 2: Threshold discriminant gains and their ratio. The ratio crosses one at n≈0.60p2 under the 15 ∘ criterion at which it was measured; Section 5.1 shows why that number is not transportable. The same thresholds computed on cells with no optimizer gap, and re-searched at a 512-fold larger restart budget, are in Appendix A and agree to within the bootstrap interval of the crossing.
Figure 1: Ratio of the exact-subspace KPP threshold to the PCA-subspace threshold against n/p2 at fixed r . The fitted fixed-rank power law is shown for reference. The ratio crossing depends on the success criterion and model configuration; the marked value is for the baseline 15∘ criterion and is not interpreted as a universal constant.
Condition
Crossing
Exponent
( n/p2 )
10∘ criterion
1.20
0.142
15∘ criterion (baseline)
0.60
0.150
20∘ criterion
0.30
0.145
Strongest-spike discriminant
0.006
—
Anisotropic Σ
not determined
—
Table 3: Sensitivity of the threshold comparison. The crossing changes with the angular criterion and with the covariance-spike configuration. For the anisotropic row, the prefactor shift is not constant across the rank grid, so no single crossing is reported.
Figure 2: Sample splitting exposes but does not remove the unrestricted-search failure. (a) Out-of-sample κ^ for the split search follows the unrestricted full-sample arm and remains near zero, while the restricted arm approaches κ⋆ . (b) With nB=800 , validation noise can make a spurious candidate look better than u⋆ ; with nB=12800 , validation correctly ranks u⋆ above the selected candidate, but the search never proposed u⋆ .
Appendix figures & tables3 assets
Supplementary material from the paper’s appendix.
Appendix
p
n
n/p2
ςKPP
gap-clean
budget
1024
4096
0.004
0.924
0.905
0.875
512
4096
0.016
0.868
0.868
0.868
256
4096
0.062
0.911
0.911
0.911
128
4096
0.250
1.098
1.098
1.098
128
16384
1.000
0.819
0.786
0.773
32
4096
4.000
0.908
0.908
0.906
Appendix
Table 4: The kurtosis threshold measured via the standard restart budget, on cells with an optimizer gap within the null tolerance, and re-searched at a 512-fold larger budget. The implied crossings are within the bootstrap interval of one another.
Figure 3: Direct evaluation of Theorem 1 . (a) Uniform deviation η=supu∈U∣κ^T(u)−κ(u)∣ against n for the unrestricted search at several p (solid) and the operator-subspace restricted search at r=4 (dashed). (b) The same data against p at fixed n ; the shaded band spans the dsearch1/2 to dsearch1 dependence allowed by Eq. ( 6 ).
fwd. model
regimes
subspace
true
method
H,Φ,σ,K
M
R
(π,μ,Σ)
labels
oracle (control)
yes
yes
yes
yes
no
latent-space k -means
yes
yes
not used
no
no
kurtosis, full space
yes
yes
not used
no
no
kurtosis, operator-subspace
yes
yes
used
no
no
kurtosis, PCA-restricted
yes
yes
estimated
no
no
Appendix
Table 5: Train-time information available to each method.
Principal component analysis (PCA) is a fundamental tool to reduce the dimensionality of the data in many applications. PCA finds a few signal directions that contain most of the variability of the data by computing the eigenvectors of the sample covariance matrix. In this work, we focus on the spiked covariance model, in which the data vectors are defined by a few orthogonal signals plus an isotropic Gaussian noise, and our goal is to estimate one or more of the leading signals. Our main theoretical finding is that the subspace spanned by several leading eigenvectors of the sample covariance matrix contains significant information about the desired signals long before the individual eigenvectors converge to the population principal components. To prove this, we derive a posteriori bounds for the angle between the subspace spanned by the desired population signals and the subspace obtained from the sample using perturbation theory for singular vectors. This leads to a new algorithm, SuperPCA (SUbsPace subsamplER PCA), which capitalizes on an approximate eigenspace of the sample covariance matrix to find the leading signals far more efficiently and accurately than classical PCA in the high-dimensional, multi-signal setting. SuperPCA exploits only a small number of subsampled coordinates of the data, which can lead to tremendous savings in data acquisition cost, especially when the signals are approximately sparse. For the same number of measurements, SuperPCA can offer a factor 10 improvement in accuracy compared to the classical PCA method.
Mathematical Institute, University of Oxford, Oxford, OX2 6GG, UK · Bernoulli Institute for Mathematics, Computer Science and Artificial Intelligence, University of Groningen, 9700 AB, Groningen, The Netherlands · Institute of Mathematics, EPFL, 1015 Lausanne, Switzerland
This paper analyzes bidirectional random projections for ordinary least squares (OLS) regression under the fixed design setting. Let (X,Y)∈Rn×p×Rn be a sample and R∈Rn1×n,W∈Rp×p1 be two properly distributed random projections. We develop an expected excess loss bound for the OLS estimator built on (WXR,WY). Compared to an established bound for OLS estimator built on (XR,Y), the gap is approximately O(p1+Cp11), where C scales with n1/n and can be negative for small n1/n. Its implications are confirmed by numerical results on real-world data.
Chao Lan, Luyuan Yang
a School of Computer Science, University of Oklahoma, U.S.
Restricted eigenvalue (RE) bounds govern stable recovery by norm-regularized estimators. For isotropic sub-Gaussian measurements, the benchmark sample size is 1+w(A)2, where w(A) is the Gaussian width of the normalized descent cone. The COLT 2015 open-problem note (Banerjee et al., 2015) asked whether the same law follows for heavy-tailed designs from a uniform small-ball condition alone. We give an explicit and systematic negative answer to the general question as formulated there: the proposed law fails in its full dimension-free, arbitrary-set form, and the missing obstruction is simultaneous threshold occupancy. A constant-width polyhedral descent cone with fixed small-ball constants has zero empirical RE on every sample path up to half the ambient dimension. More generally, every finite range space admits exact threshold encoding in an arbitrarily narrow spherical cap and a lift to a full polyhedral descent-cone section. For every fixed threshold VC dimension d, as β↓0, the sharp worst-case sample complexity is Θ(β−1[dlog(1/β)+log(1/δ)]). The separation persists under exact isotropy and all finite moments: on the same constant-width cone, Gaussian measurements succeed with O(1+log(1/δ)) samples, whereas an isotropic heavy-tailed design fails pathwise for n≲p/logp. Gaussian smoothing yields an everywhere-positive C∞ density while retaining arbitrarily poor RE. Under isotropy, a distribution-free fallback governed by affine dimension times squared enclosing radius is sharp on this family.
Shi Fu, Huibo Xu, Qixin Zhang +1
Generative AI Lab, College of Computing and Data Science, Nanyang Technological University, Singapore